Gaming the Float: How Managers Respond to EPS-based Incentives
Gaming the Float: How Managers Respond to EPS-based Incentives
Gaming the Float: How Managers Respond to EPS-based Incentives
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<strong>Gaming</strong> <strong>the</strong> <strong>Float</strong>:<br />
<strong>How</strong> <strong>Managers</strong> <strong>Respond</strong> <strong>to</strong> <strong>EPS</strong>-<strong>based</strong> <strong>Incentives</strong> ∗<br />
Alan D. Crane †<br />
Jones Graduate School of Business<br />
Rice University<br />
Chishen Wei §<br />
Nanyang Business School<br />
Nanyang Technological University<br />
July 11, 2013<br />
Andrew Koch ‡<br />
Katz Graduate School of Business<br />
University of Pittsburgh<br />
Abstract<br />
We show that <strong>the</strong> likelihood of meeting earnings per share (<strong>EPS</strong>) forecasts is mechanically positively<br />
related <strong>to</strong> <strong>the</strong> number of shares outstanding. As a result, by changing shares outstanding, managers can<br />
affect <strong>the</strong> long run probability of meeting future <strong>EPS</strong> forecasts without affecting earnings or analysts’<br />
forecasts. We find that firms with unpredictable earnings and firms with managers that have compensation<br />
more sensitive <strong>to</strong> <strong>EPS</strong> outcomes have more shares outstanding. To address causality, we find that an<br />
exogenous drop in <strong>the</strong> likelihood of meeting a forecast causes managers <strong>to</strong> increase shares outstanding,<br />
primarily through s<strong>to</strong>ck splits. Following an increase in shares, accounting and real earnings management<br />
drop and <strong>the</strong> firm meets <strong>EPS</strong> forecasts more frequently going forward. Our results suggest that managers<br />
use s<strong>to</strong>ck splits as a long term substitute for traditional earnings management <strong>to</strong>ols. This provides an<br />
important link between <strong>EPS</strong> reporting and capital market activities.<br />
Keywords. Earnings per share; Earnings management; S<strong>to</strong>ck splits<br />
∗ We thank Brian Akins, Leonce Bargeron, Alex Butler, Mike Crawley, Dave Denis, Diane Denis, Steve Dimmock, Mei Feng,<br />
Nishad Kapadia, Bin Ke, Paul Malatesta, Sebastien Michenaud, K. Ramesh, Shawn Thomas, K.C. John Wei, James Wes<strong>to</strong>n<br />
and seminar participants at Rice University and University of Pittsburgh for <strong>the</strong>ir helpful comments.<br />
† acrane@rice.edu<br />
‡ awkoch@pitt.edu. Corresponding author. 326 Mervis Hall, Rober<strong>to</strong> Clemente Drive, Pittsburgh, PA, 15260. 412-648-1187.<br />
§ cswei@ntu.edu.sg
1 Introduction<br />
Earnings per share (<strong>EPS</strong>) is a widely followed and heavily scrutinized financial indica<strong>to</strong>r in <strong>the</strong> US. Evidence<br />
suggests that managers care about <strong>EPS</strong> targets (Graham et al. (2005)). A large literature documents a<br />
variety of actions that managers take <strong>to</strong> affect <strong>the</strong> gap between earnings realizations and <strong>EPS</strong> forecasts by<br />
changing earnings, forecasts, or both. 1 This literature generally takes <strong>the</strong> concept of “meeting”, “beating”,<br />
or “missing” forecasts as given. We show that, even if two managers have identical earnings and forecasts,<br />
one can “miss” while <strong>the</strong> o<strong>the</strong>r “meets”. The rules of <strong>the</strong> game are actually <strong>the</strong> manager’s choice. In this<br />
paper, we show that managers can affect <strong>the</strong> likelihood that <strong>the</strong>ir firm meets future <strong>EPS</strong> forecasts without<br />
affecting <strong>the</strong>ir firm’s reported earnings or guiding forecasts. They do so by choosing <strong>the</strong> number of shares<br />
outstanding.<br />
For any given <strong>EPS</strong> forecast, <strong>the</strong>re exists a range of <strong>to</strong>tal earnings that will meet that <strong>EPS</strong> forecast.<br />
For example, a firm with 1000 shares outstanding and <strong>EPS</strong> forecast of $0.20 will meet <strong>the</strong> forecast with any<br />
earnings ∈ [$195, $205). This range exists because per-share earnings are rounded <strong>to</strong> <strong>the</strong> penny. Importantly,<br />
<strong>the</strong> amount of rounding is a choice variable; it is an increasing function of <strong>the</strong> number of shares outstanding.<br />
If <strong>the</strong> same firm has twice as many shares outstanding, <strong>the</strong> firm meets <strong>the</strong> forecast for any earnings ∈ [$190,<br />
$210). The wider this range, <strong>the</strong> higher <strong>the</strong> probability of meeting <strong>EPS</strong> forecasts, more specifically:<br />
P r(meet) = P r(µ − s ∗ 0.5¢ ≤ x < µ + s ∗ 0.5¢)<br />
where x represents <strong>the</strong> realization of <strong>to</strong>tal earnings, s is <strong>the</strong> number of shares outstanding, and µ is <strong>the</strong><br />
forecasted <strong>to</strong>tal earnings implied by <strong>the</strong> <strong>EPS</strong> forecast. Increasing <strong>the</strong> number of shares increases <strong>the</strong> size of<br />
this range (<strong>the</strong> “target size”). To put it simply, <strong>the</strong> practice of rounding <strong>EPS</strong> outcomes has a bigger effect<br />
<strong>the</strong> more shares a firm has. <strong>Managers</strong> can exploit this fact <strong>to</strong> influence <strong>the</strong> probability of meeting all <strong>EPS</strong><br />
forecasts going forward. <strong>How</strong>ever, this is not costless; as managers increase <strong>the</strong> number of shares, <strong>the</strong> share<br />
price drops mechanically. This can have liquidity costs and, in <strong>the</strong> limit, result in delisting.<br />
We develop and test several implications of <strong>the</strong> hypo<strong>the</strong>sis that managers engage in target size management<br />
(TSM) - adjusting shares outstanding <strong>to</strong> affect <strong>the</strong> size of <strong>the</strong> range of <strong>to</strong>tal earnings that meets<br />
<strong>EPS</strong> forecasts. 2 Our primary hypo<strong>the</strong>sis is that managers of firms that are likely <strong>to</strong> miss <strong>EPS</strong> targets due <strong>to</strong><br />
chance in <strong>the</strong> future will choose a larger target size. This is equivalent <strong>to</strong> saying that firms with unpredictable<br />
1 For comprehensive reviews of <strong>the</strong> earnings management literature, see Healy and Wahlen (1999), Dechow and Skinner<br />
(2000) and Dechow et al. (2010).<br />
2 We focus on <strong>EPS</strong> forecasts as <strong>the</strong> relevant threshold, however target size management could apply <strong>to</strong> any threshold, as long<br />
as <strong>the</strong> threshold is measured and rounded at <strong>the</strong> share level.<br />
2
earnings will choose more shares outstanding, all else equal. By choosing this larger target, a larger range<br />
of earnings outcomes will round <strong>to</strong> any given <strong>EPS</strong> forecast. If firms with unpredictable earnings did not<br />
choose larger targets, <strong>the</strong>y would miss <strong>EPS</strong> forecasts more often than similar firms with earnings that are<br />
easy <strong>to</strong> forecast. We proxy for unpredictable earnings in several ways, one of which is net income volatility. 3<br />
We find that firms in <strong>the</strong> highest decile of net income volatility have over three times <strong>the</strong> number of shares<br />
outstanding compared <strong>to</strong> firms with <strong>the</strong> lowest volatility.<br />
We also expect target size <strong>to</strong> be related <strong>to</strong> <strong>the</strong> manager’s incentives <strong>to</strong> meet or beat <strong>EPS</strong> forecasts. A<br />
large target makes a firm less likely <strong>to</strong> miss <strong>the</strong> <strong>EPS</strong> forecast. <strong>How</strong>ever, it also makes it more difficult for <strong>the</strong><br />
firm <strong>to</strong> beat that forecast. Therefore, we expect <strong>to</strong> find larger targets among managers with a high cost <strong>to</strong><br />
missing forecasts relative <strong>to</strong> <strong>the</strong> benefits of beating those same <strong>EPS</strong> forecasts. Using data on executive bonus<br />
and option ownership, we proxy for <strong>the</strong> sensitivity of <strong>the</strong> manager’s compensation in <strong>EPS</strong> outcomes. 4<br />
We<br />
find that firms with managers in <strong>the</strong> <strong>to</strong>p decile of incentive compensation have 40% more shares outstanding<br />
relative <strong>to</strong> firms with managers in <strong>the</strong> bot<strong>to</strong>m decile.<br />
Next, we examine <strong>the</strong> implications of target size management for time series variation in shares outstanding<br />
and how this impacts firms’ usage of earnings management. Over time, <strong>the</strong> fundamentals of a firm<br />
may change, and <strong>the</strong>refore <strong>the</strong> optimal target size may also change. For example, if <strong>the</strong> firm’s net income<br />
grows, <strong>the</strong> size of <strong>the</strong> target relative <strong>to</strong> <strong>the</strong> firm will shrink simply as a result of this growth. As <strong>the</strong> target<br />
size shrinks, <strong>the</strong> probability of rounding <strong>to</strong> <strong>the</strong> <strong>EPS</strong> forecast will decrease and <strong>the</strong> manager may need <strong>to</strong> use<br />
more accounting and real earnings management <strong>to</strong>ols in order <strong>to</strong> meet this shrinking target. <strong>Managers</strong> can<br />
increase <strong>the</strong> firm’s number of shares in order <strong>to</strong> change <strong>the</strong> target <strong>to</strong> a size appropriate for that of <strong>the</strong> larger<br />
firm. 5<br />
We expect an increase in shares <strong>to</strong> have one or both of <strong>the</strong> following effects: <strong>the</strong> firm should meet<br />
<strong>EPS</strong> forecasts more frequently, and/or <strong>the</strong> usage of o<strong>the</strong>r earnings management <strong>to</strong>ols should drop. We find<br />
evidence of both. The magnitudes of accruals and discretionary investment drop significantly following an<br />
increase in shares outstanding, and simultaneously <strong>the</strong> firm is 18% less likely <strong>to</strong> miss <strong>EPS</strong> forecasts.<br />
<strong>Managers</strong> have numerous mechanisms <strong>to</strong> adjust share float.<br />
We find that target size management is<br />
primarily achieved through s<strong>to</strong>ck splits. There is little evidence that <strong>the</strong> target size is adjusted through <strong>the</strong><br />
issuance (or repurchase) of new shares. This is not surprising given that splits are simply an accounting<br />
change in <strong>the</strong> number of tradeable securities, whereas issuances have direct economic effects unrelated <strong>to</strong><br />
3 We often use <strong>the</strong> term net income interchangeably with <strong>to</strong>tal earnings. We recognize that <strong>EPS</strong> may reflect adjustments <strong>to</strong><br />
net income. Our results are robust <strong>to</strong> using various definitions of <strong>to</strong>tal earnings.<br />
4 Cheng and Warfield (2005) and Bergstresser and Philippon (2006) find that higher option and s<strong>to</strong>ck compensation is<br />
associated with <strong>EPS</strong> incentives.<br />
5 This is consistent with <strong>the</strong> prior evidence that s<strong>to</strong>ck splits follow net income growth. We discuss how our results relate <strong>to</strong><br />
<strong>the</strong> literature on s<strong>to</strong>ck splits in later sections.<br />
3
target size. 6<br />
Importantly, changes <strong>to</strong> target size as a result of s<strong>to</strong>ck splits are quite common. In a typical<br />
year, roughly 5% of firms split. Over <strong>the</strong> full sample, almost all firms adjust <strong>the</strong> target size <strong>to</strong> keep up with<br />
firm growth. 7<br />
This suggests that TSM is economically important and widely used. Some firms, however,<br />
may find it <strong>to</strong>o costly <strong>to</strong> manage <strong>the</strong> target size. We find that TSM is limited by costs associated with<br />
having a large quantity of shares. A firm with a large target size will have a low s<strong>to</strong>ck price. A low s<strong>to</strong>ck<br />
price may lower s<strong>to</strong>ck liquidity, potentially <strong>to</strong> <strong>the</strong> point of delisting. For firms with low liquidity, we find a<br />
minimal response <strong>to</strong> exogenous changes in net income volatility.<br />
Our analysis is complicated by <strong>the</strong> fact that <strong>the</strong> predictability of earnings is itself a managerial choice<br />
variable. <strong>Managers</strong> can explicitly manage <strong>the</strong> volatility of net income using accruals or real investments<br />
(e.g. Beidleman (1973), Subramanyam (1996), Healy and Wahlen (1999)), and <strong>the</strong>y can use guidance <strong>to</strong><br />
manage <strong>the</strong> forecast. In order <strong>to</strong> demonstrate that our effects are evidence of TSM and not due <strong>to</strong> some o<strong>the</strong>r<br />
fac<strong>to</strong>r related <strong>to</strong> <strong>the</strong> use of accruals or guidance, we employ an instrumental variable approach that uses an<br />
exogenous change in analyst coverage (Hong and Kacperczyk (2010), Degeorge et al. (2012), Derrien and<br />
Kecskés (2012), Kelly and Ljungqvist (2012)) <strong>to</strong> instrument for changes in <strong>the</strong> predictability of <strong>the</strong> firm’s<br />
net income. This instrument captures <strong>the</strong> fact that fewer analysts will result in noisier estimates on average.<br />
Therefore, <strong>the</strong> firm experiences an increase in <strong>the</strong> probability of missing earnings forecasts that is unlikely<br />
<strong>to</strong> be related <strong>to</strong> <strong>the</strong> fundamentals of <strong>the</strong> firm. The causal effect is large. A one standard deviation increase<br />
in instrumented volatility results in an increase in shares of one-half of one standard deviation.<br />
Managerial payoffs are also endogenous. Compensation contracts and <strong>the</strong> market reaction <strong>to</strong> <strong>EPS</strong> surprises<br />
(and <strong>the</strong>refore <strong>the</strong> change in value of <strong>the</strong> manager’s s<strong>to</strong>ck and option holdings) are likely <strong>to</strong> be<br />
determined <strong>based</strong> on <strong>the</strong> underlying fundamentals of <strong>the</strong> firm, including <strong>the</strong> predictability of <strong>the</strong> earnings. 8<br />
Using <strong>the</strong> same instrumental variable approach, we examine if an exogenous shock <strong>to</strong> this predictability has<br />
a greater effect on shares among firms whose managers have pay that is ex-ante highly sensitive <strong>to</strong> <strong>EPS</strong> outcomes.<br />
We find that <strong>the</strong> relation between shares and instrumented volatility is primarily driven by managers<br />
with high incentive compensation.<br />
To summarize, on balance our evidence is consistent with TSM. In <strong>the</strong> cross section, firms with more<br />
unpredictable earnings and firms with managers more sensitive <strong>to</strong> negative <strong>EPS</strong> outcomes choose larger<br />
6 Passive changes <strong>to</strong> float occur as a result of certain policies, such as ESOP plans. We find that <strong>the</strong>se changes do not drive<br />
our results.<br />
7 Berkshire Hathaway is a notable example of a firm that does not appear <strong>to</strong> engage in TSM. The size of Berkshire Hathaway’s<br />
earnings target is small relative <strong>to</strong> <strong>the</strong> size of <strong>the</strong> firm’s earnings. They must realize earnings within ±0.00005% of <strong>the</strong> consensus<br />
forecasts <strong>to</strong> meet expectations.<br />
8 Evidence of this endogeneity can be seen in Dechow and You (2012). They document that <strong>the</strong> market reaction <strong>to</strong> <strong>EPS</strong><br />
surprises is weaker for firms with higher <strong>EPS</strong> levels which, holding earnings fixed, is equivalent <strong>to</strong> firms with lower shares<br />
outstanding.<br />
4
targets.<br />
