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Stat 598 Presentation onNonseperable, Stationary Covariance Functions for
Space-Time Data
Xiongzhi Chen
Department of Statistics
November 16, 2010
Xiongzhi Chen (Department of Statistics) Stat 598 Presentation November 16, 2010 1 / 22
Outline
Positive Definite Functions
Main Mathematical Results
Application to Irish Wind Data
Why Such A Correlation Model
Other Strategies and Wrong Claims
Proofs
Acknowledgements
Xiongzhi Chen (Department of Statistics) Stat 598 Presentation November 16, 2010 2 / 22
Key Component of Spatial-Temporal Modelling
Observations generated from a square-integrable stochastic processZ =
{Z (s; t), (s; t) ∈ Rd ×R
}Process Z induces a family of functionsC =
{Cs ,t : Rd ×R→ R| (s; t) ∈ Rd ×R
}, where
Cs ,t (h; u) = Cov ((Z (s; t) ,Z (s + h; t + u))
at each (s; t).
Covariance stationarity is equivalent to
C = {C (h; u)}
Then C (·; ·) is called the covariance function of Z.
Xiongzhi Chen (Department of Statistics) Stat 598 Presentation November 16, 2010 3 / 22
Positive-Definite (PSD) Functions
A function f : Rd+1 → K is positive definite iff
k
∑i ,j=1
f (wi − wj ) aia∗j ≥ 0
First equivalence
f being a covariance function ⇔ f positive definite
Second equivalence (Bochner’s Theorem): A continuous functionf on Rd+1 is positive definite iff
f (w) =∫exp
(√−1 〈η,w〉
)dF (η) (1)
Equivalences and Spectral Representation
Proof of Bochner’s Theorem
Xiongzhi Chen (Department of Statistics) Stat 598 Presentation November 16, 2010 4 / 22
Construction of PSD Functions
Main method: via Laplace transform and Bochner’s theorem.
Cressie and Huang (1999) [1] based on closed-form F-inverse of
Cω (u) =∫e−ih
′ωC (h; u) dh (2)
where C (h; u) ∈ Cb ∩ L1 and
C and Cω both are covariance functions or neither are (3)
Obviously C ≡ Cω mod (F) but C might be un-usable.
Gneiting (2002) [2] (i) avoids explicit F-inverse of Cω and usesL-representation of completely monotone (cm) functions andthe Bochner’s theorem; (ii) produces explicit product form ofsome PSD functions
Completely Monotone Functions
Xiongzhi Chen (Department of Statistics) Stat 598 Presentation November 16, 2010 5 / 22
Construction of PSD Functions
Main method: via Laplace transform and Bochner’s theorem.
Cressie and Huang (1999) [1] based on closed-form F-inverse of
Cω (u) =∫e−ih
′ωC (h; u) dh (2)
where C (h; u) ∈ Cb ∩ L1 and
C and Cω both are covariance functions or neither are (3)
Obviously C ≡ Cω mod (F) but C might be un-usable.
Gneiting (2002) [2] (i) avoids explicit F-inverse of Cω and usesL-representation of completely monotone (cm) functions andthe Bochner’s theorem; (ii) produces explicit product form ofsome PSD functions
Completely Monotone Functions
Xiongzhi Chen (Department of Statistics) Stat 598 Presentation November 16, 2010 5 / 22
Key Mathematical Result
Theorem 2 (Gneiting (2002) [2]): Let k, l ∈N+, σ2 > 0.Let ϕ (t) , t ≥ 0be a cm function, and let ψ (t) , t ≥ 0, be a positive function with a cmderivative. Then
C (h; u) =σ2
ψ(‖u‖2
)k/2 ϕ
‖h‖2
ψ(‖u‖2
) , (h; u) ∈ Rk ×Rl (4)
is a space-time covariance function.
