statistique, théorie et gestion de portefeuille - Docs at ISFA
statistique, théorie et gestion de portefeuille - Docs at ISFA
statistique, théorie et gestion de portefeuille - Docs at ISFA
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9.1. Les différentes mesures <strong>de</strong> dépendances extrêmes 257<br />
param<strong>et</strong>ric m<strong>et</strong>hod exists, which is based upon the m<strong>at</strong>hem<strong>at</strong>ical results by (Ledford and Tawn 1996, Ledford<br />
and Tawn 1998) and (Coles <strong>et</strong> al. 1999) and has recently been applied by (Poon <strong>et</strong> al. 2001). The m<strong>et</strong>hod<br />
consists in tranforming the original random variables X and Y into Fréch<strong>et</strong> random variables <strong>de</strong>noted by S<br />
and T respectively. Then, consi<strong>de</strong>ring the variable Z = min{S, T }, its survival distribution is:<br />
Pr{Z > z} = d · z 1/η<br />
as z → ∞, (35)<br />
and ¯ λ = 2 · η − 1, with λ = 0 if ¯ λ < 1 or ¯ λ = 1 and λ = d. The param<strong>et</strong>ers η and d can be estim<strong>at</strong>ed<br />
by maximum likelihood, and <strong>de</strong>riving their asymptotic st<strong>at</strong>istics allows one to test wh<strong>et</strong>her the hypothesis<br />
¯λ = 1 can be rejected or not, and consequently, wh<strong>et</strong>her the d<strong>at</strong>a present tail <strong>de</strong>pen<strong>de</strong>nce or not.<br />
We have implemented this procedure and the estim<strong>at</strong>ed values of the coefficient of tail <strong>de</strong>pen<strong>de</strong>nce are given<br />
in table 1 both for the positive and the neg<strong>at</strong>ive tails. Our tests show th<strong>at</strong> we cannot reject the hypothesis of<br />
tail <strong>de</strong>pen<strong>de</strong>nce b<strong>et</strong>ween the four consi<strong>de</strong>red L<strong>at</strong>in American mark<strong>et</strong>s (Argentina, Brazil, Chile and Mexico).<br />
Notice th<strong>at</strong> the positive tail <strong>de</strong>pen<strong>de</strong>nce is almost always slightly smaller than the neg<strong>at</strong>ive one, which could<br />
be linked with the trend asymm<strong>et</strong>ry of (Longin and Solnik 2001), but it turns out th<strong>at</strong> these differences are<br />
not st<strong>at</strong>istically significant. These results indic<strong>at</strong>e th<strong>at</strong>, according to this analysis of the extreme <strong>de</strong>pen<strong>de</strong>nce<br />
coefficient, the propensity of extreme co-movements is almost the same for each pair of stock mark<strong>et</strong>s:<br />
even if the transmission mechanisms of a crisis are different from a country to another one, the propag<strong>at</strong>ion<br />
occur with the same probability overall. Thus, the subsequent risks are the same. In table 2, we also<br />
give the coefficients of tail <strong>de</strong>pen<strong>de</strong>nce estim<strong>at</strong>ed un<strong>de</strong>r the Stu<strong>de</strong>nt’s copula (or in fact any copula <strong>de</strong>rived<br />
from an elliptical distribution) with three dregrees of freedom, given by expression (26). One can observe<br />
a remarkable agreement b<strong>et</strong>ween these values and the non-param<strong>et</strong>ric estim<strong>at</strong>es given in table 1. This<br />
is consistent with the results given by the conditional Spearman’s ρ, for which we have shown th<strong>at</strong> the<br />
Stu<strong>de</strong>nt’s copula seems to reasonably account for the extreme <strong>de</strong>pen<strong>de</strong>nce.<br />
4 Summary and Discussion<br />
Table 3 summarizes the asymptotic <strong>de</strong>pen<strong>de</strong>nces for large v and u of the signed conditional correl<strong>at</strong>ion<br />
coefficient ρ + v , the unsigned conditional correl<strong>at</strong>ion coefficient ρ s v and the correl<strong>at</strong>ion coefficient ρu conditioned<br />
on both variables for the bivari<strong>at</strong>e Gaussian, the Stu<strong>de</strong>nt’s mo<strong>de</strong>l, the Gaussian factor mo<strong>de</strong>l and<br />
the Stu<strong>de</strong>nt’s factor mo<strong>de</strong>l. Our results provi<strong>de</strong> a quantit<strong>at</strong>ive proof th<strong>at</strong> conditioning on exceedance leads<br />
to conditional correl<strong>at</strong>ion coefficients th<strong>at</strong> may be very different from the unconditional correl<strong>at</strong>ion. This<br />
provi<strong>de</strong>s a straightforward mechanism for fluctu<strong>at</strong>ions or changes of correl<strong>at</strong>ions, based on fluctu<strong>at</strong>ions of<br />
vol<strong>at</strong>ility or changes of trends. In other words, the many reported vari<strong>at</strong>ions of correl<strong>at</strong>ion structure might<br />
be in large part <strong>at</strong>tributed to changes in vol<strong>at</strong>ility (and st<strong>at</strong>isical uncertainty).<br />
We also suggest th<strong>at</strong> the distinct <strong>de</strong>pen<strong>de</strong>nces as a function of exceedance v and u of the conditional correl<strong>at</strong>ion<br />
coefficients may offer novel tools for characterizing the st<strong>at</strong>istical multivari<strong>at</strong>e distributions of extreme<br />
events. Since their direct characteriz<strong>at</strong>ion is in general restricted by the curse of dimensionality and the scarsity<br />
of d<strong>at</strong>a, the conditional correl<strong>at</strong>ion coefficients provi<strong>de</strong> reduced robust st<strong>at</strong>istics which can be estim<strong>at</strong>ed<br />
with reasonable accuracy and reliability. In this respect, our empirical results encourage us to assert th<strong>at</strong><br />
a Stu<strong>de</strong>nt’s copula, or more generally and elliptical copula, with a tail in<strong>de</strong>x of about three seems able to<br />
account for the main extreme <strong>de</strong>pen<strong>de</strong>nce properties investig<strong>at</strong>ed here.<br />
Table 4 gives the asymptotic values of ρ + v , ρ s v and ρu for v → +∞ and u → ∞ in or<strong>de</strong>r to compare them<br />
with the tail-<strong>de</strong>pen<strong>de</strong>nce λ.<br />
These two tables only scr<strong>at</strong>ch the surface of the rich s<strong>et</strong>s of measures of tail and extreme <strong>de</strong>pen<strong>de</strong>nces. We<br />
have shown th<strong>at</strong> compl<strong>et</strong>e in<strong>de</strong>pen<strong>de</strong>nce implies the absence of tail <strong>de</strong>pen<strong>de</strong>nce: λ = 0. But λ = 0 does not<br />
19