<strong>Managers</strong> change <strong>the</strong> target size in response <strong>to</strong> changes in <strong>the</strong> predictability of those earnings.<br />
Importantly, <strong>the</strong>se effects are stronger for firms with higher incentive compensation, weaker for firms with<br />
low liquidity.<br />
Finally, following an increase in <strong>the</strong> target size, firms meet forecasts more frequently and<br />
earnings management drops.<br />
Our paper is related <strong>to</strong>, but distinct from, <strong>the</strong> broad literature on earnings management. Prior evidence<br />
suggests that earnings management occurs when managers face short term incentives <strong>to</strong> meet or beat a<br />
threshold.<br />
The manager privately observes <strong>the</strong> firm’s earnings, and chooses accruals, investment, s<strong>to</strong>ck<br />
repurchases, or some o<strong>the</strong>r corporate action such that <strong>the</strong> firm’s reported earnings meet <strong>the</strong> threshold. In<br />
contrast, our evidence suggests that managers manage <strong>the</strong> target size not <strong>to</strong> affect <strong>the</strong> current period <strong>EPS</strong>,<br />
but <strong>to</strong> affect <strong>the</strong> ease with which <strong>the</strong> firm will meet future <strong>EPS</strong> thresholds in <strong>the</strong> long run.<br />
No private<br />
information is required by <strong>the</strong> manager for TSM <strong>to</strong> be effective, and markets need not be fooled. TSM<br />
and earnings management are related, however, in <strong>the</strong> sense that TSM is a long-term substitute for earnings<br />
management. By setting <strong>the</strong> target size <strong>to</strong>day, <strong>the</strong> manager is effectively determining <strong>the</strong> amount of earnings<br />
that will need <strong>to</strong> be managed in expectation over multiple periods in <strong>the</strong> future. 9<br />
Our findings contribute most directly <strong>to</strong> <strong>the</strong> literature on <strong>the</strong> choice of earnings management <strong>to</strong>ols. For<br />
example, recent literature focuses on <strong>the</strong> tradeoffs between earnings management <strong>to</strong>ols (e.g.<br />
Cohen and<br />
Zarowin (2010) and Zang (2011)). As noted by Fields et al. (2001), it is important <strong>to</strong> examine <strong>the</strong> combined,<br />
net effect of all earnings management <strong>to</strong>ols used <strong>to</strong>ge<strong>the</strong>r <strong>to</strong> meet <strong>EPS</strong> thresholds. Our results are important<br />
because <strong>the</strong>y suggest that, prior <strong>to</strong> trading off <strong>the</strong>se earnings management <strong>to</strong>ols, managers decide <strong>the</strong> extent<br />
<strong>to</strong> which <strong>the</strong>y will need <strong>to</strong> manage earnings in <strong>the</strong> first place.<br />
Our study highlights an important link between <strong>EPS</strong> reporting and capital market activities through<br />
<strong>the</strong> real effects of s<strong>to</strong>ck splits. Our evidence offers a new explanation for s<strong>to</strong>cks splits <strong>based</strong> on <strong>the</strong> need<br />
for target size management. While previous explanations typically involve signaling motives or s<strong>to</strong>ck price<br />
levels, we show that s<strong>to</strong>ck splits could be a result of managerial concerns regarding <strong>EPS</strong> outcomes. Thus,<br />
we extend <strong>the</strong> prior literature that examines patterns in accounting metrics and <strong>the</strong>ir relationship <strong>to</strong> s<strong>to</strong>ck<br />
splits (e.g. Louis and Robinson (2005)). Fur<strong>the</strong>rmore, a TSM-<strong>based</strong> explanation of s<strong>to</strong>ck splits is consistent<br />
with prior literature that finds that splits follow earnings growth (Lakonishok and Lev (1987), Asquith et al.<br />
(1989)), as well as <strong>the</strong> literature that documents a “nominal price puzzle”(Weld et al. (2009)). We discuss<br />
this in more detail in Section 3.3.<br />
9 Prior literature finds that firms use repurchases (which result in a change <strong>to</strong> <strong>the</strong> quantity of shares) <strong>to</strong> have an accretive<br />
effect on current period <strong>EPS</strong> (e.g. Hribar et al. (2006) and Bens et al. (2003)). Our results do not dispute <strong>the</strong>se findings, but<br />
ra<strong>the</strong>r show that share changes can have long term effects on <strong>EPS</strong> outcomes. TSM is driven primarily through s<strong>to</strong>ck splits and<br />
not through repurchases. We find little evidence that s<strong>to</strong>ck splits have an accretive effect on <strong>EPS</strong> in <strong>the</strong> short run.<br />
5
Finally, TSM has implications for a variety of per-share metrics such as analyst dispersion and forecast<br />
error.<br />
In this sense, our findings compliment Dechow and You (2012), in which <strong>the</strong> authors make <strong>the</strong><br />
observation that <strong>the</strong> precision of an <strong>EPS</strong> number is greater for higher levels of <strong>EPS</strong>. 10 We show in Section<br />
3.3 that <strong>the</strong> scale invariance of analysts’ forecast errors (Degeorge et al. (1999), Cheong and Thomas (2011),<br />
and Ball (2011)) is <strong>the</strong> expected endogenous outcome of target size management.<br />
Our paper proceeds as follows: Section 2 motivates our hypo<strong>the</strong>sis and describes <strong>the</strong> mechanism we test.<br />
Section 3 describes <strong>the</strong> data and empirical results. Section 3.3 discusses <strong>the</strong> implications of our findings, and<br />
Section 4 concludes.<br />
2 Discussion and Hypo<strong>the</strong>sis Development<br />
The convention of rounding <strong>EPS</strong> <strong>to</strong> <strong>the</strong> nearest penny creates a range of net income that will generate a<br />
given <strong>EPS</strong> number. The size of this range is determined by <strong>the</strong> number of shares outstanding. Specifically,<br />
<strong>the</strong> range of net income that meets expectations is: (E[EP S] ∗ s −<br />
s<br />
s<br />
200<br />
, E[EP S] ∗ s +<br />
200<br />
), where E[EP S]<br />
is <strong>the</strong> analysts’ <strong>EPS</strong> expectation and s is <strong>the</strong> number of shares outstanding. The expected Net Income,<br />
E[EP S] ∗ s, is <strong>the</strong> <strong>to</strong>tal earnings implied by <strong>the</strong> per share forecast and is <strong>the</strong> midpoint of this range. The<br />
highest and lowest earnings that will round <strong>to</strong> <strong>the</strong> forecast are determined by s. At a maximum, each share’s<br />
1<br />
worth of earnings will be rounded by half a penny (or in dollar terms,<br />
200<br />
). For example, Microsoft Corp.<br />
has roughly 8 billion shares outstanding. So, in any given quarter <strong>the</strong> <strong>to</strong>tal size of <strong>the</strong>ir earnings target is 80<br />
million dollars, ± 40 million centered around <strong>the</strong> amount of <strong>to</strong>tal earnings implied by <strong>the</strong> forecast. In dollar<br />
terms this amount might seem large, but relative <strong>to</strong> <strong>the</strong> magnitude of <strong>the</strong> firm’s earnings, perhaps less so.<br />
The size of <strong>the</strong> earnings target relative <strong>to</strong> <strong>the</strong> size of <strong>the</strong> firm’s <strong>to</strong>tal earnings is ± 0.5<br />
E[|EP S|]<br />
%. The average<br />
firm in our sample has <strong>EPS</strong> of $0.20.<br />
So, <strong>the</strong> typical firm will meet <strong>the</strong> earnings forecast by producing<br />
earnings within ±2.50% of expected earnings. This amount of flexibility might be considered large by some<br />
managers and small by o<strong>the</strong>rs. For example, 2.50% may be relatively large for a firm with stable business<br />
fundamentals and predictable net income. <strong>How</strong>ever, a manager whose compensation is highly concave in<br />
earnings surprises may consider this range <strong>to</strong> be small.<br />
<strong>Managers</strong> have flexibility over <strong>the</strong> size of this earnings target. In dollar terms, <strong>the</strong> size of <strong>the</strong> target is<br />
fixed solely by <strong>the</strong> number of shares. If <strong>the</strong> manager prefers an earnings target twice as large, she can simply<br />
double <strong>the</strong> number of shares outstanding. Because <strong>the</strong> size of <strong>the</strong> earnings target measured in dollars is fixed,<br />
10 In <strong>the</strong> next section, we show that <strong>the</strong> target size as a percentage of <strong>the</strong> firm’s expected net income equals one-half of <strong>the</strong><br />
inverse of <strong>EPS</strong>.<br />
6
it does not increase as <strong>the</strong> firm’s earnings increase. Equivalently, <strong>the</strong> size of <strong>the</strong> earnings target measured<br />
as a percent of <strong>the</strong> firm’s earnings shrinks as <strong>the</strong> firm’s earnings grow. The manager can counteract this by<br />
adjusting shares outstanding. An example that highlights <strong>the</strong>se effects is shown in Figure 1.<br />
[Insert Figure 1 Here]<br />
Our testable predictions focus on <strong>the</strong> manager’s choice for shares outstanding. First, we discuss predictions<br />
on <strong>the</strong> firm and manager characteristics that are related <strong>to</strong> <strong>the</strong> cross sectional distribution of shares<br />
outstanding. We discuss an identification strategy <strong>to</strong> address causality - that managers’ <strong>EPS</strong>-<strong>based</strong> incentives<br />
cause <strong>the</strong>m <strong>to</strong> choose shares outstanding. Last, we explore <strong>the</strong> conditions under which managers change<br />
shares outstanding, how <strong>the</strong>se changes relate <strong>to</strong> <strong>EPS</strong> outcomes, and how <strong>the</strong>y relate <strong>to</strong> <strong>the</strong> usage of o<strong>the</strong>r<br />
earnings management <strong>to</strong>ols.<br />
2.1 Determinants of <strong>the</strong> cross sectional distribution of shares outstanding<br />
We expect <strong>the</strong> manager’s choice of target size <strong>to</strong> be a function of <strong>the</strong> incentives she faces <strong>to</strong> generate certain<br />
<strong>EPS</strong> outcomes. Conceptually, <strong>the</strong>se incentives can be summarized by <strong>the</strong> set of payoffs <strong>the</strong> manager receives<br />
for generating certain <strong>EPS</strong> outcomes, and <strong>the</strong> probabilities that <strong>the</strong>se outcomes occur. Nei<strong>the</strong>r payoffs nor<br />
probabilities associated with a specific earnings realization can be directly measured.<br />
Fur<strong>the</strong>r, both are<br />
likely endogenously determined along with <strong>the</strong> manager’s choice for shares outstanding. This makes both<br />
hypo<strong>the</strong>sis development and empirical design challenging. We begin by assuming probabilities and payoffs<br />
are exogenous and measurable.<br />
First, we hold payoffs fixed (e.g., managers receive <strong>the</strong> same bonus for beating <strong>EPS</strong> forecasts, <strong>the</strong> market<br />
response <strong>to</strong> a negative earnings surprise is <strong>the</strong> same across firms, managerial ownership is constant, etc.)<br />
and examine how variation in probabilities should relate <strong>to</strong> variation in <strong>the</strong> number of shares. For any firm,<br />
<strong>the</strong> probability of meeting <strong>EPS</strong> forecasts is:<br />
P r(meet) = P r(µ −<br />
∫ s µ+ s<br />
200 ≤ x < µ + s<br />
200 ) = 200<br />
µ− s<br />
200<br />
f(x) dx,<br />
where f(x) is <strong>the</strong> pdf of <strong>the</strong> firm’s earnings, µ is analysts’ forecasted earnings (which equals s ∗ E[EP S]),<br />
and s is <strong>the</strong> number of shares.<br />
If we assume <strong>the</strong> firm has earnings distributed uniformly over [-e, e] and <strong>the</strong> consensus forecast is nei<strong>the</strong>r<br />
noisy nor biased (and <strong>the</strong>refore equals $0.00), <strong>the</strong>n <strong>the</strong> probability of meeting earnings is: P r(meet) =<br />
∫ s<br />
200<br />
−<br />
s<br />
200<br />
( 1<br />
e+e ) dx =<br />
s<br />
200e<br />
. From here it is easy <strong>to</strong> see that <strong>the</strong> probability of meeting forecasts is negatively<br />
7
elated <strong>to</strong> <strong>the</strong> variance (variance is e2<br />
12<br />
) of <strong>the</strong> earnings and positively related <strong>to</strong> s. If payoffs are fixed and<br />
homogenous across managers, <strong>the</strong>n all managers will prefer <strong>the</strong> same probabilities of meeting, beating, and<br />
missing <strong>EPS</strong> forecasts. Holding <strong>the</strong>se payoffs constant, it follows directly that managers of firms with volatile<br />
earnings will need <strong>to</strong> choose higher shares in order <strong>to</strong> obtain <strong>the</strong> same <strong>EPS</strong> outcome likelihoods. This positive<br />
relation between net income volatility and shares outstanding is our main prediction:<br />
H1: <strong>Managers</strong> of firms with highly volatile and unpredictable earnings will choose more shares outstanding<br />
compared <strong>to</strong> firms with stable, predictable earnings, all else equal.<br />
This prediction is difficult <strong>to</strong> test empirically for a variety of reasons. First, forward-looking volatility<br />
is not observable.<br />
Second, <strong>the</strong> volatility of earnings that is important for our purposes is <strong>the</strong> part that<br />
is unpredictable. More precisely, <strong>the</strong> variance that is important is <strong>the</strong> variance in <strong>the</strong> difference between<br />
realized earnings and expected earnings.<br />
For example, if a firm has volatile earnings due <strong>to</strong> predictable<br />
seasonal variation, <strong>the</strong>n this volatility would not reflect <strong>the</strong> likelihood that <strong>the</strong> firm will generate earnings<br />
different from forecasts. Third, as pointed out in <strong>the</strong> large literature on earnings smoothing (e.g. Beidleman<br />
(1973), Subramanyam (1996), Healy and Wahlen (1999)), <strong>the</strong> variance in earnings is itself a choice variable.<br />
To address <strong>the</strong> first two concerns, we use three proxies for net income volatility; i) variance around <strong>the</strong><br />
mean over <strong>the</strong> last twelve quarters, ii) variance around a seasonally adjusted expected mean over <strong>the</strong> last<br />
twelve quarters, and iii) variance around <strong>the</strong> expectation implied by analysts’ forecasts over <strong>the</strong> last twelve<br />
quarters.<br />
We expect <strong>to</strong> find a positive relationship between <strong>the</strong>se measures of net income volatility and<br />
shares outstanding.<br />
The last concern, that net income volatility is jointly determined with <strong>the</strong> number of shares, makes identification<br />
difficult. To address causality, we use a source of plausibly exogenous variation in <strong>the</strong> probability<br />
that <strong>the</strong> firm meets <strong>EPS</strong> forecasts and relate this <strong>to</strong> changes in shares outstanding. Specifically, we use an<br />
exogenous drop in analyst coverage as a shock <strong>to</strong> <strong>the</strong> probability that <strong>the</strong> firm meets earnings forecasts. Our<br />
reasoning is simple, if <strong>the</strong> consensus forecast is thought of as <strong>the</strong> sample mean (or median) of individual<br />
analysts’ noisy forecasts, <strong>the</strong>n <strong>the</strong> variance of this estimate is decreasing in <strong>the</strong> number of analysts, i.e.<br />
<strong>the</strong> noise in <strong>the</strong> forecast is a decreasing function of <strong>the</strong> sample size. Therefore, a drop in analyst coverage<br />
increases <strong>the</strong> variance in <strong>the</strong> <strong>EPS</strong> forecast simply because fewer analysts are sampled.<br />
Increasing <strong>the</strong> volatility of <strong>the</strong> forecast is equivalent <strong>to</strong> increasing <strong>the</strong> volatility of earnings around <strong>the</strong><br />
forecast. In <strong>the</strong> Appendix, we show explicitly that an increase in forecast noise decreases <strong>the</strong> probability of<br />
8
meeting that forecast. This leads <strong>to</strong> a variant of our main hypo<strong>the</strong>sis:<br />
