Estimation of Educational Borrowing Constraints Using Returns to ...
Estimation of Educational Borrowing Constraints Using Returns to ...
Estimation of Educational Borrowing Constraints Using Returns to ...
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educational borrowing constraints 169<br />
and<br />
′ ′ ′ ′ ′<br />
X iG 2 { XTibT1 a 1(XWibW XL0ib L0) a 2 a 1 XTib T 0, (29)<br />
˜<br />
e { a log (R ) n av n , (30)<br />
2i 3 i 1i 1 0i 0i<br />
so that G1and G2are defined appropriately. Individuals choose schooling<br />
option 1 if V1i V0i 1 0, and option 0 otherwise. Note that e1i<br />
enters the<br />
expression inside log (7) in equation (26) and is correlated with the<br />
residual e2i both through the correlation between v0i and v1i<br />
and because<br />
log (R i ) enters both residuals.<br />
The vec<strong>to</strong>r (X i, X Ci) is observable <strong>to</strong> the analyst but (v 1i, v 0i,<br />
log (R i), n 1i, n 0i) is not. We assume that (X i, X Ci)<br />
is independent <strong>of</strong><br />
(v 1i, v 0i, log(R i), n 1i, n 0i). The selection equation (26) has three indices<br />
′ ′ ′<br />
(X iG 1, X iG 2, X Cib C) and two error terms (e 1i, e 2i)<br />
. The three degrees <strong>of</strong><br />
freedom represented by these index functions are sufficient <strong>to</strong> trace out<br />
the joint distribution <strong>of</strong> (e 1i, e 2i)<br />
.<br />
Equations (28) and (30) show that these indices cannot also identify<br />
the distribution <strong>of</strong> log (R i)<br />
from the distribution <strong>of</strong> v1i. However, since<br />
wages depend on v1i<br />
but not on R i, the wage equation given by (18)<br />
provides sufficient variation <strong>to</strong> trace out the distribution <strong>of</strong> log (R i ) up<br />
<strong>to</strong> a location normalization.<br />
Theorem 1 contained in the appendix (available at http://www<br />
.econ.northwestern.edu/faculty/taber) proves nonparametric identification<br />
<strong>of</strong> the joint distribution <strong>of</strong> the error terms from the schooling<br />
choice and wage equations, (e 1i, e 2i, u 1it)<br />
, using two exclusion restrictions,<br />
one for opportunity costs and one for direct costs. 31 Once this joint<br />
distribution is identified, we can identify the conditional expectation<br />
E(u 1itFe 1i) p E(v1iFv 1i log (R i)).<br />
The appendix further demonstrates that this conditional expectation<br />
can be used <strong>to</strong> estimate the distribution <strong>of</strong> Ri<br />
when Ri<br />
is independent<br />
<strong>of</strong> v 1i . Thus the entire distribution <strong>of</strong> interest rates faced by students is<br />
identified up <strong>to</strong> a normalization.<br />
Intuition for this result follows from the fact that the form <strong>of</strong> the<br />
selection bias<br />
′ ′ ′<br />
E(v1iFa 1 log {exp [X iG1 v1i log (R i)] X Cib C} X iG2 e2i<br />
1 0,<br />
′ ′ ′<br />
X iG 1, X Cib C, X iG 2) (31)<br />
depends on the realized value <strong>of</strong> college costs. This expression is complicated<br />
and depends on the full distribution <strong>of</strong> (v 1i, R i, e 2i)<br />
. Under the<br />
same logic outlined in Section III, the term v1i log (R i)<br />
is more im-<br />
31 ′<br />
With the notation used above, the first type <strong>of</strong> exclusion restriction affects X i G 2 , but<br />
′ ′ ′ ′ ′<br />
not X G or X b ; the second enters X b but not X G or X G .<br />
i 1 Ci C Ci C i 2 i 1