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Applications of state space models in finance

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6.4 Conclud<strong>in</strong>g remarks 119<br />

<strong>of</strong> 150 weekly observations is considered <strong>in</strong> the second step <strong>of</strong> the proposed evaluation<br />

procedure.<br />

6.3.3.2 Step II: Out-<strong>of</strong>-sample period <strong>of</strong> ten years to identify the overall best model<strong>in</strong>g<br />

approach<br />

Table 6.9 summarizes the calculated mean absolute and squared errors for the RW,<br />

GRW and MMR model, respectively, by report<strong>in</strong>g their averages across all sectors; for<br />

a comprehensive sectoral breakdown, see Table C.6 <strong>in</strong> the appendix. Accord<strong>in</strong>g to the<br />

considered average mean errors, the out-<strong>of</strong>-sample forecast<strong>in</strong>g performance <strong>of</strong> all three<br />

<strong>models</strong> over the last ten years <strong>of</strong> the given sample is very similar. Even though the<br />

average MAE is slightly lower for the MMR model and the average MSE is lowest for<br />

the RW model, based on these results neither approach significantly stands out. This<br />

is also confirmed by look<strong>in</strong>g at the relative ranks, which <strong>in</strong>dicate that the different<br />

model<strong>in</strong>g approaches yield an average rank <strong>of</strong> around two.<br />

Table 6.9: Average out-<strong>of</strong>-sample MAE and MSE across sectors (520 samples).<br />

Mean absolute error (×10 2 ) Mean squared error (×10 4 )<br />

RW GRW MMR RW GRW MMR<br />

Average error 1.311 1.310 1.309 3.584 3.600 3.589<br />

Average rank 2.33 2.11 1.94 1.94 2.22 2.17<br />

When Spearman’s rank correlation coefficient is employed to evaluate the forecast<strong>in</strong>g<br />

performance <strong>in</strong> a cross-sectional context, the RW model has a small advantage over<br />

its competitors. While Figure 6.14 illustrates that the realized rank correlations are<br />

similarly distributed for all three <strong>models</strong>, the median rank correlation as well as the<br />

<strong>in</strong>formation criteria <strong>of</strong> the RW model are slightly higher.<br />

Overall, neither the less parsimonious mov<strong>in</strong>g mean revert<strong>in</strong>g nor the generalized random<br />

walk model, which are both motivated by their respective capability to capture<br />

volatility clusters and outliers, yield a forecast<strong>in</strong>g advantage over the random walk specification.<br />

This result suggests that heteroskedasticity and outliers can be considered as<br />

be<strong>in</strong>g “third-order” problems <strong>in</strong> the context <strong>of</strong> apply<strong>in</strong>g the Kalman filter to model the<br />

time-vary<strong>in</strong>g behavior <strong>of</strong> systematic risk for pan-European sector <strong>in</strong>dices.<br />

6.4 Conclud<strong>in</strong>g remarks<br />

Despite the considerable empirical evidence that systematic risk is not constant over<br />

time, only few studies deal with the explicit model<strong>in</strong>g <strong>of</strong> the time-vary<strong>in</strong>g behavior <strong>of</strong><br />

betas. Previous studies with a focus on Australia, India, New Zealand, the U.S. and<br />

the UK primarily employed Kalman filter and GARCH based techniques. The empirical<br />

analysis presented <strong>in</strong> this chapter contributes an <strong>in</strong>vestigation <strong>of</strong> time-vary<strong>in</strong>g betas for<br />

pan-European <strong>in</strong>dustry portfolios. The spectrum <strong>of</strong> model<strong>in</strong>g techniques is extended by<br />

(i) <strong>in</strong>corporat<strong>in</strong>g two Markov switch<strong>in</strong>g approaches, whose capabilities to model time-

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