Applications of state space models in finance
Applications of state space models in finance
Applications of state space models in finance
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60 5 Conditional heteroskedasticity <strong>models</strong><br />
lagged squared shocks to the function <strong>of</strong> the conditional variance. However, allow<strong>in</strong>g q to<br />
become large results <strong>in</strong> many parameters to be estimated. This would be <strong>in</strong>feasible given<br />
the positiveness and stationarity conditions that have to be imposed. In many cases, an<br />
ARCH(q) process is not capable <strong>of</strong> captur<strong>in</strong>g both the height and shape dimensions <strong>of</strong><br />
the autocorrelation function; further generalization is required (cf. Pagan 1996).<br />
By <strong>in</strong>clud<strong>in</strong>g a lagged conditional variance term to the conditional variance function,<br />
Bollerslev (1986) generalized the ARCH(q) model. The GARCH(p, q) class <strong>of</strong> <strong>models</strong><br />
allows for a more flexible lag structure and for longer memory effects:<br />
ht = ω +<br />
q�<br />
i=1<br />
γiɛ 2 t−i +<br />
p�<br />
j=1<br />
δjht−j<br />
= ω + γ(L)ɛ 2 t + δ(L)ht, (5.5)<br />
with ω > 0 and L denot<strong>in</strong>g the lag operator, where γ(L) = γ1L + · · · + γqL q and<br />
δ(L) = δ1L + · · · + δpL p . For δj = 0 and j = 1, . . . , p, the GARCH(p, q) process reduces<br />
to an ARCH(q) model. Follow<strong>in</strong>g Bollerslev et al. (1994) the process is well-def<strong>in</strong>ed if<br />
all parameters <strong>in</strong> the <strong>in</strong>f<strong>in</strong>ite-order autoregressive representation<br />
ht = (1 − δ(L)) −1 γ(L)ɛ 2 t<br />
(5.6)<br />
are nonnegative. It is assumed that all the roots <strong>of</strong> 1−δ(L) lie outside the unit circle. The<br />
condition for covariance-stationary <strong>of</strong> the GARCH(p, q) process is �q i=1 γi+ �p j=1 δj < 1.<br />
5.1.1.1 Statistical properties<br />
A specification with p = q = 1 represents the simplest and most common GARCH<br />
model. As it is found to be sufficient for most empirical applications (cf. Bollerslev<br />
et al. 1992), only the GARCH(1,1) process will be considered <strong>in</strong> the follow<strong>in</strong>g. The<br />
GARCH(1,1) model corresponds to an ARCH(∞) process, <strong>in</strong> which the conditional<br />
variance is guaranteed to be nonnegative with ω > 0, γ1 > 0 and δ1 ≥ 0. Under the<br />
assumption <strong>of</strong> covariance-stationarity, which is assured for γ1 +δ1 < 1, the unconditional<br />
variance <strong>of</strong> ɛt is def<strong>in</strong>ed. It can be calculated as<br />
σ 2 ω<br />
=<br />
. (5.7)<br />
1 − γ1 − δ1<br />
If (γ1 + δ1) 2 + 2γ 2 1 < 1, the unconditional fourth moment <strong>of</strong> ɛt exists. For normally<br />
distributed zt, the kurtosis <strong>of</strong> ɛt is def<strong>in</strong>ed as<br />
Kɛ = 3 � 1 − (γ1 + δ1) 2�<br />
1 − (γ1 + δ1) 2 − 2γ2 . (5.8)<br />
1<br />
The kurtosis <strong>of</strong> ɛt is always greater than three. It captures some <strong>of</strong> the excess kurtosis<br />
usually <strong>in</strong>herent to f<strong>in</strong>ancial time series.<br />
When the GARCH(1,1) model is applied to high-frequency data, a common f<strong>in</strong>d<strong>in</strong>g is<br />
that current <strong>in</strong>formation has an impact on conditional variance forecasts for any horizon.<br />
This leads to a sum <strong>of</strong> γ1 and δ1 that is close or equal to unity. Engle and Bollerslev