K: Kendall Distribution Function for Archimedean Copulas

Description

The Kendall distribution of an Archimedean copula is defined by $$K(u) = P(C(U_1,U_2,\dots,U_d) \le u),$$ where $u \in [0,1]$, and the $d$-dimensional $(U_1,U_2,\dots,U_d)$ is distributed according to the copula $C$. Note that the random variable $C(U_1,U_2,\dots,U_d)$ is known as “probability integral transform”. Its distribution function $K$ is equal to the identity if $d = 1$, but is non-trivial for $d \ge 2$.

Kn() computes the empirical Kendall distribution function, pK() the distribution function (so $K()$ itself), qK() the quantile function, dK() the density, and rK() random number generation from $K()$ for an Archimedean copula.

Usage


Kn(u, x, method = c("GR", "GNZ")) # empirical Kendall distribution function
dK(u, copula, d, n.MC = 0, log.p = FALSE) # density
pK(u, copula, d, n.MC = 0, log.p = FALSE) # df
qK(p, copula, d, n.MC = 0, log.p = FALSE, # quantile function
   method = c("default", "simple", "sort", "discrete", "monoH.FC"),
   u.grid, xtraChecks = FALSE, …)
rK(n, copula, d) # random number generation

Arguments

evaluation point(s) (in $[0,1]$).

data (in the $d$-dimensional space) based on which the Kendall distribution function is estimated.

copula

'>acopula with specified parameter, or (currently for rK only) a '>outer_nacopula.

dimension (not used when copula is an '>outer_nacopula).

n.MC

integer, if positive, a Monte Carlo approach is applied with sample size equal to n.MC to evaluate the generator derivatives involved; otherwise (n.MC = 0) the exact formula is used based on the generator derivatives as found by Hofert et al. (2012).

log.p

logical; if TRUE, probabilities $p$ are given as $\log p$.

probabilities or log-probabilities if log.p is true.

method

for qK(), character string for the method how to compute the quantile function of $K$; available are:

"default": default method. Currently chooses method="monoH.FC" with u.grid = 0:128/128. This is fast but not too accurate (see example).
"simple": straightforward root finding based on uniroot.
"sort": root finding based on uniroot but first sorting u.
"discrete": first, $K$ is evaluated at the given grid points u.grid (which should contain 0 and 1). Based on these probabilities, quantiles are computed with findInterval.
"monoH.FC": first, $K$ is evaluated at the given grid points u.grid. A monotone spline is then used to approximate $K$. Based on this approximation, quantiles are computed with uniroot.

For Kn(), character string indicating the method according to which the empirical Kendall distribution is computed; available are:

"GR": the default. Computed as in Genest and Rivest (1993, Equations (4) and (5)).
"GNZ": computed as in Genest et al. (2011, Equation (19) and Lemma 1); this is guaranteed to satisfy that the estimator lies above the diagonal at any point in [0,1).

u.grid

(for method="discrete":) The grid on which $K$ is evaluated, a numeric vector.

xtraChecks

experimental logical indicating if extra checks should be done before calling uniroot() in some cases.

…

additional arguments passed to uniroot (for method="default", method="simple", method="sort", and method="monoH.FC") or findInterval (for method="discrete"), notably tol (uniroot) for increased accuracy.

sample size for rK.

Value

The empirical Kendall distribution function, density, distribution function, quantile function and random number generator.

Details

For a completely monotone Archimedean generator $\psi$, $$K(u)=\sum_{k=0}^{d-1} \frac{\psi^{(k)}(\psi^{-1}(u))}{k!} (-\psi^{-1}(u))^k,\ u\in[0,1];$$ see Barbe et al. (1996). The corresponding density is $$\frac{(-1)^d\psi^{(d)}(\psi^{-1}(u))}{(d-1)!} (-(\psi^{-1})'(u))(\psi^{-1}(u))^{d-1}$$

References

Barbe, P., Genest, C., Ghoudi, K., and R<U+00E9>millard, B. (1996), On Kendall's Process, Journal of Multivariate Analysis 58, 197--229.

