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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38 3 L<strong>in</strong>ear Gaussian <strong>state</strong> <strong>space</strong> <strong>models</strong> and the Kalman filter<br />
3.6.2 Goodness <strong>of</strong> fit<br />
Measures <strong>of</strong> the goodness <strong>of</strong> fit are usually computed on the basis <strong>of</strong> forecast errors.<br />
The basic goodness <strong>of</strong> fit measure for time series <strong>models</strong> is the prediction error variance,<br />
which also serves as an <strong>in</strong>put to calculate the coefficient <strong>of</strong> determ<strong>in</strong>ation. A comparison<br />
between <strong>models</strong> with different numbers <strong>of</strong> parameters is commonly made on the basis<br />
<strong>of</strong> <strong>in</strong>formation criteria.<br />
3.6.2.1 Prediction error variance<br />
In case <strong>of</strong> time-homogeneity, the prediction error variance (p.e.v.) is def<strong>in</strong>ed as<br />
σ 2 = σ 2 ∗ ¯ f, (3.87)<br />
where ¯ f represents the value to which ft converges <strong>in</strong> steady-<strong>state</strong>. When a concentrated<br />
likelihood function is used with σ 2 ∗ be<strong>in</strong>g estimated by (3.61), σ2 can be estimated as<br />
˜σ 2 = ˜σ 2 ∗ ¯ f. (3.88)<br />
The <strong>in</strong>corporation <strong>of</strong> regression effects <strong>in</strong>to a model slightly changes the def<strong>in</strong>ition <strong>of</strong> the<br />
. When deal<strong>in</strong>g with time-vary<strong>in</strong>g regression <strong>models</strong>, the ML estimator<br />
estimator <strong>of</strong> σ2 ∗<br />
<strong>of</strong> σ2 ∗ for stochastic βt is a function <strong>of</strong> the generalized recursive residuals:<br />
s 2 ∗<br />
= (T − d − k)−1<br />
T�<br />
t=d+k+1<br />
˜v †2<br />
t , (3.89)<br />
where k is equal to the dimension <strong>of</strong> the vector <strong>of</strong> explanatory variables. For fixed β t ,<br />
the ML estimator <strong>of</strong> σ 2 ∗ depends on the GLS residuals:<br />
˜σ +2<br />
∗<br />
= (T − d)−1<br />
T�<br />
t=d+1<br />
˜v +2<br />
t , (3.90)<br />
where the sums <strong>of</strong> squares are identical <strong>in</strong> both cases. Tak<strong>in</strong>g (3.89) and (3.90) <strong>in</strong>to<br />
account, the prediction error variance for <strong>models</strong> that conta<strong>in</strong> explanatory variables can<br />
be estimated as<br />
or as<br />
s 2 = s 2 ∗ ¯ f, (3.91)<br />
˜σ +2 = ˜σ +2<br />
∗ ¯ f. (3.92)<br />
Accord<strong>in</strong>g to Harvey (1989, ¢ 7.4.3) the prediction error variance can be approximated<br />
for large samples <strong>in</strong> terms <strong>of</strong> the unstandardized GLS residuals as def<strong>in</strong>ed <strong>in</strong> (3.85):<br />
˜σ 2 =<br />
¯ f<br />
T − d<br />
T�<br />
t=d+1<br />
˜v +2<br />
t<br />
= 1<br />
T − d<br />
T�<br />
t=d+1<br />
v +2<br />
t<br />
ft<br />
¯f ≈ 1<br />
T − d<br />
T�<br />
t=d+1<br />
v +2<br />
t . (3.93)