Abstract
This paper proposes a new rank-based test of extreme-value dependence. The procedure is based on the first three moments of the bivariate probability integral transform of the underlying copula. It is seen that the test statistic is asymptotically normal and its finite- and large-sample variance are calculated explicitly. Consistent plug-in estimators for the variance are proposed, and a fast algorithm for their computation is given. Although it is shown via counterexamples that no test based on the probability integral transform can be consistent, the proposed procedure achieves good power against common alternatives, both in finite samples and asymptotically.
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Grants from the Natural Sciences and Engineering Research Council and the Fonds québécois de la recherche sur la nature et les technologies are gratefully acknowledged.
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Appendices
Appendix A
Proof of Proposition 1
Since \(\mathrm{E}(I_{ij})=\mu _1\), \(\mathrm{E}(I_{ij}I_{kj})=\mu _2\) as well as \(\mathrm{E}(I_{ij}I_{kj}I_{lj})=\mu _3\), it is immediate that \(\mathrm{E}(S_{3n}+1)=4\mu _1+9\mu _2-16\mu _3\). Hence,
Next,
can be expanded as follows:
Expectations of the first three terms are computed in Appendix A of Ben Ghorbal et al. (2009) and lead to the terms involving \(A_n\), \(B_n\) and \(C_n\). Expectations of the remaining terms can be calculated analogously by multiplying out the sums, distinguishing cases according to the number of distinct indices and taking expectations. For example, applying these steps to the fourth term leads to Table 6. Tallying the terms listed therein, one finds
The same strategy leads to the expectations of the remaining two terms. There are 71 and 209 cases to be distinguished in the computation of the expectation of the fifth and the sixth term, respectively. A detailed list of all cases fills several pages and is available from the authors upon request. However, many indicator products are identical up to index relabeling and have the same expectation. For example,
Tables 7 and 8 present a list of all parameters involved in the formula for \(E_n\) and \(F_n\) respectively, along with typical terms having these parameters as expectations. The number of terms leading to the same expectation is also given. Summing up, one finds
as well as
This completes the proof. \(\square \)
Proof of Proposition 2
From Proposition 1, one may write \(n\cdot \text{ var}(S_{3n})=\alpha _n+\beta _n+\gamma _n\), where
as well as
and
It is easy to see that as \(n\rightarrow \infty \), \(\alpha _n \rightarrow 0\) while
and
Collecting the terms yields the result. \(\square \)
Appendix B: An algorithm for computing the plug-in estimators of the finite and large-sample variance of \(S_{3n}\)
Let \((I_{ij})\) be an \(n\times n\) matrix with entries \(I_{ij}=\mathbf{1}(X_i\le X_j,Y_i\le Y_j)\). Let also \(J\) be the \(n\times n\) identity matrix and write \(\mathbf{1}\) for an \(n\times 1\) vector of 1’s. Given arbitrary \(k\times \ell \) matrices \(A=(A_{ij})\) and \(B=(B_{ij})\), denote the sum of all elements of \(A\) by
and the Hadamard (or entrywise) product of \(A\) and \(B\) by \(A\star B\).
To compute the plug-in estimators of the finite- and large-sample variance of \(S_{3n}\), respectively, proceed as follows.
-
Step 0.
Compute \(M=(I_{ij})-J\), \(A=M\mathbf{1}\), \(B=M^\top \mathbf{1}\), \(N=M^\top M\), \(P=MM^\top -\mathrm{diag}(MM^\top )\), \(Q=N-\mathrm{diag}(N)\).
-
Step 1.
For \(k\in \{1, \ldots ,6\}\), set \(b_k=\Sigma {(B_k)}\), where \(B_k=B\star \cdots \star B\) is the \(k\)-fold Hadamard product of \(B\). Let also \(a_2=\Sigma {(A\star A)}\), \(c=\Sigma {(A\star B_2)}\), \(d=\Sigma {(A\star B_3)}\). Also, for \(i\in \{2,3\}\), compute \(N_i=N\star \cdots \star N\) as the \(i\)-fold Hadamard product of \(N\).
-
Step 2.
Set \(m_1=b_1\) and compute \(t_1=\Sigma {(A\star B)}\), \(t_2=a_2-b_1\).
-
Step 3.
Compute sequentially
$$\begin{aligned} \begin{array}{ll} m_2&= b_2-m_1,\\ m_3&= b_3-m_1-3m_2,\\ m_4&= b_4-m_1-7m_2-6m_3,\\ m_{11}&= m_1^2-b_2-2t_1-t_2,\quad \end{array}\quad \begin{array}{ll} t_3&= c-t_1,\\ t_4&= B^\top MB-2t_1,\\ t_5&= A^\top MB-b_2-t_1-t_2,\\ t_8&= \Sigma (PP^\top )-m_2. \end{array} \end{aligned}$$ -
Step 4.