Hofert, M., M<U+00E4>chler, M., and McNeil, A. J. (2012). Likelihood inference for Archimedean copulas in high dimensions under known margins. Journal of Multivariate Analysis 110, 133--150. 10.1016/j.jmva.2012.02.019

Genest, C. and Rivest, L.-P. (1993). Statistical inference procedures for bivariate Archimedean copulas. Journal of the American Statistical Association 88, 1034--1043.

Genest, C., G. Ne<U+0161>lehov<U+00E1>, J., and Ziegel, J. (2011). Inference in multivariate Archimedean copula models. TEST 20, 223--256.

Examples

Run this code

# NOT RUN {
tau <- 0.5
(theta <- copGumbel@iTau(tau)) # 2
d <- 20
(cop <- onacopulaL("Gumbel", list(theta,1:d)))

## Basic check of the empirical Kendall distribution function
set.seed(271)
n <- 1000
U <- rCopula(n, copula = cop)
X <- qnorm(U)
K.sample <- pCopula(U, copula = cop)
u <- seq(0, 1, length.out = 256)
edfK <- ecdf(K.sample)
plot(u, edfK(u), type = "l", ylim = 0:1,
     xlab = quote(italic(u)), ylab = quote(K[n](italic(u)))) # simulated
K.n <- Kn(u, x = X)
lines(u, K.n, col = "royalblue3") # Kn
## Difference at 0
edfK(0) # edf of K at 0
K.n[1] # K_n(0); this is > 0 since K.n is the edf of a discrete distribution
## => therefore, Kn(K.sample, x = X) is not uniform
plot(Kn(K.sample, x = X), ylim = 0:1)
## Note: Kn(0) -> 0 for n -> Inf

## Compute Kendall distribution function
u <- seq(0,1, length.out = 255)
Ku    <- pK(u, copula = cop@copula, d = d) # exact
Ku.MC <- pK(u, copula = cop@copula, d = d, n.MC = 1000) # via Monte Carlo
stopifnot(all.equal(log(Ku),
		    pK(u, copula = cop@copula, d = d, log.p=TRUE)))# rel.err 3.2e-16

## Build sample from K
set.seed(1)
n <- 200
W <- rK(n, copula = cop)

## Plot empirical distribution function based on W
## and the corresponding theoretical Kendall distribution function
## (exact and via Monte Carlo)
plot(ecdf(W), col = "blue", xlim = 0:1, verticals=TRUE,
     main = quote("Empirical"~ F[n](C(U)) ~
                     "and its Kendall distribution" ~ K(u)),
     do.points = FALSE, asp = 1)
abline(0,1, lty = 2); abline(h = 0:1, v = 0:1, lty = 3, col = "gray")
lines(u, Ku.MC, col = "red") # not quite monotone
lines(u, Ku, col = "black")  # strictly  monotone:
stopifnot(diff(Ku) >= 0)
legend(.25, .75, expression(F[n], K[MC](u), K(u)),
       col=c("blue" , "red", "black"), lty = 1, lwd = 1.5, bty = "n")

if(require("Rmpfr")) { # pK() now also works with high precision numbers:
 uM <- mpfr(0:255, 99)/256
 if(FALSE) {
   # not yet, now fails in  polyG() :
   KuM <- pK(uM, copula = cop@copula, d = d)
  ##  debug(copula:::.pK)
  debug(copula:::polyG)
 }
}# if( Rmpfr )