H1a: <strong>Managers</strong> increase shares in response <strong>to</strong> an exogenous decrease in analyst coverage.<br />
Next, we discuss how manager payoffs might relate <strong>to</strong> variation in shares outstanding. All else equal,<br />
we expect a positive relationship between <strong>the</strong> sensitivity of payoffs <strong>to</strong> negative earnings surprises relative<br />
<strong>to</strong> positive surprises (concavity) and shares outstanding. The more shares are outstanding, <strong>the</strong> lower is <strong>the</strong><br />
probability of missing earnings. <strong>How</strong>ever, because this rounding effect is symmetric, it also decreases <strong>the</strong><br />
probability of beating earnings. A manager with convex payoffs (higher sensitivity <strong>to</strong> meeting than missing)<br />
should prefer a small range. In this case, <strong>the</strong> probability of missing is high, but <strong>the</strong> probability of beating<br />
is high as well. A manager who incurs large costs when missing relative <strong>to</strong> beating (concave payoffs) will<br />
prefer a larger range <strong>to</strong> minimize <strong>the</strong> chances of incurring those costs.<br />
H2: <strong>Managers</strong> with payoffs that are concave (convex) in earnings surprises will choose higher (lower) level<br />
of shares outstanding.<br />
Similar <strong>to</strong> net income volatility, payoffs are nei<strong>the</strong>r observable nor exogenous. <strong>How</strong>ever, <strong>the</strong>re is considerable<br />
evidence that CEO’s receive compensation that is concave in earnings surprises. Bonuses in CEO<br />
compensation contracts are often tied <strong>to</strong> <strong>EPS</strong> thresholds <strong>based</strong> on analyst forecasts (Murphy (1999), De Angelis<br />
and Grinstein (2011) and Kim and Yang (2012)). Also, <strong>the</strong> negative s<strong>to</strong>ck price reactions <strong>to</strong> negative<br />
earnings surprises are significantly larger than <strong>the</strong> positive reactions associated with beating forecasts. 11<br />
Given that most CEOs have substantial ownership stakes in <strong>the</strong> company, this creates a stronger incentive<br />
<strong>to</strong> avoid missing earnings expectations compared <strong>to</strong> <strong>the</strong> incentive <strong>to</strong> beat those targets. Burgstahler and<br />
Dichev (1997) and Degeorge et al. (1999) show empirically that <strong>the</strong> distribution of <strong>EPS</strong> outcomes is consistent<br />
with <strong>the</strong> view that managers respond <strong>to</strong> incentives <strong>to</strong> meet or beat <strong>EPS</strong> targets. Fur<strong>the</strong>rmore, prior<br />
literature has documented a connection between <strong>EPS</strong> outcomes and managerial compensation. For example,<br />
Cheng and Warfield (2005) find that managers with high equity ownership are less likely <strong>to</strong> miss <strong>EPS</strong> targets.<br />
We expect managers with larger bonuses tied <strong>to</strong> accounting targets <strong>to</strong> have more shares outstanding, and<br />
hence wider rounding ranges. We would also expect managers who have more ownership and more equity<br />
11 Payne and Thomas (2003) and Skinner and Sloan (2002) show differences in <strong>the</strong> source of this effect, but both generally<br />
find stronger negative reactions.<br />
9
ased compensation <strong>to</strong> have similar incentives. The amount of incentive compensation as a percent of <strong>to</strong>tal<br />
compensation captures both of <strong>the</strong>se effects. Consequently, <strong>the</strong> percentage of incentive compensation will be<br />
positively related <strong>to</strong> <strong>the</strong> number of shares outstanding.<br />
Because compensation contracts are endogenous, we again utilize <strong>the</strong> exogenous drop in analyst coverage<br />
<strong>to</strong> empirically test a variant of H2:<br />
H2a: The effect of an exogenous drop in analyst coverage should be stronger (weaker) among firms whose<br />
managers have high (low) incentive compensation.<br />
2.1.1 Additional costs and benefits relating <strong>to</strong> shares outstanding<br />
Discussion so far has focused on benefits and costs of shares outstanding as <strong>the</strong>y relate <strong>to</strong> <strong>the</strong> rounding<br />
effects and <strong>EPS</strong>-<strong>based</strong> incentives. If <strong>the</strong>se were <strong>the</strong> only trade-offs faced by managers, <strong>the</strong>n any manager<br />
with concave payoffs should choose infinite shares outstanding. We do not observe this because <strong>the</strong>re are<br />
o<strong>the</strong>r costs and benefits related <strong>to</strong> shares outstanding. Prior literature has shown that s<strong>to</strong>ck liquidity is a<br />
function of per-share price levels. In <strong>the</strong> extreme, if <strong>the</strong> price is <strong>to</strong>o low <strong>the</strong> s<strong>to</strong>ck is de-listed, which severely<br />
inhibits liquidity. Therefore, we expect that <strong>the</strong> relationships described in H1 and H2 <strong>to</strong> be weaker for illiquid<br />
firms or those close <strong>to</strong> delisting. In this case, market microstructure considerations are likely <strong>to</strong> outweigh<br />
<strong>EPS</strong>-<strong>based</strong> incentives when <strong>the</strong> manager is choosing shares outstanding.<br />
H3: <strong>Managers</strong> will increase shares as a response <strong>to</strong> an exogenous decrease in analyst coverage, but only for<br />
liquid firms.<br />
Similarly, some corporate decisions are made for reasons not primarily related <strong>to</strong> shares outstanding, yet<br />
<strong>the</strong>se decisions result in a change in shares. For example, firms often repurchase or issue s<strong>to</strong>ck. While <strong>the</strong>se<br />
actions change <strong>the</strong> number of shares, this change is a byproduct, not <strong>the</strong> goal of <strong>the</strong> decision. We do not<br />
expect our hypo<strong>the</strong>ses <strong>to</strong> hold for changes in shares that result from repurchases or issuances. We expect our<br />
results <strong>to</strong> be driven primarily by s<strong>to</strong>ck splits, which do not result in changes <strong>to</strong> <strong>the</strong> firms capital structure.<br />
H4: Changes <strong>to</strong> shares outstanding as a response <strong>to</strong> an exogenous decrease in analyst coverage are driven<br />
by s<strong>to</strong>ck splits.<br />
10
2.2 Time series determinants of shares outstanding<br />
In this section, we examine <strong>the</strong> conditions under which managers might choose <strong>to</strong> change shares outstanding.<br />
In <strong>the</strong> previous section, we discuss how <strong>the</strong> level of shares should be related <strong>to</strong> earnings volatility and <strong>the</strong><br />
concavity of payoffs. If one of <strong>the</strong>se cross sectional determinants were <strong>to</strong> change, <strong>the</strong>n we would expect <strong>the</strong><br />
manager <strong>to</strong> correspondingly change shares outstanding and, in fact, we use a shock <strong>to</strong> net income volatility<br />
(relative <strong>to</strong> forecasts) <strong>to</strong> address causality. <strong>How</strong>ever, we expect that much of <strong>the</strong> within-firm variation in<br />
shares is driven not by changes in compensation contracts or analyst coverage, but simply by firm growth.<br />
Dechow and You (2012) make <strong>the</strong> observation that <strong>the</strong> precision of an <strong>EPS</strong> number is increasing in <strong>the</strong><br />
level of <strong>EPS</strong>. We offer one way <strong>to</strong> quantify this effect; - <strong>the</strong> firm needs <strong>to</strong> produce net income within ± 0.5<br />
E[|EP S|]<br />
% of expected net income <strong>to</strong> meet expectations. Therefore as <strong>the</strong> firm’s net income grows, <strong>the</strong> target size as<br />
a fraction of <strong>the</strong> firm’s expected net income shrinks. 12<br />
It is well known that managers increase shares following earnings growth (see e.g.<br />
Lakonishok and<br />
Lev (1987) and Asquith et al. (1989)). We examine a conditional hypo<strong>the</strong>sis that is unique <strong>to</strong> target size<br />
management. This helps distinguish TSM from o<strong>the</strong>r explanations that also predict an increase in shares<br />
following earnings growth.<br />
The relationship between earnings growth and target size is non-mono<strong>to</strong>nic, with a kink at <strong>EPS</strong>=0.<br />
Earnings growth shrinks <strong>the</strong> target size, but only for firms with positive earnings. If <strong>the</strong> firm has negative<br />
earnings and experiences earnings growth (a positive change in earnings), <strong>the</strong>n this growth actually widens<br />
<strong>the</strong> range making it easier <strong>to</strong> meet expectations, not harder. Therefore, we expect increases in shares <strong>to</strong><br />
follow earnings growth, but only among positive <strong>EPS</strong> firms.<br />
H5: <strong>Managers</strong> increase shares following earnings growth, but only for firms with positive earnings.<br />
A manager can compensate for a shrinking target by using more accruals, guidance, and o<strong>the</strong>r earnings<br />
management <strong>to</strong>ols. <strong>How</strong>ever, usage of <strong>the</strong>se earnings management <strong>to</strong>ols is costly. As <strong>the</strong> costs of <strong>the</strong> usage<br />
of <strong>the</strong>se alternatives increase, <strong>the</strong> manager can choose <strong>to</strong> “reset” <strong>the</strong> size of <strong>the</strong> earnings target, res<strong>to</strong>ring<br />
it <strong>to</strong> a size appropriate for <strong>the</strong> now-larger firm. Therefore, we expect that <strong>the</strong> manager will ei<strong>the</strong>r meet<br />
12 To be clear, if <strong>the</strong> firm’s mean earnings grows but <strong>the</strong>re is no growth in variance, <strong>the</strong>n this growth has no effect on <strong>the</strong><br />
probability of meeting forecasts, despite <strong>the</strong> fact that <strong>the</strong> target size relative <strong>to</strong> firm size has shrunk. Therefore, thinking of<br />
target size relative <strong>to</strong> firm size is useful only if <strong>the</strong> size of <strong>the</strong> firm in terms of expected net income is related <strong>to</strong> <strong>the</strong> volatility<br />
of <strong>the</strong> firm’s net income. Not surprisingly, we find empirically that earnings growth is associated with higher levels of earnings<br />
volatility going forward.<br />
11
<strong>EPS</strong> forecasts more frequently or will use less earnings management (or both) following an increase in shares<br />
outstanding.<br />
H6: The likelihood of meeting (missing or beating) <strong>EPS</strong> forecasts increases (decreases) following increases<br />
in shares.<br />
H7: The usage of accounting and real earnings management <strong>to</strong>ols decreases following increases in shares.<br />
2.3 Short-term rounding effects<br />
Discussion up <strong>to</strong> this point has focused on <strong>the</strong> long-run effects of shares on <strong>the</strong> size of <strong>the</strong> earnings target.<br />
Given that <strong>the</strong> number of shares persists from quarter-<strong>to</strong>-quarter, we expect managers <strong>to</strong> choose shares in<br />
response <strong>to</strong> long horizon trade-offs and expectations. <strong>How</strong>ever, it is possible that managers ignore long term<br />
effects and adjust shares outstanding in light of private information regarding current period earnings. To<br />
<strong>the</strong> best of our knowledge, reported earnings must reflect splits that occur during <strong>the</strong> period between <strong>the</strong><br />
fiscal quarter end and actual earnings report date. Therefore, it is possible that managers adjust shares in<br />
order <strong>to</strong> affect current period <strong>EPS</strong> outcomes. Prior evidence suggests that managers use s<strong>to</strong>ck repurchases<br />
<strong>to</strong> affect current period <strong>EPS</strong> outcomes (Bens et al. (2003) and Hribar et al. (2006)).<br />
If managers observe that current period earnings are lower than expectations, <strong>the</strong>y may choose <strong>to</strong> increase<br />
<strong>the</strong> target size such that <strong>the</strong>y meet (<strong>the</strong> split adjusted) <strong>EPS</strong> expectation. This seems unlikely for a few<br />
reasons. First, we do not observe managers rebalancing shares each quarter - if a firm splits in one quarter<br />
for short-term reasons, <strong>the</strong> firm would prefer <strong>to</strong> reverse split in <strong>the</strong> next quarter <strong>to</strong> return <strong>to</strong> <strong>the</strong> optimal<br />
target size. More importantly, <strong>the</strong>re is a well established positive market reaction <strong>to</strong> s<strong>to</strong>ck splits. This<br />
evidence is not consistent with managers splitting because of negative temporary earnings shocks.<br />
<strong>How</strong>ever, <strong>the</strong>re may be scope for short term considerations <strong>to</strong> affect not whe<strong>the</strong>r <strong>the</strong> firm should split, but<br />
by how much. For example, perhaps <strong>the</strong> manager has determined that <strong>the</strong> firm needs <strong>to</strong> roughly double <strong>the</strong><br />
number of shares. The manager might choose a 7-for-3 split instead of a 2-for-1 split, so that <strong>the</strong> change has<br />
an accretive effect on current period <strong>EPS</strong>. 13 We hypo<strong>the</strong>size that if managers choose split ratios out of short<br />
term considerations, <strong>the</strong>n we should observe atypical ratios more frequently in <strong>the</strong> period after earnings are<br />
13 An example of an accretive split is <strong>the</strong> following: The manager observes current period net income <strong>to</strong> be $15.4. The firm<br />
has 100 shares outstanding, and analysts’ forecasted <strong>EPS</strong> is 0.15. If <strong>the</strong> manager issues a 7-for-3 split, split-adjusted expectation<br />
is 0.06. <strong>How</strong>ever, <strong>the</strong> manager will report split-adjusted <strong>EPS</strong> as 0.07.<br />
12
ealized but before <strong>the</strong>y are reported. We also expect that <strong>the</strong>se splits should more frequently be accretive<br />
than dilutive.<br />
3 Data and Results<br />
3.1 Data<br />
The sample analyzed in this study is compiled from four major databases.<br />
The primary data sample is<br />
ga<strong>the</strong>red from <strong>the</strong> quarterly CRSP/COMPUSTAT Merged database and combined with analyst forecast<br />
data obtained from I/B/E/S. Our sample starts in 1984 since we require 12 previous quarters of analyst<br />
forecasts in our main tests. Our sample ends in 2011. We include s<strong>to</strong>ck return data from CRSP. Only common<br />
s<strong>to</strong>ck with CRSP share code 10 or 11 are included. We merge in institutional ownership obtained from <strong>the</strong><br />
Thomson Reuters 13(f) institutional holdings database. For a subset of tests, we include compensation data<br />
from ExecuComp.<br />
To distinguish between changes in shares outstanding due <strong>to</strong> s<strong>to</strong>ck splits, repurchases, or equity issuances,<br />
we use distribution codes from CRSP. S<strong>to</strong>ck splits have a distribution code equal <strong>to</strong> 5523. In our sample,<br />
we assign a split <strong>to</strong> a fiscal quarter if <strong>the</strong> CRSP payment date (PAYDT) occurs after <strong>the</strong> prior earnings<br />
report date, but before <strong>the</strong> earnings report date as reported in COMPUSTAT. If <strong>the</strong> earnings report date is<br />
missing, a split is assigned <strong>to</strong> a fiscal quarter if it occurs within <strong>the</strong> fiscal quarter begin and end dates.<br />
A key prediction in our study centers on <strong>the</strong> link between shares outstanding and <strong>the</strong> volatility of earnings.<br />
We create three measures of earnings volatility. Net Income Volatility is calculated as <strong>the</strong> standard deviation<br />
of net income over <strong>the</strong> past 12 quarters.<br />
This directly measures <strong>the</strong> variance in net income, however it<br />
does not capture predictable, seasonal net income variation. Net Income Volatility - Naive Forecast is <strong>the</strong><br />