The family includes almost all examples given in Cressie and Huang(1999) [1]
In application, ϕ,ψ can be associated with the data’s spatial andtemporal structures, respectively
Note how the temporal correlation is "scaled" by spatialcorrelation
Xiongzhi Chen (Department of Statistics) Stat 598 Presentation November 16, 2010 6 / 22
Key Mathematical Result
Theorem 2 (Gneiting (2002) [2]): Let k, l ∈N+, σ2 > 0.Let ϕ (t) , t ≥ 0be a cm function, and let ψ (t) , t ≥ 0, be a positive function with a cmderivative. Then
C (h; u) =σ2
ψ(‖u‖2
)k/2 ϕ
‖h‖2
ψ(‖u‖2
) , (h; u) ∈ Rk ×Rl (4)
is a space-time covariance function.
The family includes almost all examples given in Cressie and Huang(1999) [1]
In application, ϕ,ψ can be associated with the data’s spatial andtemporal structures, respectively
Note how the temporal correlation is "scaled" by spatialcorrelation
Xiongzhi Chen (Department of Statistics) Stat 598 Presentation November 16, 2010 6 / 22
Key Mathematical Result
Theorem 2 (Gneiting (2002) [2]): Let k, l ∈N+, σ2 > 0.Let ϕ (t) , t ≥ 0be a cm function, and let ψ (t) , t ≥ 0, be a positive function with a cmderivative. Then
C (h; u) =σ2
ψ(‖u‖2
)k/2 ϕ
‖h‖2
ψ(‖u‖2
) , (h; u) ∈ Rk ×Rl (4)
is a space-time covariance function.
The family includes almost all examples given in Cressie and Huang(1999) [1]
In application, ϕ,ψ can be associated with the data’s spatial andtemporal structures, respectively
Note how the temporal correlation is "scaled" by spatialcorrelation
Xiongzhi Chen (Department of Statistics) Stat 598 Presentation November 16, 2010 6 / 22
Examples of Building Functions
ϕ1 (t) = exp (−ctγ) c > 0,γ ∈ (0, 1]ϕ2 (t) =
(2ν−1Γ (ν)
)−1 (ct1/2)νKν
(ct1/2) c > 0, ν > 0
ϕ3 (t) = (1+ ctγ)−ν c > 0, ν > 0,γ ∈ (0, 1]
ϕ4 (t) = 2ν((exp
(ct1/2))+ exp (−ct1/2))−ν
c > 0, ν > 0ψ1 (t) = (at
α + 1)β a > 0, α ∈ (0, 1], β ∈ [0, 1]ψ1 (t) = ln (at
α + b) / ln (b) a > 0, b > 1, α ∈ (0, 1]ψ1 (t) = (at
α + b) / (b (atα + 1)) a > 0; b, α ∈ (0, 1]Table 1: Building Functions
Fitted Model
Why This Model
Xiongzhi Chen (Department of Statistics) Stat 598 Presentation November 16, 2010 7 / 22
Correlation Model for Irish Wind Data
For this data set, the estimated correlation model is
C (h; u|β) =
ψ−11 (u) =
(.901 |u|1.544 + 1
)−1if h = 0
.968ψ1 (u) exp
(− .00134 ‖h‖
ψβ/2(u)
)otherwise
(5)
where ψ1 and ϕ1 in Table 1 are chosen and ‖h‖ ≤ 450km, |u| ≤ 3
ψ−11 (u) =
(.901 |u|1.544 + 1
)−1, temporal correlation, estimated
from data
ϕ (h) = .968 exp (−.00134 ‖h‖) , spatial correlation, borrowed fromHaslett and Raftery (1989) ([4])
β = 0.61, spatial-temporal interaction, estimated from data; γ = 1/2in ϕ1 was forced
Table of Functions
Why This Model
Xiongzhi Chen (Department of Statistics) Stat 598 Presentation November 16, 2010 8 / 22
Correlation Model for Irish Wind Data
For this data set, the estimated correlation model is
C (h; u|β) =
