Etude des marchés d'assurance non-vie à l'aide d'équilibres de ...
Etude des marchés d'assurance non-vie à l'aide d'équilibres de ...
Etude des marchés d'assurance non-vie à l'aide d'équilibres de ...
You also want an ePaper? Increase the reach of your titles
YUMPU automatically turns print PDFs into web optimized ePapers that Google loves.
tel-00703797, version 2 - 7 Jun 2012<br />
4.4. Focus on the <strong>de</strong>pen<strong>de</strong>nce structure<br />
any bivariate pair (X, Y ): B is not a distribution, whereas D is a distribution function but<br />
not a copula.<br />
Let us now consi<strong>de</strong>r two exponential random variables that are conditionally in<strong>de</strong>pen<strong>de</strong>nt<br />
given a factor Θ. We choose to focus here only on the bivariate case. Suppose that these<br />
variables are discretized by taking their integer parts. We will see that the two resulting<br />
random variables have geometric distributions; these are, of course, correlated. Our purpose<br />
in Subsections 4.4.1 - 4.4.4 below is precisely to study the <strong>de</strong>pen<strong>de</strong>nce involved.<br />
4.4.1 Depen<strong>de</strong>nce induced by the mixing approach<br />
We start by comparing the joint distributions of two mixed exponential random variables<br />
and of geometric approximations obtained by discretization.<br />
Continous case<br />
Now, consi<strong>de</strong>r Yi, i = 1, 2 to be conditionnaly in<strong>de</strong>pen<strong>de</strong>nt exponential random variables,<br />
i.e. Yi|Θ = θ i.i.d.<br />
∼ E(θ). We have<br />
FY1 (x) = P (Y1 ≤ x) =<br />
∞<br />
P (Y1 ≤ x|Θ = θ)dFΘ(θ) = 1 − LΘ(x),<br />
0<br />
where LΘ stands for the Laplace transform of the random variable Θ, assuming LΘ exists.<br />
Using this formulation, we can check that the random variable FYi (Yi) is uniformly distributed.<br />
In<strong>de</strong>ed we have<br />
P (FY1 (Y1) ≤ u) = P (Y1 ≤ L −1<br />
Θ<br />
−1<br />
(1 − u)) = 1 − LΘ(LΘ (1 − u)) = u.<br />
Furthermore, the (unique) copula of the couple (Y1, Y2) can be <strong>de</strong>rived by<br />
CY1,Y2 (u, v) = P (FY1 (Y1) ≤ u, FY2 (Y2) ≤ v) = P (Y1 ≤ L −1<br />
=<br />
∞<br />
0<br />
(1 − e −θL−1<br />
Θ (1−u) )(1 − e −θL−1<br />
Θ (1−v) )dFΘ(θ).<br />
Hence the copula function is given by<br />
CY1,Y2 (u, v) = u + v − 1 + LΘ<br />
Θ (1 − u), Y2 ≤ L −1<br />
Θ<br />
(1 − v))<br />
−1<br />
LΘ (1 − u) + L−1<br />
Θ (1 − v) . (4.10)<br />
We retrieve the fact that the couple (Y1, Y2) has an Archime<strong>de</strong>an survival copula with generator<br />
L −1<br />
Θ , see, e.g., Albrecher et al. (2011). In other words, the joint distribution of the tail is given<br />
by<br />
P ( ¯ FY1 (Y1) > u, ¯ FY2 (Y2)<br />
−1<br />
> v) = LΘ LΘ (u) + L−1<br />
Θ (v) .<br />
From Theorem 4.6.2 of Nelsen (2006), the above expression can be exten<strong>de</strong>d to any dimension.<br />
A n-dimension function C(u1, . . . , un) <strong>de</strong>fined by a generator φ and C(u1, . . . , un) =<br />
φ−1 (φ(u1) + · · · + φ(un)) is a n-copula for all n ≥ 2 if and only if the generator φ−1 is<br />
completely monotone, i.e. for all k ∈ N,<br />
(−1) k dk φ −1<br />
dt k (t) ≥ 0.<br />
As the generator is φ−1 (t) = LΘ(t) in our mo<strong>de</strong>l, then the Laplace transform is completely<br />
monotone. In particular, LΘ is a <strong>de</strong>creasing convex function. As φ is the generator of an<br />
Archime<strong>de</strong>an copula, φ is a convex <strong>de</strong>creasing function. Since φ(t) = L −1<br />
Θ (t), L−1<br />
Θ is also a<br />
convex <strong>de</strong>creasing function.<br />
197