standard deviation of seasonally adjusted net income over <strong>the</strong> past 12 quarters. This proxy captures <strong>the</strong><br />
variance around a time-varying mean using a simple forecast for <strong>the</strong> mean <strong>based</strong> on seasonality and prior<br />
growth in net income. Net Income Volatility - Analysts Forecast is calculated as <strong>the</strong> standard deviation of<br />
(Net Income - median IBES forecasted earnings) over <strong>the</strong> past 12 quarters, where median IBES forecasted<br />
earnings is <strong>the</strong> median <strong>EPS</strong> forecast multiplied by shares outstanding. The benefit of this measure is that it<br />
captures actual earnings expectations in each period. <strong>How</strong>ever, <strong>the</strong> drawback is that it requires data from<br />
IBES which reduces <strong>the</strong> sample.<br />
[Insert Table 1 Here]<br />
13
Table 1 presents <strong>the</strong> summary statistics of <strong>the</strong> sample. The key dependent variable used in this study is<br />
shares outstanding (median = 23.55 million, mean = 83.85 million). <strong>EPS</strong> has a median of $0.19 and mean<br />
of $0.20. This translates <strong>to</strong> a median and mean earnings target size of ±2.6% and ±2.5% of expected net<br />
income.<br />
3.2 Results<br />
We begin by examining if data are consistent with <strong>the</strong> view that managers recognize <strong>the</strong> effects of rounding<br />
and <strong>the</strong> earnings target size, and in particular <strong>the</strong> lower bound of earnings required <strong>to</strong> meet forecasts.<br />
Evidence in prior literature is consistent with this.<br />
For example, Das and Zhang (2003) document an<br />
abnormally large number of net income realizations that round upwards when translating net income <strong>to</strong><br />
<strong>EPS</strong>. Given this evidence, we expect that an abnormal number of net income realizations will be just above<br />
<strong>the</strong> minimum that will round <strong>to</strong> <strong>the</strong> <strong>EPS</strong> forecast.<br />
We present a figure that is similar in spirit <strong>to</strong> analyses presented in Burgstahler and Dichev (1997)<br />
and Degeorge et al. (1999), who find an abnormal number of <strong>EPS</strong> outcomes that are just enough <strong>to</strong> clear<br />
certain thresholds. Instead of examining <strong>EPS</strong> outcomes, we plot net income realizations around <strong>the</strong> threshold<br />
E[EP S] ∗ s −<br />
s<br />
200<br />
, which is <strong>the</strong> minimum net income required <strong>to</strong> meet <strong>the</strong> median analyst <strong>EPS</strong> forecast.<br />
We scale each firm’s realized net income by E[EP S] ∗ s − s<br />
200<br />
and plot frequencies in Figure 2. Any value<br />
< 1 means <strong>the</strong> firm missed <strong>the</strong> <strong>EPS</strong> forecast, and a value of 1 indicates that <strong>the</strong> firm reported just enough<br />
net income such that it rounds <strong>to</strong> <strong>the</strong> <strong>EPS</strong> forecast.<br />
[Insert Figure 2 Here]<br />
The red line (left line) in <strong>the</strong> figure indicates <strong>the</strong> minimum net income that meets forecasts - <strong>the</strong> lower<br />
bound of <strong>the</strong> target size. The green line (right line) indicates, for <strong>the</strong> average firm, <strong>the</strong> net income implied by<br />
analysts’ forecasts (E[EP S] ∗ s). The figure shows a disproportionate occurrence of net income realizations<br />
that are just enough <strong>to</strong> meet <strong>the</strong> minimum net income required <strong>to</strong> satisfy <strong>the</strong> <strong>EPS</strong> forecast.<br />
In what follows, we examine if managers recognize that <strong>the</strong> location of this threshold is a choice variable<br />
and choose <strong>the</strong> number of shares accordingly.<br />
Our main hypo<strong>the</strong>sis is that managers of firms with<br />
unpredictable net income will choose high levels of shares outstanding so that a wide range of net income<br />
realizations will meet forecasts. We also expect that managers with high incentive compensation will choose<br />
more shares outstanding for similar reasons. We briefly examine <strong>the</strong>se relationships using multivariate sorts.<br />
Figure 3 presents <strong>the</strong> average median shares outstanding across deciles of net income volatility in Panel<br />
14
A and incentive compensation in Panel B. We present medians <strong>to</strong> alleviate concerns of extreme outliers. 14 In<br />
each quarter, we first sort <strong>the</strong> sample in<strong>to</strong> 20 groups <strong>based</strong> on net income, <strong>the</strong>n within each net income group<br />
we sort in<strong>to</strong> deciles <strong>based</strong> on net income volatility or incentive compensation. This allows us <strong>to</strong> compare<br />
firms with roughly equivalent net income. We plot median shares (bar height) across net income deciles. We<br />
also report median net income (line) <strong>to</strong> confirm that we are comparing firms of similar size.<br />
[Insert Figure 3 Here]<br />
We find a strong association between shares outstanding and both net income volatility and incentive<br />
compensation. Shares outstanding mono<strong>to</strong>nically increases across net income volatility deciles. We also<br />
observe a positive trend in shares outstanding across incentive compensation deciles, although <strong>the</strong> pattern<br />
is weaker. In both figures, <strong>the</strong> average net income (line-plot) is stable across <strong>the</strong> decile ranks. 15<br />
While <strong>the</strong><br />
extreme deciles have similar net income, <strong>the</strong> <strong>to</strong>p net income volatility decile has three times as many shares<br />
outstanding (in thousands) than its bot<strong>to</strong>m decile counterpart (33,162 vs. 10,037, p-value < 0.01). In Panel<br />
B, <strong>the</strong> <strong>to</strong>p incentive compensation decile has nearly 40% more shares outstanding than <strong>the</strong> bot<strong>to</strong>m decile<br />
(49,774 vs. 70,898, p-value < 0.01).<br />
3.2.1 Regression Analysis<br />
Results from <strong>the</strong> dependent sorts indicate that firms with similar mean net income but different variance<br />
have drastically different shares outstanding. In this section, we examine cross sectional variation in shares<br />
outstanding in more detail.<br />
Table 2 presents pooled OLS regression models of shares outstanding as a function of firm characteristics.<br />
These results are suggestive of <strong>the</strong> cross sectional determinants of <strong>the</strong> level of shares outstanding. Regression<br />
coefficients are standardized <strong>to</strong> represent standard deviation effects in shares outstanding for a one standard<br />
deviation difference in a given covariate. All determinants of shares outstanding are lagged one period. Column<br />
1 presents a basic specification, including variables representing size (Market Cap), liquidity (Amihud),<br />
and ownership (Percent Institutional Ownership). These determinants have previously been associated with<br />
s<strong>to</strong>ck splits and, as such, we expect <strong>the</strong>m <strong>to</strong> be related <strong>to</strong> <strong>the</strong> level of shares outstanding. This specification<br />
includes a proxy for earnings volatility, Net Income Volatility t−1 , defined as <strong>the</strong> standard deviation of Net<br />
Income over <strong>the</strong> last twelve quarters. These results are robust <strong>to</strong> using various income definitions including<br />
Operating Income Before Depreciation as well as Income Before Extraordinary Items.<br />
14 The patterns in both figures are stronger using averages.<br />
15 The higher level of average net income in Panel B reflects <strong>the</strong> fact that <strong>the</strong> ExecuComp sample of firms are larger.<br />
15
Column 2 presents <strong>the</strong> same specification as column 1, but uses an earnings volatility proxy adjusted<br />
for expectations <strong>based</strong> on prior earnings. Specifically, Net Income Volatility - Naive Forecast t−1 is measured<br />
as <strong>the</strong> standard deviation of <strong>the</strong> difference between actual earnings and a seasonally adjusted proxy for<br />
expected earnings. The expected earnings is earnings from 4 quarters prior, plus <strong>the</strong> difference between <strong>the</strong><br />
earnings 4 quarters and 8 quarters before. Column 3 presents ano<strong>the</strong>r specification using a third proxy for<br />
earnings volatility, Net Income Volatility - Analyst Forecast t−1 . This is <strong>the</strong> volatility of earnings adjusted for<br />
analysts’ forecasts over <strong>the</strong> last twelve quarters. Finally, column 4 presents <strong>the</strong> same specification as column<br />
1, but includes a measure for <strong>the</strong> level of incentive compensation. This is measured as 1 − (<br />
salary<br />
<strong>to</strong>talcompensation )<br />
and is meant <strong>to</strong> capture both explicit <strong>EPS</strong> incentives (through bonuses) and implicit incentives including<br />
sensitivity <strong>to</strong> market reactions due <strong>to</strong> unexpected earnings (through grants and options). This measure is<br />
available only for firms in <strong>the</strong> ExecuComp database.<br />
[Insert Table 2 Here]<br />
The hypo<strong>the</strong>sis described in Section 2 suggests that <strong>the</strong> number of shares outstanding should be related<br />
<strong>to</strong> <strong>the</strong> volatility of earnings relative <strong>to</strong> expectations as well as <strong>to</strong> <strong>the</strong> payoffs <strong>to</strong> managers, conditional on<br />
meeting earnings. We examine both of <strong>the</strong>se aspects. The higher <strong>the</strong> volatility, <strong>the</strong> more likely a firm<br />
misses earnings by chance, while <strong>the</strong> lower <strong>the</strong> volatility, <strong>the</strong> higher <strong>the</strong> probability of meeting or beating<br />
earnings. In column 1, we see that <strong>the</strong> higher <strong>the</strong> level of Net Income Volatility t−1 , <strong>the</strong> higher <strong>the</strong> number<br />
of shares outstanding. This is strongly significant, both economically and statistically. A firm with earnings<br />
volatility one standard deviation above <strong>the</strong> mean has 0.21 standard deviations more shares outstanding.<br />
The association is consistent across columns 1-3 using different proxies for earnings volatility. In fact, when<br />
looking at volatility relative <strong>to</strong> analyst forecasts, <strong>the</strong> effect is even larger. One standard deviation higher<br />
earnings volatility is associated with 0.30 standard deviations more shares.<br />
We also examine payoffs <strong>to</strong> managers conditional on meeting or beating earnings. Under our hypo<strong>the</strong>sis,<br />
we expect that <strong>the</strong> stronger <strong>the</strong> incentives for managers <strong>to</strong> avoid missing earnings forecasts, <strong>the</strong> more shares<br />
outstanding. In column 4, we proxy for <strong>the</strong>se incentives with <strong>the</strong> fraction of CEO compensation that is<br />
performance <strong>based</strong>. S<strong>to</strong>ck and option ownership should be associated with strong incentives <strong>to</strong> meet or beat<br />
earnings due <strong>to</strong> <strong>the</strong> strong negative s<strong>to</strong>ck market reaction <strong>to</strong> missing forecasts. Bonuses paid <strong>to</strong> managers<br />
are often paid <strong>based</strong> on meeting <strong>EPS</strong> targets (De Angelis and Grinstein (2011), Young and Yang (2011),<br />
Kim and Yang (2012)). The measure of <strong>to</strong>tal incentive compensation should capture both of <strong>the</strong>se aspects<br />
of a manager’s incentive <strong>to</strong> meet earnings. Consistent with this, we see a small but significantly positive<br />
16
elationship between incentive compensation and shares outstanding. Specifically, a one standard deviation<br />
larger incentive compensation is associated with 0.05 standard deviations more shares outstanding.<br />
Consistent with <strong>the</strong> nominal price puzzle (Weld et al. (2009)), we see that larger firms have more shares<br />
outstanding.<br />
A one standard deviation change in size is associated with 0.76 standard deviations more<br />
shares outstanding. We also find that a one standard deviation larger Amihud measure is associated with a<br />
small (0.11 of a standard deviation), but statistically significant lower number of shares outstanding. This<br />
is consistent with <strong>the</strong> evidence that liquidity tends <strong>to</strong> improve after a s<strong>to</strong>ck splits. In column 1, we see<br />
no evidence of Institutional Ownership relating <strong>to</strong> <strong>the</strong> share structure of <strong>the</strong> firm. <strong>How</strong>ever, in column 4,<br />
controlling for incentive compensation (which reduces <strong>the</strong> sample due <strong>to</strong> data requirements), we see that<br />
Institutional Ownership is negatively related <strong>to</strong> shares outstanding. This is consistent with Dyl and Elliott<br />
(2006) who find that smaller share price s<strong>to</strong>cks have lower institutional ownership.<br />
While our evidence on <strong>the</strong> volatility of earnings and incentive compensation is consistent with our hypo<strong>the</strong>sis,<br />
we find evidence that <strong>the</strong> level of net income is negatively associated with shares outstanding.<br />
This is not entirely surprising. After controlling for size, <strong>the</strong>re is significantly less variation in net income.<br />
Moreover, <strong>the</strong>se findings highlight <strong>the</strong> thorny fact that <strong>the</strong>se firm characteristics are jointly determined and<br />
are likely related <strong>to</strong> o<strong>the</strong>r, unobserved characteristics. Therefore, fully understanding what is driving <strong>the</strong><br />
<strong>the</strong> shares outstanding choice requires a different identification strategy.<br />
To <strong>the</strong> extent that firms have unobserved characteristics that determine share structure and managerial<br />
incentives, <strong>the</strong> simple pooled OLS estimates will be biased and inconsistent. The first step we take <strong>to</strong> mitigate<br />
<strong>the</strong>se issues is <strong>to</strong> examine a simple first difference model. This specification will measure <strong>the</strong> relationship<br />
between changes in firm characteristics and changes in shares outstanding. To <strong>the</strong> extent that a firm’s level<br />
of shares is determined by some variety of unobserved firm characteristics, focusing on changes will allow us<br />
<strong>to</strong> identify <strong>the</strong> effect of firm observable characteristics that change over time. While <strong>the</strong> specification itself<br />
mitigates issues with unobserved time invariant heterogeneity, it does not rule out <strong>the</strong> possibility of reverse<br />
causality.<br />
In Table 3, we present three specifications, one for each of <strong>the</strong> earnings volatility proxies described in<br />
Table 2. Consistent with prior results, earnings volatility is an important determinant of shares outstanding.<br />
In this case, a one standard deviation change in earnings volatility is associated with between 0.03 and 0.07<br />
standard deviations of changes in shares outstanding. This effect is statistically significant at <strong>the</strong> 1% level<br />
and is still economically large when considering it is an estimate of changes.<br />
[Insert Table 3 Here]<br />
17
While Table 2 and Table 3 establish a relationship between earnings volatility and shares outstanding<br />
in both <strong>the</strong> cross section and time series, <strong>the</strong>y do not establish a clear causal link due <strong>to</strong> <strong>the</strong> presence of<br />
unobserved firm characteristics that likely change through time. In order <strong>to</strong> examine this question more<br />
carefully and test <strong>the</strong> explicit hypo<strong>the</strong>ses outlined above, we use exogenous variation in <strong>the</strong> volatility of<br />
earnings around <strong>the</strong> expectation <strong>to</strong> establish a causal link between incentives and share structure.<br />
In Table 4 we use an instrumental variable approach for <strong>the</strong> first difference model described above. We<br />