Compute sequentially
$$\begin{aligned} t_6&= B_2^\top { MB} - 2c- t_3 -t_4,\\ t_7&= ({ MB}-A)^\top { MB} + b_2-b_3-c-t_3-t_5-t_8,\\ m_{12}&= -2(A+B)^\top { MB} + 2a_2-2b_1-(b_1)^2+3b_2+b_1b_2-b_3+4t_1-t_3,\\ m_{22}&= (2A+2B-4B_2-2{ MB})^\top { MB} - 2b_2 - b_1b_2 + (b_2)^2 + 3b_3-b_4\\&+ 7c - m_{12} - 3t_1 - 2t_7. \end{aligned}$$ -
Step 5.
Compute sequentially
$$\begin{aligned} m_5&= b_5-10m_4-25m_3-15m_2-m_1,\\ m_6&= b_6-15m_5-65m_4-90m_3-31m_2-m_1,\\ t_9&= B^\top M(B_2-3B)+2t_1-2t_4,\\ t_{10}&= A^\top M(B_2-3B)+2a_2-m_3-2t_4,\\ t_{11}&= d-c-2t_3,\\ t_{12}&= B_2^\top M(B_2-3B)+2c-2t_3-2t_4-4t_6-t_9,\\ t_{15}&= \Sigma {(B^\top N_2)}-B^\top \mathrm{diag}(N_2)-A^\top { MB} + b_2 -2t_8-t_3, \\ t_{13}&= ({ MB}_2-{ MB}-B_2)^\top { MB}+b_3-b_4-3t_3-t_4-2t_5-t_6\\&-2t_7-2t_8-t_{10}-t_{11}-2t_{15},\\ t_{14}&= (B_3-3B_2+2B)^\top { MB}-4t_{11},\\ t_{17}&= (B_3-3B_2+2B)^\top { MB}_2-16t_{11}-9t_{14},\\ t_{19}&= \Sigma {N_3}-\Sigma (N_2)-2t_8,\\ t_{18}&= B^\top N_2B-B_2^\top \mathrm{diag}(N_2)-({ MB})^\top { MB} \\&+b_3-4t_3-4t_8-2t_{11}-4t_{15}-t_{19},\\ t_{16}&= ({ MB}_2-3{ MB}+2A)^\top { MB}_2-2(B_3-{ MB})^\top { MB} \\&-2(B^\top N_2B-B_2^\top \mathrm{diag}(N_2))+4d-4b_3\\&+3b_4-b_5+8t_3+8t_8-t_{10}-3t_{11}-3t_{13} -2t_{14}+2t_{15}-2t_{18},\\ m_{13}&= b_1(2b_1-3b_2+b_3)-2b_2+3b_3-b_4-6t_4-3t_9-3t_{10}-t_{11},\\ m_{23}&= b_2(2b_1-3b_2+b_3)-2b_3+3b_4-b_5-6c-3B_2^\top M(B_2-3B)\\&-3t_{10}-7t_{11}-6t_{13}-2t_{14} -6t_{15}-m_{13},\\ m_{33}&= (9MB-3MB_2-6A-4B_3+3B_2-2B)^\top { MB}_2+15B_3^\top { MB}\\&+b_3(2b_1-3b_2+b_3)+6b_3-11b_4+6b_5-b_6-18d-9t_{13}-9t_{14}\\&-6t_{16}-2t_{17}-6t_{18}-m_{13}-3m_{23}. \end{aligned}$$ -
Step 6.
Set \(n_1=n_2=3\), \(n_3=n_4=n_5=n_8=4\), \(n_6=n_7=n_9=n_{10}=n_{11}=n_{15}=n_{19}=5\), \(n_{12}=n_{13}=n_{14}=n_{18}=6\), and \(n_{16}=n_{17}=7\). Then compute
$$\begin{aligned} \hat{\mu }_i=m_i\cdot (n)_{i+1},\quad \hat{\mu }_{ij}=m_{ij}\cdot (n)_{i+j+2},\quad \hat{\theta }_{i}=t_{i}\cdot (n)_{n_i}, \end{aligned}$$where \((n)_i\) represents the falling factorial \(n(n-1)(n-2)\cdots (n-i+1)\).
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Du, Y., Nešlehová, J. A moment-based test for extreme-value dependence. Metrika 76, 673–695 (2013). https://doi.org/10.1007/s00184-012-0410-z
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DOI: https://doi.org/10.1007/s00184-012-0410-z
Keywords
- Extreme-value copula
- Ghoudi–Khoudraji–Rivest test
- Kendall’s distribution
- Kendall’s tau
- Test of extremeness
- \(U\)-statistic