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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256 9. Mesure <strong>de</strong> la dépendance extrême entre <strong>de</strong>ux actifs financiers<br />
to a non-uniform convergence which makes the or<strong>de</strong>r to two limits non-commut<strong>at</strong>ive: taking first the limit<br />
u → 1 and then ν → ∞ is different from taking first the limit ν → ∞ and then u → 1. In a sense, by taking<br />
first the limit u → 1, we always ensure somehow the power law regime even if ν is l<strong>at</strong>er taken to infinity.<br />
This is different from first “sitting” on the Gaussian limit ν → ∞. It then is a posteriori reasonable th<strong>at</strong> the<br />
absence of uniform convergence is ma<strong>de</strong> strongly apparent in its consequences when measuring a quantity<br />
probing the extreme tails of the distributions.<br />
As an illustr<strong>at</strong>ion, figure 12 represents the coefficient of tail <strong>de</strong>pen<strong>de</strong>nce for the Stu<strong>de</strong>nt’s copula and Stu<strong>de</strong>nt’s<br />
factor mo<strong>de</strong>l as a function of ρ for various value of ν. It is interesting to note th<strong>at</strong> λ equals zero for all<br />
neg<strong>at</strong>ive ρ in the case of the factor mo<strong>de</strong>l, while λ remains non-zero for neg<strong>at</strong>ive values of the correl<strong>at</strong>ion<br />
coefficient for bivari<strong>at</strong>e Stu<strong>de</strong>nt’s variables.<br />
If Y and ɛ have different numbers νY and νɛ of <strong>de</strong>grees of freedom, two cases occur. For νY < νɛ, ɛ is<br />
negligible asymptotically and λ = 1. For νY > νɛ, X becomes asymptotically i<strong>de</strong>ntical to ɛ. Then, X and<br />
Y have the same tail-<strong>de</strong>pen<strong>de</strong>nce as ɛ and Y , which is 0 by construction.<br />
3.4 Estim<strong>at</strong>ion of the coefficient of tail <strong>de</strong>pen<strong>de</strong>nce<br />
It would seem th<strong>at</strong> the coefficient of tail <strong>de</strong>pen<strong>de</strong>nce could provi<strong>de</strong> a useful measure of the extreme <strong>de</strong>pen<strong>de</strong>nce<br />
b<strong>et</strong>ween two random variables which could then be useful for the analysis of contagion b<strong>et</strong>ween<br />
mark<strong>et</strong>s. In<strong>de</strong>ed, either the whole d<strong>at</strong>a s<strong>et</strong> does not exhibit tail <strong>de</strong>pen<strong>de</strong>nce, and a contagion mechanism<br />
seems necessary to explain the occurrence of concomitant large movements during turmoil periods, or it<br />
exhibits tail <strong>de</strong>pen<strong>de</strong>nce so th<strong>at</strong> the usual <strong>de</strong>pen<strong>de</strong>nce structure is such th<strong>at</strong> it is able to produce by itself<br />
concomitant extremes.<br />
Unfortun<strong>at</strong>ely, the empirical estim<strong>at</strong>ion of the coefficient of tail <strong>de</strong>pen<strong>de</strong>nce is a strenuous task. In<strong>de</strong>ed, a<br />
direct estim<strong>at</strong>ion of the conditional probability Pr{X > FX −1 (u) | Y > FY −1 (u)}, which should tend<br />
to λ when u → 1 is impossible to put in practice due to the combin<strong>at</strong>ion of the curse of dimensionality<br />
and the drastic <strong>de</strong>crease of the number of realis<strong>at</strong>ions as u become close to one. A b<strong>et</strong>ter approach consists<br />
in using kernel estim<strong>at</strong>ors, which generally provi<strong>de</strong> smooth and accur<strong>at</strong>e estim<strong>at</strong>ors (Kulpa 1999, Li <strong>et</strong><br />
al. 1998, Scaill<strong>et</strong> 2000). However, these smooth estim<strong>at</strong>ors lead to differentiable estim<strong>at</strong>ed copulas which<br />
have autom<strong>at</strong>ically vanishing tail <strong>de</strong>pen<strong>de</strong>nce. In<strong>de</strong>ed, in or<strong>de</strong>r to obtain a non-vanishing coefficient of tail<br />
<strong>de</strong>pen<strong>de</strong>nce, it is necessary for the corresponding copula to be non-differentiable <strong>at</strong> the point (1, 1) (or <strong>at</strong><br />
(0, 0)). An altern<strong>at</strong>ive is then the fully param<strong>et</strong>ric approach. One can choose to mo<strong>de</strong>l <strong>de</strong>pen<strong>de</strong>nce via a<br />
specific copula, and thus to d<strong>et</strong>ermine the associ<strong>at</strong>ed tail <strong>de</strong>pen<strong>de</strong>nce (Longin and Solnik 2001, Malevergne<br />
and Sorn<strong>et</strong>te 2001, P<strong>at</strong>ton 2001). The problem with such a m<strong>et</strong>hod is th<strong>at</strong> the choice of the param<strong>et</strong>eriz<strong>at</strong>ion<br />
of the copula amounts to choose a priori wh<strong>et</strong>her or not the d<strong>at</strong>a presents tail <strong>de</strong>pen<strong>de</strong>nce.<br />
In fact, there exist three ways to estim<strong>at</strong>e the tail <strong>de</strong>pen<strong>de</strong>nce coefficient. The two first ones are specific to a<br />
class of copulas or of mo<strong>de</strong>ls, while the last one is very general, but obvioulsy less accur<strong>at</strong>e. The first m<strong>et</strong>hod<br />
is only reliable when it is known th<strong>at</strong> the un<strong>de</strong>rlying copula is Archimedian (see (Joe 1997) or (Nelsen 1998)<br />
for the <strong>de</strong>finition). In such a case, a limit theorem established by (Juri and Wüthrich 2002) allows to estim<strong>at</strong>e<br />
the tail <strong>de</strong>pen<strong>de</strong>nce. The problem is th<strong>at</strong> it is not obvious th<strong>at</strong> the Archimedian copulas provi<strong>de</strong> a good<br />
represent<strong>at</strong>ion of the <strong>de</strong>pen<strong>de</strong>nce structure for financial ass<strong>et</strong>s. For instance, the Achimedian copulas are<br />
generally inconsistent with a represent<strong>at</strong>ion of ass<strong>et</strong>s by factor mo<strong>de</strong>ls. In such case, a second m<strong>et</strong>hod<br />
provi<strong>de</strong>d by (Malevergne and Sorn<strong>et</strong>te 2002) offers good results allowing to estim<strong>at</strong>e the tail <strong>de</strong>pen<strong>de</strong>nce in<br />
a semi-param<strong>et</strong>ric way, which solely relies on the estim<strong>at</strong>ion of marginal distributions, a significantly easier<br />
task.<br />
When none of these situ<strong>at</strong>ions occur, or when the factors are too difficult to extract, a third and fully non-<br />
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