instrument for <strong>the</strong> volatility of earnings (proxied for in Table 2 using <strong>the</strong> volatility of earnings relative <strong>to</strong><br />
analyst forecasts) by using exogenous drops in analyst coverage. Our identification strategy is similar <strong>to</strong><br />
those used in Hong and Kacperczyk (2010), Kelly and Ljungqvist (2012), and Derrien and Kecskés (2012)<br />
who argue that <strong>the</strong> consolidation of analyst coverage following brokerage house mergers leads <strong>to</strong> exogenous<br />
drops in overall coverage. When brokerage houses merge, <strong>the</strong> combined houses will often have more than<br />
one analyst covering a s<strong>to</strong>ck. As brokerages reduce coverage <strong>to</strong> eliminate this duplication of effort, <strong>the</strong> <strong>to</strong>tal<br />
number of analysts following certain s<strong>to</strong>cks drops; however, this drop in coverage is exogenous <strong>to</strong> <strong>the</strong> firm’s<br />
fundamentals.<br />
[Insert Table 4 Here]<br />
We use a slight variation in <strong>the</strong> brokerage house strategy employed by Degeorge et al. (2012). We use<br />
drops in analyst coverage brought on by analysts that leave <strong>the</strong> IBES database permanently in that period.<br />
As shown in Degeorge et al. (2012), <strong>the</strong>se drops match <strong>the</strong> distribution of those from brokerage mergers.<br />
After a drop in analyst coverage, <strong>the</strong> consensus forecasts will be noisier because <strong>the</strong> consensus is formed over<br />
a smaller sampling of analysts - <strong>the</strong> variance of <strong>the</strong> sample mean is decreasing in n. Therefore, it is less<br />
likely that realized <strong>EPS</strong> will meet forecasts solely as a result of <strong>the</strong> drop.<br />
In Table 4, we show results from <strong>the</strong> second stage of a 2SLS regression using <strong>the</strong> drop in a analyst<br />
coverage as an instrument for Net Income Volatility-Analyst Forecast t−1 . Our instrument is strong. In <strong>the</strong><br />
first stage regression, <strong>the</strong> t-statistic on <strong>the</strong> instrument is > 5 and <strong>the</strong> F-statistic is > 25, both well above<br />
<strong>the</strong> benchmarks established in S<strong>to</strong>ck et al. (2002). Using <strong>the</strong> instrumental variable approach, we see still<br />
see a strong causal relationship between changes in <strong>the</strong> volatility of forecast errors and shares outstanding.<br />
Specifically, a one standard deviation increase in Net Income Volatility-Analyst Forecast t−1 is associated<br />
with a 0.53-0.58 standard deviation increase in <strong>the</strong> number of shares outstanding. This is an economically<br />
large effect, as one standard deviation is measured over <strong>the</strong> entire cross sectional distribution of shares<br />
outstanding. Given <strong>the</strong> exogenous nature of <strong>the</strong> instrument, we can now document evidence consistent with<br />
18
<strong>the</strong> view that increases in forecast volatility cause managers <strong>to</strong> increase <strong>the</strong> number of shares outstanding.<br />
Comparing <strong>the</strong>se coefficients <strong>to</strong> Table 3 we see a much larger effect. This difference provides strong evidence<br />
of <strong>the</strong> endogenous relationship between <strong>the</strong>se variables and shows <strong>the</strong> importance of <strong>the</strong> exogenous shock in<br />
terms of measuring magnitudes.<br />
We also see a clearer relationship with respect <strong>to</strong> o<strong>the</strong>r incentives and share structures. Changes in Market<br />
<strong>to</strong> Book are negatively related <strong>to</strong> shares outstanding. A one standard deviation increase in Market <strong>to</strong> Book<br />
is associated with 0.03 standard deviation decrease in shares outstanding, but this effect is insignificant<br />
when we control for incentive compensation. We also find a positive effect of 0.08 standard deviations due<br />
<strong>to</strong> a change in Market Cap. These two results are consistent with De Angelis and Grinstein (2011) who<br />
show that small, high growth firms compensate managers less on accounting <strong>based</strong> criteria. We also observe<br />
that as Net Income grows, shares outstanding increase. Finally, in column 2 of Table 4 <strong>the</strong>re is a small<br />
but significant positive relationship between increases in incentive compensation and <strong>the</strong> change in shares<br />
outstanding. Overall, we find that changes in forecast error volatility cause an increase in shares and that<br />
net income growth and incentive compensation increases are also associated with an increase in shares. This<br />
evidence supports our hypo<strong>the</strong>sis H1A described in Section 2.<br />
In Table 5, we explore in more detail <strong>the</strong> mechanism by which managers increase <strong>the</strong>ir shares outstanding.<br />
In order <strong>to</strong> compare across columns, we use standardized independent variables and unstandardized measures<br />
for changes in shares outstanding.<br />
This allows us <strong>to</strong> interpret <strong>the</strong> coefficients as <strong>the</strong> number of shares<br />
increased (or decreased) due <strong>to</strong> a one standard deviation change in a given independent variable. We do<br />
this <strong>to</strong> compare across different sources of share increases which have different cross sectional distributions.<br />
Column 1 reports <strong>the</strong> effect of changes in characteristics on increases in shares from sources o<strong>the</strong>r than s<strong>to</strong>ck<br />
splits. While <strong>the</strong> point estimate for changes in Net Income Volatility as instrumented by analyst coverage<br />
drops shows an increase in shares outstanding from a combination of issuances, treasury shares, and s<strong>to</strong>ck<br />
awards, <strong>the</strong> effect is not statistically significant. In contrast, column 2 shows a large and significant increase<br />
in shares due <strong>to</strong> an increase in Net Income Volatility (as instrumented by analyst coverage) as a result of<br />
s<strong>to</strong>ck splits. These results suggest that <strong>the</strong> channel managers use <strong>to</strong> increase <strong>the</strong> range of Net Income that<br />
will round <strong>to</strong> analyst expectations is through s<strong>to</strong>ck splits, not through issuances or use of treasury s<strong>to</strong>ck.<br />
This evidence is consistent with hypo<strong>the</strong>sis H4.<br />
To provide fur<strong>the</strong>r evidence that managers engage in target size management, we explore a unique feature<br />
of <strong>the</strong> relationship between shares, net income, and target size. The size of <strong>the</strong> earnings target is a function of<br />
<strong>the</strong> magnitude of <strong>the</strong> <strong>EPS</strong> forecast, not <strong>the</strong> sign. Therefore, earnings growth has opposite effects, depending<br />
19
on whe<strong>the</strong>r <strong>the</strong> firm has positive or negative earnings. As such, we expect differential results depending on<br />
whe<strong>the</strong>r firms have positive or negative <strong>EPS</strong> (see Section 2 H5).<br />
[Insert Table 5 Here]<br />
Columns 3 and 4 test this discontinuity in our prediction explicitly. We split <strong>the</strong> sample <strong>based</strong> on firms<br />
that have negative earnings (column 3) and firms with positive earnings (column 4). The effect of Net Income<br />
Volatility is driven largely by <strong>the</strong> positive <strong>EPS</strong> firms. Consistent with our predictions, <strong>the</strong> coefficient on Net<br />
Income growth is negative for those firms with negative <strong>EPS</strong>. The net income of <strong>the</strong>se firms is growing (i.e.<br />
getting closer <strong>to</strong> zero) which suggests that <strong>the</strong> rounding range is actually increasing. As a result, <strong>the</strong>se firms<br />
are less likely <strong>to</strong> split.<br />
In columns 5 and 6, we examine in fur<strong>the</strong>r detail <strong>the</strong> effect that compensation structure has on <strong>the</strong> response<br />
of firms <strong>to</strong> volatility shocks. We split <strong>the</strong> sample <strong>based</strong> on Incentive Compensation. We expect that<br />
<strong>the</strong> stronger <strong>the</strong> <strong>EPS</strong> incentives, <strong>the</strong> stronger <strong>the</strong> observed effect of forecast volatility on s<strong>to</strong>ck splits (hypo<strong>the</strong>sis<br />
H2a). We see that <strong>the</strong> coefficient is substantially larger for firms with high incentive compensation<br />
(column 5) compared <strong>to</strong> low incentive compensation (column 6), for which <strong>the</strong> coefficient is not statistically<br />
different from zero. While we cannot reject <strong>the</strong> null that <strong>the</strong>se two coefficients are statistically <strong>the</strong> same,<br />
<strong>the</strong> point estimates suggest a strong relationship between incentive compensation and <strong>the</strong> magnitude of our<br />
effect.<br />
3.2.2 Costs of Splitting<br />
The evidence so far is consistent with managers adjusting shares <strong>to</strong> manage <strong>the</strong> size of <strong>the</strong> <strong>EPS</strong> target. In<br />
this section, we examine if target size management is conditional on o<strong>the</strong>r costs or benefits relating <strong>to</strong> shares.<br />
<strong>How</strong>ever, we also recognize that a change in <strong>the</strong> quantity of tradeable securities affects things o<strong>the</strong>r than<br />
just <strong>the</strong> target, and that managers likely trade off o<strong>the</strong>r costs or benefits when choosing <strong>to</strong> adjust shares. In<br />
certain cases, <strong>the</strong> manager might find it <strong>to</strong>o costly <strong>to</strong> increase <strong>the</strong> target size for o<strong>the</strong>r share-related reasons,<br />
such as liquidity/delisting.<br />
In Table 6, we estimate models <strong>the</strong> using same specification presented in Table 5. Motivated by <strong>the</strong><br />
“optimal trading range” (see, e.g., Baker and Gallagher (1980)), we include indica<strong>to</strong>r variables for high<br />
priced s<strong>to</strong>cks (above $80) and low priced s<strong>to</strong>cks (below $20). While we control for price (market value) in<br />
all previous regressions, <strong>the</strong> optimal trading range suggests a non-linear relationship. High priced s<strong>to</strong>cks are<br />
much more likely <strong>to</strong> split, but our results are not driven by <strong>the</strong>se firms. The results are robust <strong>to</strong> using o<strong>the</strong>r<br />
price level cu<strong>to</strong>ffs as well.<br />
20
In columns 2 and 3, we measure our effect conditional on illiquidity. We split <strong>the</strong> sample <strong>based</strong> on median<br />
Amihud. We expect <strong>the</strong> cost of splitting <strong>to</strong> be significantly higher for less liquid s<strong>to</strong>cks due <strong>to</strong> microstructure<br />
constraints (hypo<strong>the</strong>sis H3). Consistent with this, we see little effect in <strong>the</strong> highly illiquid s<strong>to</strong>cks. Conversely,<br />
we see a large effect in column 3 for those that are highly liquid.<br />
[Insert Table 6 Here]<br />
3.2.3 Changes in shares, earnings management, and <strong>EPS</strong> outcomes<br />
If managers increase shares in order <strong>to</strong> increase <strong>the</strong> size of <strong>the</strong> earnings target, <strong>the</strong>n increases in shares should<br />
be associated with an increase in <strong>the</strong> frequency with which <strong>the</strong> firms meets <strong>EPS</strong> expectations (H6) and with<br />
a decrease in <strong>the</strong> usage of o<strong>the</strong>r earnings management <strong>to</strong>ols (H7). To examine potential associations, we<br />
distinguish quarters in which <strong>the</strong> firm’s shares increased by at least 25% (a split ratio of at least 5-for-4).<br />
In Table 7, we examine changes in <strong>EPS</strong> outcomes over time and distinguish between changes around share<br />
increases from those without.<br />
[Insert Table 7 Here]<br />
In Panel A, we compare <strong>the</strong> frequencies with which firms meet, beat, or miss <strong>EPS</strong> targets at quarter<br />
t − 1 (<strong>the</strong> “pre” period) <strong>to</strong> those at quarter t + 1 (“post”). We compute <strong>the</strong> difference in <strong>the</strong> pre and post<br />
period, and <strong>the</strong>n differentiate firms that increase shares at t = 0 (<strong>the</strong> treatment group) from those that do<br />
not (control) and compute <strong>the</strong> difference in <strong>the</strong> sample mean differences.<br />
Among firms that increase shares in quarter t = 0, we find that <strong>the</strong>y meet <strong>EPS</strong> forecasts 71% on average<br />
in quarter t − 1 and this increases <strong>to</strong> 76% in <strong>the</strong> quarter after <strong>the</strong> share increase. This is statistically and<br />
economically different from <strong>the</strong> difference among <strong>the</strong> control group. We also find that <strong>the</strong> treatment firms<br />
miss and beat <strong>EPS</strong> forecasts less frequently following share increases. These differences relative <strong>to</strong> those<br />
of <strong>the</strong> control group are also significant - firms miss <strong>EPS</strong> forecasts 22% of <strong>the</strong> time in <strong>the</strong> quarter prior <strong>to</strong><br />
<strong>the</strong> share increase and this drops <strong>to</strong> 18% in <strong>the</strong> quarter following <strong>the</strong> increase. Firms beat <strong>EPS</strong> 7.3% pre<br />
increase, and this drops <strong>to</strong> 6.1%. We find similar effects in Panel B which uses four quarter averages for <strong>the</strong><br />
pre and post periods.<br />
We also examine <strong>the</strong> association between increases in shares and <strong>the</strong> usage of accruals and real earnings<br />
management <strong>to</strong>ols in a similar manner. We use two measures of accruals and three measures of real earnings<br />
management. Discretionary accruals are residuals from industry <strong>to</strong>tal accruals regressions including performance<br />
controls following Ecker et al. (2011). Total accruals are defined as <strong>the</strong> change in current assets,<br />
21
adjusted for <strong>the</strong> change in cash, minus <strong>the</strong> change in current liabilities, adjusted for current liabilities used<br />
for financing, minus depreciation expense. Measures of real earnings management are estimated by abnormal<br />
cash flow, production costs, and expenditure following <strong>the</strong> methodology in Roychowdhury (2006). We do<br />
not have predictions on <strong>the</strong> sign of accruals or real earnings management, only on <strong>the</strong> magnitude of <strong>the</strong>ir<br />
usage because increasing <strong>the</strong> target size makes it easier <strong>to</strong> meet <strong>EPS</strong> forecasts from above as well as from<br />
below. Therefore, we examine changes in <strong>the</strong> absolute values of <strong>the</strong>se earnings management <strong>to</strong>ols. Results<br />
are reported in Table 8.<br />
[Insert Table 8 Here]<br />
We find evidence that <strong>the</strong> usage of accruals and real earnings management drops after <strong>the</strong> manager<br />
increases shares outstanding. This is broadly consistent with Cheong and Thomas (2012) who show that<br />
higher accruals are associated with higher <strong>EPS</strong> levels. For example, among firms that increase shares, <strong>the</strong><br />
usage of <strong>to</strong>tal accruals drops from 3.76% of assets over t − 1 <strong>to</strong> 3.30% over t + 1. This is compared <strong>to</strong> a slight<br />
increase (3.09% <strong>to</strong> 3.10%) over time among <strong>the</strong> control group. There are similar drops in <strong>the</strong> usage of o<strong>the</strong>r<br />
measures of accounting and real earnings management surrounding increases in shares, and <strong>the</strong>se hold using<br />
four quarter averages as well (Panel B). Overall, <strong>the</strong> results indicate that an increase in <strong>the</strong> target size is<br />
associated with significant, real effects on <strong>EPS</strong> outcomes and <strong>the</strong> usage of o<strong>the</strong>r earnings management <strong>to</strong>ols.<br />