## Testing qK
pexpr <- quote( 0:63/63 );  p <- eval(pexpr)
d <- 10
cop <- onacopulaL("Gumbel", list(theta = 2, 1:d))
system.time(qK0 <- qK(p, copula = cop@copula, d = d)) # "default" - fast
# }
# NOT RUN {
<!-- % needs a couple of valuable CRAN seconds :-) -->

system.time(qK1  <- qK(p, copula= cop@copula, d=d, method = "simple"))
system.time(qK1. <- qK(p, copula= cop@copula, d=d, method = "simple", tol = 1e-12))
system.time(qK2  <- qK(p, copula= cop@copula, d=d, method = "sort"))
system.time(qK2. <- qK(p, copula= cop@copula, d=d, method = "sort",   tol = 1e-12))
system.time(qK3  <- qK(p, copula= cop@copula, d=d, method = "discrete", u.grid = 0:1e4/1e4))
system.time(qK4  <- qK(p, copula= cop@copula, d=d, method = "monoH.FC",
                       u.grid = 0:5e2/5e2))
system.time(qK4. <- qK(p, copula= cop@copula, d=d, method = "monoH.FC",
                       u.grid = 0:5e2/5e2, tol = 1e-12))
system.time(qK5  <- qK(p, copula= cop@copula, d=d, method = "monoH.FC",
                       u.grid = 0:5e3/5e3))
system.time(qK5. <- qK(p, copula= cop@copula, d=d, method = "monoH.FC",
                       u.grid = 0:5e3/5e3, tol = 1e-12))
system.time(qK6  <- qK(p, copula= cop@copula, d=d, method = "monoH.FC",
                       u.grid = (0:5e3/5e3)^2))
system.time(qK6. <- qK(p, copula= cop@copula, d=d, method = "monoH.FC",
                       u.grid = (0:5e3/5e3)^2, tol = 1e-12))

## Visually they all coincide :
cols <- adjustcolor(c("gray50", "gray80", "light blue",
                      "royal blue", "purple3", "purple4", "purple"), 0.6)
matplot(p, cbind(qK0, qK1, qK2, qK3, qK4, qK5, qK6), type = "l", lwd = 2*7:1, lty = 1:7, col = cols,
        xlab = bquote(p == .(pexpr)), ylab = quote({K^{-1}}(u)),
        main = "qK(p, method = *)")
legend("topleft", col = cols, lwd = 2*7:1, lty = 1:7, bty = "n", inset = .03,
       legend= paste0("method= ",
             sQuote(c("default", "simple", "sort",
                      "discrete(1e4)", "monoH.FC(500)", "monoH.FC(5e3)", "monoH.FC(*^2)"))))

## See they *are* inverses  (but only approximately!):
eqInv <- function(qK) all.equal(p, pK(qK, cop@copula, d=d), tol=0)

eqInv(qK0 ) # "default"	       0.03  worst
eqInv(qK1 ) # "simple"	       0.0011 - best
eqInv(qK1.) # "simple", e-12   0.00000 (8.73 e-13) !
eqInv(qK2 ) # "sort"	       0.0013 (close)
eqInv(qK2.) # "sort", e-12     0.00000 (7.32 e-12)
eqInv(qK3 ) # "discrete"       0.0026
eqInv(qK4 ) # "monoH.FC(500)"  0.0095
eqInv(qK4.) # "m.H.FC(5c)e-12" 0.00963
eqInv(qK5 ) # "monoH.FC(5e3)"  0.001148
eqInv(qK5.) # "m.H.FC(5k)e-12" 0.000989
eqInv(qK6 ) # "monoH.FC(*^2)"  0.001111
eqInv(qK6.) # "m.H.FC(*^2)e-12"0.00000 (1.190 e-09)

## and ensure the differences are not too large
stopifnot(
 all.equal(qK0, qK1, tol = 1e-2) # !
 ,
 all.equal(qK1, qK2, tol = 1e-4)
 ,
 all.equal(qK2, qK3, tol = 1e-3)
 ,
 all.equal(qK3, qK4, tol = 1e-3)
 ,
 all.equal(qK4, qK0, tol = 1e-2) # !
)

# }
# NOT RUN {
<!-- %dont -->
# }
# NOT RUN {
stopifnot(all.equal(p, pK(qK0, cop@copula, d=d), tol = 0.04))
# }

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