3.2.4 Short term rounding effects<br />
As discussed in Section 2, managers might choose <strong>the</strong> amount by which <strong>the</strong>y change shares in light of current<br />
period earnings. To examine this, we distinguish splits by <strong>the</strong> timing in which <strong>the</strong>y are declared and <strong>the</strong><br />
magnitude of <strong>the</strong> split fac<strong>to</strong>r. First, we identify a split as late if it occurs after <strong>the</strong> quarter end but before<br />
<strong>the</strong> earnings report date. Also, for each split we set a dummy variable atypical equal <strong>to</strong> one if <strong>the</strong> split fac<strong>to</strong>r<br />
is not in (1.25, 1.33, 1.5, 1.75, 2, 2.5, 3, 4, 5, 10).<br />
Similar <strong>to</strong> Bens et al. (2003) and Hribar et al. (2006), we determine if each split had an accretive or<br />
dilutive effect (or nei<strong>the</strong>r) on that quarter-end’s <strong>EPS</strong> by comparing <strong>the</strong> post-split <strong>EPS</strong> <strong>to</strong> what <strong>the</strong> <strong>EPS</strong><br />
would have been had <strong>the</strong> firm not split. We compute post-split as IBADJQ/CSHPRQ (from Compustat)<br />
rounded <strong>to</strong> <strong>the</strong> penny. We compute pre-split <strong>EPS</strong> as IBADJQ/CSHPRQ*FACSHR, rounded <strong>to</strong> <strong>the</strong> penny,<br />
<strong>the</strong>n divided by <strong>the</strong> split fac<strong>to</strong>r. If <strong>the</strong> post-split <strong>EPS</strong> is greater than <strong>the</strong> pre-split <strong>EPS</strong> <strong>the</strong>n <strong>the</strong> split is<br />
accretive. The split is dilutive if <strong>the</strong> post-split <strong>EPS</strong> is less than pre-split, and nei<strong>the</strong>r if <strong>the</strong>re is no difference.<br />
We expect that, if firms choose <strong>the</strong> magnitude of <strong>the</strong> split out of concern for its accretive or dilutive<br />
effects on current period <strong>EPS</strong>, <strong>the</strong>se splits will occur late in <strong>the</strong> quarter, and will, on average, be in an<br />
22
atypical amount. In Table 9, we report <strong>the</strong> percentage of splits that are accretive, dilutive, or nei<strong>the</strong>r for<br />
<strong>the</strong> full sample and subsamples. We find little evidence that managers use atypical split ratios and timing<br />
<strong>to</strong> generate accretive rounding effects. Given <strong>the</strong> lack of economic significance, we do not formally report<br />
statistical significance. Across all splits, 31.8% have an accretive effect and 29% have a dilutive effect. This<br />
difference is roughly <strong>the</strong> same whe<strong>the</strong>r <strong>the</strong> split occurred during <strong>the</strong> quarter or after quarter end. Similarly,<br />
we see no meaningful difference between accretive and dilutive when distinguishing between typical and<br />
atypical split ratios.<br />
[Insert Table 9 Here]<br />
When we look exactly where we expect <strong>to</strong> see an effect - late splits that are of atypical split fac<strong>to</strong>rs -<br />
we see a large difference. <strong>How</strong>ever, only 13 splits satisfy <strong>the</strong>se criteria, far from an economically meaningful<br />
effect. To summarize, we find very little evidence that splits are used <strong>to</strong> have an accretive effect on current<br />
period <strong>EPS</strong>.<br />
3.3 Additional Implications<br />
In this section, we discuss a few additional implication of TSM. Because TSM is achieved by changing shares,<br />
any per-share metric will be affected. This suggests that cross sectional variation in a variety of per share<br />
metrics such as analyst forecast error or dispersion, and even s<strong>to</strong>ck prices, may be <strong>the</strong> endogenous outcome<br />
of TSM. We briefly examine how TSM may relate <strong>to</strong> i) analysts’ forecast errors, ii) <strong>the</strong> nominal s<strong>to</strong>ck price<br />
puzzle, and iii) idiosyncratic return volatility.<br />
3.3.1 Scale invariance of forecast volatility<br />
The observation that firms with higher <strong>EPS</strong> levels have lower variance in forecast errors than what would<br />
o<strong>the</strong>rwise be expected was first documented in Degeorge et al. (1999). More recent work has attempted <strong>to</strong><br />
understand why this scale invariance exists. Cheong and Thomas (2011) test three potential explanations<br />
and find results that, on net, suggest managers suppress <strong>the</strong> natural variation due <strong>to</strong> scale. Importantly,<br />
forecast error variance is computed at <strong>the</strong> per-share level, which means it is a function of <strong>the</strong> magnitude<br />
of rounding. Ball (2011) describes how rounding net income at <strong>the</strong> share level can introduce noise, and<br />
suggests that this could contribute <strong>to</strong> a lack of variance with scale. We build on this by positing that scale<br />
invariance is <strong>the</strong> endogenous outcome of TSM. In fact, <strong>the</strong> lack of variation with scale is essentially our main<br />
prediction. To see this, consider a simple example.<br />
23
Two firms are <strong>the</strong> same in all ways except for <strong>the</strong>ir distributions of net income. Firm A’s net income is<br />
distributed uniformly over [9, 11), and Firm B’s net income is uniformly distributed over [8, 12). So both firms<br />
have <strong>the</strong> same expected net income but B is more volatile than A. If both managers equally value meeting<br />
<strong>EPS</strong> forecasts, <strong>the</strong>n each will choose shares outstanding such that <strong>the</strong> probability of meeting expectations is<br />
<strong>the</strong> same across both firms. If Firm A has 100 shares outstanding, <strong>the</strong>n <strong>the</strong> probability that <strong>the</strong> firm meets<br />
earnings is 1/2. 16 If <strong>the</strong> manager of B also wants <strong>to</strong> meet forecasts half of <strong>the</strong> time, <strong>the</strong> firm will need 200<br />
shares outstanding. 17<br />
From here it is easy <strong>to</strong> show that <strong>the</strong> two firms will have identical variance in forecast errors.<br />
For<br />
each firm, one fourth of <strong>the</strong> time <strong>the</strong> firm will miss <strong>EPS</strong> forecasts by one penny, one-half of <strong>the</strong> time <strong>the</strong>y<br />
meet expectations, and one-fourth of <strong>the</strong> time <strong>the</strong>y beat expectations by a penny. 18<br />
In this way, <strong>the</strong> scale<br />
invariance of forecast errors is <strong>the</strong> equilibrium outcome of managers’ incentive <strong>to</strong> meet <strong>EPS</strong> forecasts.<br />
Fur<strong>the</strong>rmore, we would expect forecast error variance <strong>to</strong> drop after a split. If nothing changes about<br />
Firm A o<strong>the</strong>r than that it issues a two-for-one s<strong>to</strong>ck split, <strong>the</strong> variance in forecast errors drops <strong>to</strong> zero (all<br />
possible net income outcomes generate <strong>EPS</strong> = 0.05).<br />
We do not think our results completely explain <strong>the</strong> puzzle of scale invariant forecast errors. Cheong and<br />
Thomas (2011) find that <strong>the</strong> scale invariance is not present in per share cash flow forecasts, for example.<br />
A simple rounding <strong>based</strong> explanation is not consistent with this important finding.<br />
Therefore, it seems<br />
reasonable <strong>to</strong> conclude that target size management can explain some of <strong>the</strong> scale invariance results, but <strong>the</strong><br />
active smoothing of earnings by managers also plays an important role.<br />
3.3.2 Nominal price puzzle<br />
Weld et al. (2009) document that nominal per-share s<strong>to</strong>ck prices have remained remarkably constant across<br />
time (1933-2007). This is surprising given significant inflation over <strong>the</strong> same period. The authors estimate<br />
that if real s<strong>to</strong>ck prices had remained constant over this period, prices <strong>to</strong>day would average around $450.<br />
Fur<strong>the</strong>rmore, <strong>the</strong> authors make <strong>the</strong> observation that existing <strong>the</strong>ories of s<strong>to</strong>ck splits fail <strong>to</strong> predict that<br />
nominal share prices would remain constant. The authors conclude that social norms drive managers <strong>to</strong> use<br />
s<strong>to</strong>ck splits <strong>to</strong> keep nominal prices at some fixed level.<br />
While our results may not fully explain <strong>the</strong> nominal price puzzle, TSM may contribute <strong>to</strong> <strong>the</strong> constant<br />
16 For simplicity assume that forecasts are unbiased. The firm needs net income within ± 0.5 = 5%, or any net income<br />
|E[EP S]|<br />
∈ [9.5, 10.5). The firm will generate net income in this range 10.5−9.5 = 1 of <strong>the</strong> time.<br />
11−9 2<br />
s<br />
17 Set <strong>the</strong> probability of meeting forecasts equal <strong>to</strong> 1/2 and solve for s: 1/2 = 100<br />
12−8 .<br />
18 For Firm A, Var = 1 4 (0.09 − 0.10)2 + 1 2 (0)2 + 1 4 (0.11 − 0.10)2 = 1 2 (0.01)2 . For Firm B, Var = 1 4 (0.04 − 0.5)2 + 1 2 (0)2 +<br />
1<br />
4 (0.06 − 0.05)2 = 1 2 (0.01)2 .<br />
24
price levels observed in <strong>the</strong> data. Firms are required <strong>to</strong> round <strong>EPS</strong> <strong>to</strong> <strong>the</strong> penny, and this remains true<br />
despite <strong>the</strong> penny declining in real value. Because <strong>the</strong> norm of rounding <strong>to</strong> <strong>the</strong> penny has been stable, so<br />
should nominal <strong>EPS</strong> levels. If managers choose shares outstanding <strong>to</strong> maintain a constant nominal level of<br />
<strong>EPS</strong>, <strong>the</strong>n it may not be surprising <strong>to</strong> also find constant nominal price levels over time.<br />
In each quarter, we compute <strong>the</strong> median price-per-share and median earnings-per-share. We plot <strong>the</strong>se<br />
median values over time in Figure 3. Due <strong>to</strong> Compustat earnings data limitations, we limit <strong>the</strong> sample <strong>to</strong><br />
post 1970. Weld et al (2009) argue that managers choose shares outstanding <strong>to</strong> keep prices constant, whereas<br />
we argue that managers choose shares outstanding <strong>to</strong> keep earnings per share constant. The figure shows<br />
that, not surprisingly, prices and earnings levels are strongly related. It is also evident that <strong>the</strong>re is variation<br />
in both price-per-share and earnings-per-share medians.<br />
[Insert Figure 4 about here]<br />
It is difficult <strong>to</strong> distinguish between <strong>the</strong> incentive for constant nominal <strong>EPS</strong> generating constant nominal<br />
prices from <strong>the</strong> incentive for constant nominal prices generating nominal <strong>EPS</strong>. We attempt <strong>to</strong> provide some<br />
evidence that <strong>the</strong> incentive for constant <strong>EPS</strong> does affect aggregate price levels. To do so, we use time series<br />
variation in net income volatility. Our earlier results suggest that firms respond <strong>to</strong> increases in net income<br />
volatility by reducing <strong>EPS</strong> levels.<br />
Therefore, we predict that changes in aggregate net income volatility<br />
should predict changes in aggregate <strong>EPS</strong> levels.<br />
If managers are choosing constant <strong>EPS</strong> levels and not<br />
constant price levels, <strong>the</strong>n this variation should also show up in price levels. O<strong>the</strong>rwise, it is less clear why<br />
aggregate per share price levels should be a function of lagged aggregate net income volatility.<br />
We compute correlations between median price-per-share, median earnings-per-share, and median Net<br />
Income volatility (measured for each firm using <strong>the</strong> prior 12 quarters) over time. Median prices and median<br />
earnings are highly correlated, 0.68. The correlation between median <strong>EPS</strong> and median NI volatility is -0.38,<br />
and significant at <strong>the</strong> 1% level. This is consistent with our cross-sectional results which suggest that firms<br />
decrease <strong>EPS</strong> as a response <strong>to</strong> an increase in volatility. More interestingly, median nominal prices are also<br />
negatively correlated with trailing 12-quarter NI volatility (ρ = −0.16, pvalue = 0.025). This suggests that<br />
managers’ incentives for certain <strong>EPS</strong> levels contribute <strong>to</strong> variation in price levels.<br />
Our results do not suggest that social norms have no role. In fact norms may be <strong>the</strong> primary determinant<br />
of constant nominal prices. We merely suggest that TSM is an explanation for s<strong>to</strong>ck splits that is consistent<br />
with constant nominal price levels.<br />
25
3.3.3 S<strong>to</strong>ck price levels and idiosyncratic volatility<br />
Target Size Management has implications for <strong>the</strong> relationship between per share s<strong>to</strong>ck price levels and return<br />
volatility. One result documented in Brandt et al. (2010) is that lower priced s<strong>to</strong>cks have higher return<br />
volatility. An interpretation of this relationship is that low priced s<strong>to</strong>cks have higher volatility because <strong>the</strong>y<br />
have a low price, and that this is a result of a retail trader clientele effect. TSM suggest that causality may<br />
run in <strong>the</strong> opposite direction. Firms with high earnings volatility may choose low prices as a result of <strong>EPS</strong><br />
incentives. To <strong>the</strong> extent that earnings volatility and return volatility are correlated, we would expect <strong>to</strong> see<br />
similar empirical outcomes but with causality running in <strong>the</strong> opposite direction.<br />
In unreported tests, we observe a nearly identical relationship between per share price levels and return<br />
volatility (Brandt et al. (2010)) and per share price level and net income volatility (TSM). Distinguishing<br />
between <strong>the</strong>se two possible explanations is beyond <strong>the</strong> scope of this paper.<br />
<strong>How</strong>ever, this highlights an<br />
example of potential implications of target size management that are beyond financial reporting and <strong>EPS</strong><br />
outcomes.<br />
4 Conclusion<br />
A range of net income numbers will generate <strong>the</strong> same <strong>EPS</strong> number. This is because earnings per share<br />
are rounded <strong>to</strong> <strong>the</strong> nearest penny. So, for any given <strong>EPS</strong> forecast, <strong>the</strong>re is a range of <strong>to</strong>tal earnings that<br />
will meet that forecast. We refer <strong>to</strong> <strong>the</strong> magnitude of this range as <strong>the</strong> size of <strong>the</strong> earnings target. The<br />
size of <strong>the</strong> earnings target is a function of <strong>the</strong> number of shares outstanding. We find evidence consistent<br />
with <strong>the</strong> view that managers engage in target size management - adjusting <strong>the</strong> firm’s quantity of tradeable<br />
securities <strong>to</strong> affect <strong>the</strong> size of <strong>the</strong> range of net income numbers that meet <strong>EPS</strong> forecasts. We find that an<br />
exogenous decrease in <strong>the</strong> probability of meeting earnings estimates causes managers <strong>to</strong> split <strong>the</strong>ir s<strong>to</strong>cks,<br />
<strong>the</strong>reby increasing <strong>the</strong> earnings target size. We find that this effect is stronger among firms whose managers’<br />
compensation is highly sensitive <strong>to</strong> <strong>EPS</strong> surprises, and weaker among firms for which an increase in shares<br />
would be highly costly (e.g., highly illiquid firms).<br />
Target size management has real effects. We find that firms are more likely <strong>to</strong> meet <strong>EPS</strong> expectations<br />
following an increase in shares. Simultaneously, <strong>the</strong>se firms use less accounting and real earnings management<br />
<strong>to</strong>ols. Both of <strong>the</strong>se associations are consistent with an increase in shares increasing <strong>the</strong> earnings target size.<br />
Our results suggest that <strong>the</strong> magnitude of <strong>the</strong> firm’s long run usage of earnings management <strong>to</strong>ols is a<br />
managerial choice. This has implications for research examining <strong>the</strong> determinants of traditional earnings<br />
26
management <strong>to</strong>ols.<br />
27
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30
A<br />
Appendix<br />
We show that a drop in analyst coverage decreases <strong>the</strong> probability of meeting <strong>the</strong> earnings forecast. Consider<br />
a firm with s shares outstanding and net income uniformly distributed [−e, e]), where e is in dollars. Assume<br />
that each analyst issues a forecast that is independently drawn from a uniform distribution over [−e, e]), and<br />
that <strong>the</strong> consensus forecast is <strong>the</strong> sample mean. With infinite analysts, <strong>the</strong> forecast equals <strong>the</strong> mean and<br />
<strong>the</strong>re is no variance. In this benchmark case <strong>the</strong> forecast is unbiased and has no noise, and <strong>the</strong> probability<br />
that <strong>the</strong> firm meets earnings forecasts is<br />
s<br />
200e .<br />
For simplicity, we compare <strong>to</strong> <strong>the</strong> case in which <strong>the</strong>re is only one analyst. The variance in <strong>the</strong> estimate<br />
will <strong>the</strong>refore be much higher than <strong>the</strong> benchmark case (<strong>the</strong> variance of <strong>the</strong> sample mean is decreasing in<br />
N). Because <strong>the</strong> variance is higher, <strong>the</strong> probability of meeting <strong>the</strong> forecast is lower. The intuition for this is<br />
straightforward. If <strong>the</strong> forecast is relatively close <strong>to</strong> <strong>the</strong> mean, <strong>the</strong>n P r(meet) =<br />
is close <strong>to</strong> one of <strong>the</strong> tails of <strong>the</strong> distribution, <strong>the</strong>n P r(meet) <<br />
s<br />
200e<br />
. But if <strong>the</strong> forecast<br />
s<br />
200e<br />
. No matter where <strong>the</strong> forecast is, <strong>the</strong><br />
target size around <strong>the</strong> forecast is always ± s<br />
200<br />
, but integrating over this range results in different probabilities<br />
depending on where in <strong>the</strong> distribution <strong>the</strong> forecast is. When <strong>the</strong> forecast deviates from <strong>the</strong> mean, <strong>the</strong> result<br />
is a lower probability simply because <strong>the</strong> outcomes in <strong>the</strong> tails are less likely <strong>to</strong> occur.<br />
With probability 1 −<br />
With probability<br />
P r(meet) =<br />
s<br />
200e<br />
<strong>the</strong> forecast will be close enough <strong>to</strong> <strong>the</strong> mean such that P r(meet) =<br />
s<br />
200e .<br />
s<br />
400e<br />
<strong>the</strong> forecast will be on <strong>the</strong> left tail of <strong>the</strong> uniform distribution such that in expectation<br />
3s<br />
800e<br />
. Because <strong>the</strong> forecast is unbiased <strong>the</strong> effect is <strong>the</strong> same on <strong>the</strong> right tail. Therefore, with<br />
a noisy, unbiased forecast:<br />
E[P r(meet)] = (1 −<br />
s<br />
200e ) s<br />
200e + 2( s<br />
400e ) 3s<br />
400e =<br />
s<br />
200e (1 −<br />
s<br />
800e ).<br />
We can compare this probability <strong>to</strong> <strong>the</strong> case in which <strong>the</strong> forecast is not noisy (infinite analysts). It<br />
is easy <strong>to</strong> show that if <strong>the</strong> manager prefers <strong>the</strong> same Pr(meet), shares need <strong>to</strong> increase in response <strong>to</strong><br />
a drop in analyst coverage.<br />
Using s ∗ <strong>to</strong> denote <strong>the</strong> shares in <strong>the</strong> case of a forecast without noise, <strong>the</strong>n<br />
s<br />
200e (1 −<br />
s<br />
800e ) =<br />
s∗<br />
200e → s > s∗ .<br />
The result shown above assumes analysts are unbiased. It can be shown that an increase in forecast bias<br />
has <strong>the</strong> same qualitative effect. Intuitively, integrating over <strong>the</strong> ± s<br />
200<br />
range results in a lower probability<br />
when <strong>the</strong> forecast is far<strong>the</strong>r away from <strong>the</strong> mean. In this way an increase in bias has an effect similar <strong>to</strong> an<br />
increase in forecast variance.<br />
31
Table 1: Summary Statistics<br />
This table presents summary statistics of <strong>the</strong> key variables used in this study. Shares outstanding (millions) is<br />
<strong>the</strong> <strong>to</strong>tal number of shares outstanding (CRSP) at <strong>the</strong> end of <strong>the</strong> quarter. <strong>EPS</strong> is <strong>the</strong> primary earnings per share<br />
(COMPUSTAT). Net Income is <strong>the</strong> reported net income at <strong>the</strong> fiscal quarter end. Net Income Vol is <strong>the</strong> standard<br />
deviation of net income over <strong>the</strong> past 12 qtrs. Net Income Vol - Naive is <strong>the</strong> standard deviation of seasonally adjusted<br />
net income over <strong>the</strong> past 12 qtrs. Net Income Vol - Analyst is <strong>the</strong> standard deviation of net income minus <strong>the</strong> consensus<br />
IBES median forecast of net income over <strong>the</strong> previous 12 qtrs. S<strong>to</strong>ck Volatility is <strong>the</strong> standard deviation of daily<br />
s<strong>to</strong>ck returns over <strong>the</strong> past year. Market Capitalization is <strong>the</strong> <strong>to</strong>tal market capitalization in millions at <strong>the</strong> quarter<br />
end. Institutional Ownership is <strong>the</strong> % of institutional ownership from Thomson 13(f). Incentive Compensation is<br />
calculated as 1-(Salary/TDC1). Num of Analysts is <strong>the</strong> number of analysts cover <strong>the</strong> s<strong>to</strong>ck during <strong>the</strong> quarter.<br />
Annual S<strong>to</strong>ck Return is <strong>the</strong> past 12 month s<strong>to</strong>ck return. Amihud is <strong>the</strong> log of <strong>the</strong> Amihud ratio calculated over <strong>the</strong><br />
past year. Split ratio is <strong>the</strong> ratio <strong>to</strong> adjust shares at s<strong>to</strong>ck split announcement. Share price is <strong>the</strong> s<strong>to</strong>ck price at <strong>the</strong><br />
end of <strong>the</strong> quarter. Age is <strong>the</strong> years since IPO. The sample is from 1984-2012.<br />
Variable Mean P25 Median P75 STD<br />
Shares Outstanding 83.85 10.16 23.55 56.75 346.78<br />
<strong>EPS</strong> 0.20 -0.02 0.19 0.47 1.19<br />
Net Income 34.48 -0.30 3.05 17.65 388.95<br />
Net Income Vol 51.48 1.59 5.23 20.57 347.76<br />
Net Income Vol - Naive 40.38 1.47 4.75 18.20 264.06<br />
Net Income Vol - Analyst 32.04 0.58 2.38 11.01 250.83<br />
S<strong>to</strong>ck Volatility 3.30 1.82 2.68 4.04 2.35<br />
Market Capitalization 2766 95 338 1316 13069<br />
Institutional Ownership 47.97 24.34 46.85 70.22 27.78<br />
Incentive Compensation 66.65 54.04 73.24 85.19 24.46<br />
Num of Analysts 4.24 1 3 5 4.35<br />
Annual S<strong>to</strong>ck Return 15.74 -21.13 5.96 34.78 81.12<br />
Amihud -1.05 -2.90 -0.98 0.80 2.57<br />
Split Ratio 1.64 1.50 1.50 2.00 0.68<br />
Share Price 22.68 7.70 17.25 30.75 24.94<br />
Age 16.1 5.5 11.2 21.2 15.2<br />
32
Figure 1: Example of <strong>the</strong> relationship between earnings growth, shares outstanding and <strong>EPS</strong>.<br />
This figure shows <strong>the</strong> mechanical relationship between earnings growth, shares outstanding, and <strong>EPS</strong> as a result<br />
of <strong>EPS</strong> rounding. The Base Case presents an example of a firm with $100 of expected earnings and 1000 shares<br />
outstanding with a target size of ±5% of expected earings. Earnings Growth (1000 shares) presents an example of<br />
<strong>the</strong> same 1000 shares outstanding and expected earnings of $200. The target size is ±2.5% of expected earnings.<br />
Earnings Growth and 2:1 Split presents <strong>the</strong> same example but with 2000 shares outstanding. The target size returns<br />
<strong>to</strong> ±5%.<br />
Base Case (1000 Shares)<br />
<strong>EPS</strong>= $0.10<br />
Earnings=$95<br />
E[Earnings]=$100<br />
+/- 5% of E[Earnings]<br />
Earnings=$105<br />
Earnings Growth (1000 Shares)<br />
<strong>EPS</strong>= $0.20<br />
E[Earnings]=$200<br />
Earnings=$195<br />
Earnings=$205<br />
+/- 2.5% of E[Earnings]<br />
Earnings Growth and 2:1 Split (2000 Shares)<br />
<strong>EPS</strong>= $0.10<br />
Earnings=$190<br />
E[Earnings]=$200<br />
+/- 5% of E[Earnings]<br />
Earnings=$210<br />
33
Figure 2: His<strong>to</strong>gram of net income scaled by <strong>the</strong> minimum necessary <strong>to</strong> meet <strong>the</strong> median analyst forecast.<br />
This figure presents a his<strong>to</strong>gram of earnings outcomes. For each firm-quarter, we compute <strong>the</strong> minimum net income<br />
needed <strong>to</strong> meet <strong>the</strong> median forecast. We scale each firm-quarter reported net income by this minimum. The dark<br />
vertical line that intersects <strong>the</strong> x-axis at a value of 1 indicates <strong>the</strong> point at which <strong>the</strong> firm generates just enough net<br />
income <strong>to</strong> meet <strong>the</strong> median forecast. The lighter line that intersects <strong>the</strong> x-axis near 1.02 reflects <strong>the</strong> average amount<br />
of net income that would equal <strong>the</strong> forecasted net income (<strong>EPS</strong> forecast times shares).<br />
34
Figure 3: Median Shares Outstanding across Net Income Volatility and Incentive Compensation Deciles<br />
This figure presents median shares outstanding (bar chart) and median net income (line-plot) across deciles sorted<br />
on Net Income Volatility (Panel A) and Incentive Compensation (Panel B). Shares outstanding are adjusted for net<br />
income by first sorting <strong>the</strong> sample firms in<strong>to</strong> 20 groups <strong>based</strong> on net income each quarter, and <strong>the</strong>n sorting in<strong>to</strong> deciles<br />
<strong>based</strong> on Net Income Volatility or Incentive Compensation. Net Income Volatility is <strong>the</strong> standard deviation of <strong>the</strong><br />
previous 12 quarters of net income. Incentive Compensation is calculated as 1-(Salary/TDC1). Shares outstanding<br />
is represented on <strong>the</strong> left axis and net income is on <strong>the</strong> right axis. The sample period is 1984-2011.<br />
Panel A. Shares Outstanding across Net Income Volatility Deciles<br />
Shares Outstanding<br />
40,000<br />
35,000<br />
30,000<br />
25,000<br />
20,000<br />
15,000<br />
10,000<br />
5,000<br />
0<br />
Bot<strong>to</strong>m Net<br />
Income Volatility<br />
Decile<br />
2 3 4 5 6 7 8 9<br />
Net Income<br />
5<br />
Top Net Income<br />
Volatility<br />
Decile<br />
4<br />
3<br />
2<br />
1<br />
0<br />
Shares Outstanding<br />
Net Income<br />
Panel B. Shares Outstanding across Incentive Compensation Deciles<br />
Shares Outstanding<br />
80,000<br />
70,000<br />
60,000<br />
50,000<br />
40,000<br />
30,000<br />
20,000<br />
Bot<strong>to</strong>m<br />
Incentive<br />
Comp Decile<br />
2 3 4 5 6 7 8 9<br />
Net Income<br />
50<br />
40<br />
30<br />
20<br />
10<br />
0<br />
Top<br />
Incentive<br />
Comp Decile<br />
Shares Outstanding<br />
Net Income<br />
35
Figure 4: Median nominal price-per-share and earnings-per-share, 1971-2011.<br />
This figure shows median nominal price-per-share and earnings-per-share, 1971-2011 for all US firms with price and<br />
earnings data in Compustat.<br />
36
Table 2: Determinants of Shares Outstanding<br />
This table presents OLS cross sectional regression models of shares outstanding as a function of firm characteristics. Shares outstanding<br />
is measured as <strong>the</strong> <strong>to</strong>tal number of shares outstanding (1000’s) from CRSP at <strong>the</strong> end of <strong>the</strong> quarter. Net Income Volatility is <strong>the</strong><br />
standard deviation of Net Income over <strong>the</strong> previous 12 quarters. Net Income Forecast Error Volatility - Naive is <strong>the</strong> standard deviation of<br />
<strong>the</strong> <strong>the</strong> difference between actual earnings and an expectation of earnings <strong>based</strong> on <strong>the</strong> earnings from 4 quarters prior plus <strong>the</strong> difference<br />
between <strong>the</strong> earnings 4 quarters and 8 quarters prior. Net Income Forecast Error Volatility - Analyst is <strong>the</strong> standard deviation of <strong>the</strong><br />
<strong>the</strong> difference between actual earnings and median IBES forecast of earnings. Market <strong>to</strong> Book is <strong>to</strong>tal market equity plus <strong>the</strong> book value<br />
of <strong>to</strong>tal debt divided by <strong>to</strong>tal assets. Net Income is from Compustat at quarter end. Market Cap is <strong>the</strong> <strong>to</strong>tal market capitalization in<br />
millions at <strong>the</strong> quarter end. Institutional ownership is percent ownership of all institutions. Return Volatility is <strong>the</strong> standard deviation<br />
of daily s<strong>to</strong>ck returns over <strong>the</strong> prior 90 days. Annual Return is <strong>the</strong> past 12 month s<strong>to</strong>ck return. The Amihud measure of illiquidity<br />
calculated over <strong>the</strong> previous 90 days. Incentive Comp is <strong>the</strong> percent of <strong>to</strong>tal compensation made up by bonus, s<strong>to</strong>ck, and option grants.<br />
(1) (2) (3) (4)<br />
Shares Shares Shares Shares<br />
VARIABLES Outstanding Outstanding Outstanding Outstanding<br />
Net Income Volatility t−1 0.21*** 0.25***<br />
(0.01) (0.01)<br />
Net Income Volatility - Naive Forecast t−1 0.21***<br />
(0.01)<br />
Net Income Volatility - Analyst Forecast t−1 0.30***<br />
(0.02)<br />
Market <strong>to</strong> Book t−1 0.01*** 0.01*** -0.01** -0.02**<br />
(0.00) (0.00) (0.00) (0.01)<br />
Net Income t−1 -0.11*** -0.11*** -0.09*** -0.07***<br />
(0.01) (0.01) (0.01) (0.01)<br />
Institutional Ownership t−1 0.01** 0.01*** 0.00 -0.14***<br />
(0.00) (0.00) (0.01) (0.02)<br />
Market Cap t−1 0.84*** 0.85*** 0.77*** 0.76***<br />
(0.01) (0.01) (0.01) (0.01)<br />
Annual Return t−1 -0.04*** -0.04*** -0.05*** -0.10***<br />
(0.00) (0.00) (0.00) (0.01)<br />
Amihud t−1 -0.05*** -0.06*** -0.11*** -0.43***<br />
(0.00) (0.00) (0.00) (0.13)<br />
Return Volatility t−1 0.05*** 0.06*** 0.06*** 0.12***<br />
(0.00) (0.00) (0.00) (0.01)<br />
Incentive Comp t−1 0.05***<br />
(0.01)<br />
Constant -0.04*** -0.03*** 0.03** 0.11*<br />
(0.01) (0.01) (0.02) (0.06)<br />
Year Effects Y Y<br />
Observations 582,754 486,137 332,578 120,635<br />
R-squared 0.81 0.81 0.81 0.82<br />
Standard errors clustered by firm in paren<strong>the</strong>ses<br />
*** p
Table 3: Shares Outstanding: First Differences<br />
This table presents First Differences regression models of changes in shares outstanding as a function of changes in firm characteristics.<br />
Shares outstanding is measured as <strong>the</strong> <strong>to</strong>tal number of shares outstanding (1000’s) from CRSP at <strong>the</strong> end of <strong>the</strong> quarter. Net Income<br />
Volatility is <strong>the</strong> standard deviation of Net Income over <strong>the</strong> previous 12 quarters. Net Income Forecast Error Volatility - Naive is <strong>the</strong><br />
standard deviation of <strong>the</strong> <strong>the</strong> difference between actual earnings and an expectation of earnings <strong>based</strong> on <strong>the</strong> earnings from 4 quarters<br />
prior plus <strong>the</strong> difference between <strong>the</strong> earnings 4 quarters and 8 quarters prior. Net Income Forecast Error Volatility - Analyst is <strong>the</strong><br />
standard deviation of <strong>the</strong> <strong>the</strong> difference between actual earnings and median IBES forecast of earnings. Market <strong>to</strong> Book is <strong>to</strong>tal market<br />
equity plus <strong>the</strong> book value of <strong>to</strong>tal debt divided by <strong>to</strong>tal assets. Net Income is from Compustat at quarter end. Market Cap is <strong>the</strong> <strong>to</strong>tal<br />
market capitalization in millions at <strong>the</strong> quarter end. Institutional ownership is percent ownership of all institutions. Return Volatility<br />
is <strong>the</strong> standard deviation of daily s<strong>to</strong>ck returns over <strong>the</strong> prior 90 days. Annual Return is <strong>the</strong> past 12 month s<strong>to</strong>ck return. The Amihud<br />
measure of illiquidity calculated over <strong>the</strong> previous 90 days.<br />
(1) (2) (3)<br />
∆ Shares ∆ Shares ∆ Shares<br />
VARIABLES Outstanding Outstanding Outstanding<br />
∆ Net Income Volatility t−1 0.04***<br />
(0.00)<br />
∆ Net Income Volatility - Naive Forecast t−1 0.03***<br />
(0.00)<br />
∆ Net Income Volatility - Analyst Forecast t−1 0.07***<br />
(0.01)<br />
∆ Market <strong>to</strong> Book t−1 0.01*** 0.02*** 0.02***<br />
(0.00) (0.00) (0.00)<br />
∆ Net Income t−1 0.00 0.00 0.01***<br />
(0.00) (0.00) (0.00)<br />
∆ Institutional Ownership t−1 0.12*** 0.13*** 0.13***<br />
(0.00) (0.00) (0.00)<br />
∆ Market Cap t−1 0.10*** 0.10*** 0.10***<br />
(0.00) (0.00) (0.00)<br />
∆ Annual Return t−1 0.00 -0.00 -0.00<br />
(0.00) (0.00) (0.00)<br />
∆ Amihud t−1 -0.01*** -0.01*** -0.02***<br />
(0.00) (0.00) (0.00)<br />
∆ Return Volatility t−1 0.01*** 0.01*** 0.02***<br />
(0.00) (0.00) (0.00)<br />
∆ Incentive Comp t−1<br />
Constant 0.02 0.02 0.24<br />
(0.02) (0.02) (0.29)<br />
Year Effects Y Y Y<br />
Observations 543,355 454,258 313,297<br />
R-squared 0.03 0.03 0.03<br />
Standard errors clustered by firm in paren<strong>the</strong>ses<br />
*** p
Table 4: Shares Outstanding: First Differences and IV<br />
This table presents IV regression models of changes in shares outstanding as a function of changes in firm characteristics. Net Income<br />
Forecast Error Volatility - Analyst is instrumented for using exogenous changes in analyst coverage. Shares outstanding is measured as<br />
<strong>the</strong> <strong>to</strong>tal number of shares outstanding (1000’s) from CRSP at <strong>the</strong> end of <strong>the</strong> quarter. Net Income Forecast Error Volatility - Analyst<br />
is <strong>the</strong> standard deviation of <strong>the</strong> <strong>the</strong> difference between actual earnings and median IBES forecast of earnings. Market <strong>to</strong> Book is <strong>to</strong>tal<br />
market equity plus <strong>the</strong> book value of <strong>to</strong>tal debt divided by <strong>to</strong>tal assets. Net Income is from Compustat at quarter end. Market Cap is<br />
<strong>the</strong> <strong>to</strong>tal market capitalization in millions at <strong>the</strong> quarter end. Institutional ownership is percent ownership of all institutions. Return<br />
Volatility is <strong>the</strong> standard deviation of daily s<strong>to</strong>ck returns over <strong>the</strong> prior 90 days. Annual Return is <strong>the</strong> past 12 month s<strong>to</strong>ck return.<br />
The Amihud measure of illiquidity calculated over <strong>the</strong> previous 90 days.<br />
(1) (2)<br />
∆ Shares ∆ Shares<br />
VARIABLES Outstanding Outstanding<br />
∆ Net Income Volatility - Analyst Forecast t−1 0.53*** 0.58**<br />
(0.17) (0.26)<br />
∆ Market <strong>to</strong> Book t−1 0.03*** 0.02<br />
(0.01) (0.01)<br />
∆ Net Income t−1 0.03*** 0.04**<br />
(0.01) (0.02)<br />
∆ Institutional Ownership t−1 0.15*** 0.20***<br />
(0.00) (0.01)<br />
∆ Market Cap t−1 0.08*** 0.08***<br />
(0.01) (0.01)<br />
∆ Annual Return t−1 0.01 0.01<br />
(0.01) (0.02)<br />
∆ Amihud t−1 -0.02*** -0.03<br />
(0.00) (0.05)<br />
∆ Return Volatility t−1 0.02*** 0.04***<br />
(0.00) (0.01)<br />
∆ Incentive Comp t−1 0.01**<br />
(0.00)<br />
Constant 0.02 -0.14***<br />
(0.02) (0.03)<br />
Year Effects Y Y<br />
Observations 246,077 105,571<br />
R-squared 0.04 0.04<br />
Standard errors clustered by firm in paren<strong>the</strong>ses<br />
*** p
Table 5: Changes in Shares Outstanding: S<strong>to</strong>ck Splits and <strong>EPS</strong><br />
This table presents IV regression models of shares outstanding as a function of firm characteristics. In <strong>the</strong>se specifications, Net Income Error Volatility is instrumented for using<br />
exogenous changes in analyst coverage. Columns 1 presents standardized regression coefficients. Columns 1 and 2 show changes in shares outstanding due <strong>to</strong> splits and o<strong>the</strong>r<br />
than splits respectively. Column 3 controls for high and low s<strong>to</strong>ck prices where High is defined as s<strong>to</strong>cks above $80 and Low is defined as below $20. Columns 4 and 5 show<br />
results for share changes due <strong>to</strong> splits for firms with negative <strong>EPS</strong> and positive <strong>EPS</strong>. Column 6 and 7 shows results for share changes do <strong>to</strong> splits for firms with above median<br />
incentive compensation and below median incentive compensation. Shares outstanding is measured as <strong>the</strong> <strong>to</strong>tal number of shares outstanding (1000’s) from CRSP at <strong>the</strong> end of<br />
<strong>the</strong> quarter. Net Income Error volatility is <strong>the</strong> standard deviation of <strong>the</strong> <strong>the</strong> difference between actual earnings and median IBES forecast of earnings. Market <strong>to</strong> Book is <strong>to</strong>tal<br />
market equity plus <strong>the</strong> book value of <strong>to</strong>tal debt divided by <strong>to</strong>tal assets. Operating income is defined as operating income before interest and depreciation from Compustat at<br />
quarter end. Market Cap is <strong>the</strong> <strong>to</strong>tal market capitalization in millions at <strong>the</strong> quarter end. Institutional ownership is percent ownership of all institutions. Return Volatility is <strong>the</strong><br />
standard deviation of daily s<strong>to</strong>ck returns over <strong>the</strong> prior 90 days. Annual Return is <strong>the</strong> past 12 month s<strong>to</strong>ck return.<br />
(1) (2) (3) (4) (5) (6)<br />
∆ Shares ∆ Shares s ∆ Shares ∆ Shares ∆ Shares ∆ Shares<br />
VARIABLES non-Splits from Splits from Splits from Splits from Splits from Splits<br />
Full Sample Full Sample Negative <strong>EPS</strong> Positive <strong>EPS</strong> Low Incent. Comp High Incent. Comp<br />
∆ Net Income Volatility - Analyst Forecastt−1 136 6,676*** 2,115 7,204*** 4,142 15,867*<br />
(268) (1,709) (1,714) (1,907) (3,146) (9,302)<br />
∆ Market <strong>to</strong> Bookt−1 -11 241*** 38 458*** 989*** 312*<br />
(9) (61) (31) (112) (223) (182)<br />
∆ Net Incomet−1 13 408*** 51 536*** 412* 632*<br />
(14) (106) (43) (145) (230) (332)<br />
∆ Institutional Ownershipt−1 196*** 282*** -36 422*** 752*** 307***<br />
(6) (44) (37) (63) (169) (102)<br />
∆ Market Capt−1 114*** 587*** 412*** 547*** 635*** 332<br />
(10) (72) (107) (95) (112) (277)<br />
∆ Annual Returnt−1 3 -45 -32 -30 -239 162<br />
(10) (62) (25) (94) (249) (297)<br />
∆ Amihudt−1 -40*** 1 11 -20 44 147<br />
(6) (22) (24) (21) (481) (532)<br />
∆ Return Volatilityt−1 22*** 150*** 27* 244*** 464*** 117<br />
(5) (23) (14) (37) (100) (113)<br />
Constant 246*** 255* 281 39 99 713<br />
(28) (139) (204) (184) (271) (738)<br />
Year Effects Y Y Y Y Y Y<br />
Observations 245,267 245,281 60,781 184,144 55,820 51,195<br />
Standard errors clustered by firm in paren<strong>the</strong>ses<br />
*** p
Table 6: Changes in Shares Outstanding: High Cost <strong>to</strong> Splitting<br />
This table presents IV regression models of shares outstanding as a function of firm characteristics. In <strong>the</strong>se specifications, Net Income<br />
Error Volatility is instrumented for using exogenous changes in analyst coverage. Column presents <strong>the</strong> regression specification from table<br />
5 and controls for high and low s<strong>to</strong>ck prices where High is defined as s<strong>to</strong>cks above $80 and Low is defined as below $20. Columns 2 and 3<br />
show show results for share changes due <strong>to</strong> splits for firms with above median illiquidity and below median illiquidity respectively.Shares<br />
outstanding is measured as <strong>the</strong> <strong>to</strong>tal number of shares outstanding (1000’s) from CRSP at <strong>the</strong> end of <strong>the</strong> quarter. Net Income Error<br />
volatility is <strong>the</strong> standard deviation of <strong>the</strong> <strong>the</strong> difference between actual earnings and median IBES forecast of earnings. Market <strong>to</strong> Book<br />
is <strong>to</strong>tal market equity plus <strong>the</strong> book value of <strong>to</strong>tal debt divided by <strong>to</strong>tal assets. Operating income is defined as operating income before<br />
interest and depreciation from Compustat at quarter end. Market Cap is <strong>the</strong> <strong>to</strong>tal market capitalization in millions at <strong>the</strong> quarter end.<br />
Institutional ownership is percent ownership of all institutions. Return Volatility is <strong>the</strong> standard deviation of daily s<strong>to</strong>ck returns over<br />
<strong>the</strong> prior 90 days. Annual Return is <strong>the</strong> past 12 month s<strong>to</strong>ck return.<br />
(1) (2) (3)<br />
∆ Shares ∆ Shares ∆ Shares<br />
VARIABLES Full Sample High Illiquidity Low Illiquidity<br />
∆ Net Income Volatility - Analyst Forecast t−1 4,796** -1,295 6,263**<br />
(1,882) (4,037) (2,477)<br />
∆ Market <strong>to</strong> Book t−1 204*** 21 482***<br />
(60) (15) (119)<br />
∆ Net Income t−1 301*** 27 446***<br />
(110) (82) (159)<br />
∆ Institutional Ownership t−1 280*** 43*** 561***<br />
(43) (10) (88)<br />
∆ Market Cap t−1 451*** 424*** 569***<br />
(57) (51) (90)<br />
∆ Annual Return t−1 -56 -27 -40<br />
(61) (18) (155)<br />
∆ Amihud t−1 5 -9 58,847<br />
(16) (8) (59,775)<br />
∆ Return Volatility t−1 118*** 14** 417***<br />
(19) (6) (66)<br />
High Price t−1 13,008*<br />
(1,335)<br />
Low Price t−1 -101<br />
(244)<br />
Constant -155 -87 2,924<br />
(155) (381) (2,886)<br />
Year Effects Y Y Y<br />
Observations 280,067 146,010 134,048<br />
Standard errors clustered by firm in paren<strong>the</strong>ses<br />
*** p
Table 7: Changes in Shares and <strong>EPS</strong> Outcomes<br />
This table presents results from a difference-in-difference analysis examining <strong>the</strong> association between increases in<br />
shares outstanding and <strong>EPS</strong> outcomes, and earnings management. We distinguish firms that significantly increase<br />
<strong>the</strong> number of shares outstanding in quarter t from those that do not. We define a significant increase as any change<br />
that results in a 25% increase or greater (a split fac<strong>to</strong>r of 5-for-4 or greater). Then we compare how changes in <strong>EPS</strong><br />
outcomes differs across samples. Miss, Beat and Meet are dummies set <strong>to</strong> one if <strong>the</strong> firm’s reported <strong>EPS</strong> was below,<br />
above, or equal <strong>to</strong> <strong>the</strong> median analyst forecast, respectively, zero o<strong>the</strong>rwise. Panel A reports <strong>the</strong> average of <strong>the</strong>se<br />
dummy variables over quarter t − 1 (<strong>the</strong> ‘pre’ period) and that over quarter t + 1 (post). We distinguish firms that<br />
increased shares at t = 0 from those that did not, and report <strong>the</strong> difference across <strong>the</strong>se two groups in <strong>the</strong> differences<br />
across time. Panel B uses <strong>the</strong> firm average over <strong>the</strong> 4 quarters prior <strong>to</strong> t = 0 and compares this <strong>to</strong> <strong>the</strong> firm average<br />
over <strong>the</strong> t + 1 <strong>to</strong> t + 4. t-statistics on <strong>the</strong> differences in differences are clustered at <strong>the</strong> firm-level.<br />
Panel A: 1 quarter pre and post evaluation period<br />
split? pre post dif t-stat<br />
Miss N 16.70% 16.83% 0.13%<br />
Y 21.97% 17.94% -4.03%<br />
-4.16% (-6.64)<br />
Beat N 4.98% 5.01% 0.03%<br />
Y 7.32% 6.08% -1.24%<br />
-1.27% (-3.04)<br />
Meet N 78.33% 78.16% -0.17%<br />
Y 70.71% 75.99% 5.28%<br />
5.45% (7.80)<br />
Panel B: 4 quarter pre and post evaluation period<br />
split? pre post dif t-stat<br />
Miss N 17.71% 17.54% -0.17%<br />
Y 19.75% 18.43% -1.32%<br />
-1.15% (-3.34)<br />
Beat N 4.71% 4.68% -0.03%<br />
Y 7.03% 5.68% -1.35%<br />
-1.32% (-5.86)<br />
Meet N 77.58% 77.78% 0.20%<br />
Y 73.22% 75.89% 2.67%<br />
2.47% (6.29)<br />
42
Table 8: Changes in Shares and Accounting and Real Earnings Management<br />
This table presents results from a difference-in-difference analysis examining <strong>the</strong> association between increases in<br />
shares outstanding and measures of accounting and real earnings management. We distinguish firms that significantly<br />
increase <strong>the</strong> number of shares outstanding in quarter t from those that do not. We define a significant increase as<br />
any change that results in a 25% increase or greater (a split fac<strong>to</strong>r of 5-for-4 or greater). Then we compare how<br />
changes in <strong>the</strong> usage of earnings management <strong>to</strong>ols differs across samples. Discretionary accruals are residuals from<br />
industry <strong>to</strong>tal accruals regressions including performance controls following Ecker et al. (2011). Total accruals are<br />
defined as <strong>the</strong> change in current assets, adjusted for <strong>the</strong> change in cash, minus <strong>the</strong> change in current liabilities,<br />
adjusted for current liabilities used for financing, minus depreciation expense. Measures of real earnings management<br />
are estimated by abnormal cash flow (RealEM CF ), production costs (RealEM P rod ), and expenditure (RealEM CF )<br />
following <strong>the</strong> methodology in Roychowdhury (2006). In Panel A report <strong>the</strong> average of <strong>the</strong> absolute value of <strong>the</strong>se<br />
variables over quarter t − 1 (<strong>the</strong> ‘pre’ period) and compare it <strong>to</strong> that over quarter t + 1 (post). We distinguish firms<br />
that increased shares at t = 0 from those that did not, and report <strong>the</strong> difference across <strong>the</strong>se two groups in <strong>the</strong><br />
differences across time. Panel B uses <strong>the</strong> firm average over <strong>the</strong> 4 quarters prior <strong>to</strong> t = 0 and compares this <strong>to</strong> <strong>the</strong><br />
firm average over <strong>the</strong> t + 1 <strong>to</strong> t + 4. t-statistics on <strong>the</strong> differences across samples are clustered at <strong>the</strong> firm-level.<br />
Panel A: 1 quarter pre and post evaluation period<br />
split? pre post dif<br />
|Accruals T otal | N 3.09% 3.10% 0.01%<br />
Y 3.76% 3.30% -0.46%<br />
-0.47% (-7.07)<br />
|Accruals Disc | N 6.66% 6.67% 0.01%<br />
Y 7.38% 6.59% -0.79%<br />
-0.80% (-4.21)<br />
|RealEM CF | N 2.83% 2.83% 0.01%<br />
Y 3.31% 3.03% -0.28%<br />
-0.29% (-5.50)<br />
|RealEM P rod | N 3.62% 3.63% 0.01%<br />
Y 4.31% 3.96% -0.34%<br />
-0.35% (-6.31)<br />
|RealEM Exp | N 3.43% 3.45% 0.02%<br />
Y 3.84% 3.40% -0.43%<br />
-0.45% (-8.62)<br />
Panel B: 4 quarter pre and post evaluation period<br />
split? pre post dif<br />
|Accruals T otal | N 2.97% 2.88% -0.09%<br />
Y 3.49% 3.17% -0.32%<br />
-0.23% (-3.98)<br />
|Accruals Disc | N 6.14% 6.34% 0.20%<br />
Y 6.65% 6.23% -0.42%<br />
-0.62% (-4.88)<br />
|RealEM CF | N 2.67% 2.63% -0.05%<br />
Y 3.18% 2.89% -0.29%<br />
-0.24% (-6.63)<br />
|RealEM P rod | N 3.52% 3.43% -0.09%<br />
Y 4.21% 3.87% -0.34%<br />
-0.25% (-4.19)<br />
|RealEM Exp | N 3.30% 3.29% -0.01%<br />
Y 3.79% 3.35% -0.44%<br />
-0.43% (-8.86)<br />
43
Table 9: Short-term Accretive and Dilutive Effects<br />
This table presents summary statistics on <strong>the</strong> accretive and dilutive effect of s<strong>to</strong>ck splits on quarter-end <strong>EPS</strong>. A split<br />
is determined <strong>to</strong> be accretive if <strong>the</strong> firm’s <strong>EPS</strong> (measured as Compustat IBADJQ/CSHPRQ rounded <strong>to</strong> <strong>the</strong> penny)<br />
is greater than <strong>the</strong> <strong>EPS</strong> had <strong>the</strong> firm not split (measured as IBADJQ/CSHPRQ*facshr, rounded <strong>to</strong> <strong>the</strong> penny, <strong>the</strong>n<br />
divided by <strong>the</strong> split fac<strong>to</strong>r). The split is dilutive if <strong>the</strong> post-split <strong>EPS</strong> is less than pre-split, and nei<strong>the</strong>r if <strong>the</strong>re is no<br />
difference. Atypical split ratios are defined as any split fac<strong>to</strong>r not in (1.25,1.33,1.5,1.75,2,2.5,3,4,5,10). A split is late<br />
if it occurs after <strong>the</strong> quarter end but before <strong>the</strong> earnings report date. Accretive, nei<strong>the</strong>r, dilutive, atypical, and late<br />
are all indica<strong>to</strong>r variables.<br />
Sample Means<br />
all splits late=0 late=1 atypical=0 atypical=1<br />
N 11447 11016 431 11148 299<br />
accretive 0.318 0.319 0.309 0.315 0.431<br />
nei<strong>the</strong>r 0.393 0.392 0.415 0.401 0.097<br />
dilutive 0.290 0.290 0.276 0.285 0.472<br />
atypical 0.026 0.026 0.030<br />
late 0.037 0.043<br />
late=0 late=1 late=0 late=1<br />
atypical=0 atypical=0 atypical=1 atypical=1<br />
N 10730 418 286 13<br />
accretive 0.316 0.300 0.423 0.615<br />
nei<strong>the</strong>r 0.400 0.426 0.098 0.077<br />
dilutive 0.285 0.275 0.479 0.308<br />
44