ψ−11 (u) =
(.901 |u|1.544 + 1
)−1if h = 0
.968ψ1 (u) exp
(− .00134 ‖h‖
ψβ/2(u)
)otherwise
(5)
where ψ1 and ϕ1 in Table 1 are chosen and ‖h‖ ≤ 450km, |u| ≤ 3
ψ−11 (u) =
(.901 |u|1.544 + 1
)−1, temporal correlation, estimated
from data
ϕ (h) = .968 exp (−.00134 ‖h‖) , spatial correlation, borrowed fromHaslett and Raftery (1989) ([4])
β = 0.61, spatial-temporal interaction, estimated from data; γ = 1/2in ϕ1 was forced
Table of Functions
Why This Model
Xiongzhi Chen (Department of Statistics) Stat 598 Presentation November 16, 2010 8 / 22
Correlation Model for Irish Wind Data
For this data set, the estimated correlation model is
C (h; u|β) =
ψ−11 (u) =
(.901 |u|1.544 + 1
)−1if h = 0
.968ψ1 (u) exp
(− .00134 ‖h‖
ψβ/2(u)
)otherwise
(5)
where ψ1 and ϕ1 in Table 1 are chosen and ‖h‖ ≤ 450km, |u| ≤ 3
ψ−11 (u) =
(.901 |u|1.544 + 1
)−1, temporal correlation, estimated
from data
ϕ (h) = .968 exp (−.00134 ‖h‖) , spatial correlation, borrowed fromHaslett and Raftery (1989) ([4])
β = 0.61, spatial-temporal interaction, estimated from data; γ = 1/2in ϕ1 was forced
Table of Functions
Why This Model
Xiongzhi Chen (Department of Statistics) Stat 598 Presentation November 16, 2010 8 / 22
Why the Above Covariance Function?
The fitted model is composed of
Purely Spatial Correlation with nugget effect C (h; 0|β) = 1 ifh = 0;C (h; 0|β) = ϕ (h) , otherwise. Note ϕ ∈ C∞
Purely Temporal Correlation: C (u; 0|β) = ψ−11 (u) . Note ψ1 /∈ C∞
Some reasons:
Intrinsic: instrument variations and highly irregular wind speedsGeneric: evidence from data (see Graphs)
Technical: choice of ϕ fits into the family
C (h; u) =σ2(
a ‖u‖2α + 1)βk/2 exp
− c ‖h‖2γ(a ‖u‖2α + 1
)βγ
Table of Functions
Xiongzhi Chen (Department of Statistics) Stat 598 Presentation November 16, 2010 9 / 22
Why the Above Covariance Function?
The fitted model is composed of
Purely Spatial Correlation with nugget effect C (h; 0|β) = 1 ifh = 0;C (h; 0|β) = ϕ (h) , otherwise. Note ϕ ∈ C∞
Purely Temporal Correlation: C (u; 0|β) = ψ−11 (u) . Note ψ1 /∈ C∞
Some reasons:
Intrinsic: instrument variations and highly irregular wind speedsGeneric: evidence from data (see Graphs)
Technical: choice of ϕ fits into the family
C (h; u) =σ2(
a ‖u‖2α + 1)βk/2 exp
− c ‖h‖2γ(a ‖u‖2α + 1
)βγ
Table of Functions
Xiongzhi Chen (Department of Statistics) Stat 598 Presentation November 16, 2010 9 / 22
Why the Above Covariance Function?
The fitted model is composed of
Purely Spatial Correlation with nugget effect C (h; 0|β) = 1 ifh = 0;C (h; 0|β) = ϕ (h) , otherwise. Note ϕ ∈ C∞
Purely Temporal Correlation: C (u; 0|β) = ψ−11 (u) . Note ψ1 /∈ C∞
Some reasons:
Intrinsic: instrument variations and highly irregular wind speeds
Generic: evidence from data (see Graphs)
Technical: choice of ϕ fits into the family
C (h; u) =σ2(
a ‖u‖2α + 1)βk/2 exp
− c ‖h‖2γ(a ‖u‖2α + 1
)βγ
Table of Functions
Xiongzhi Chen (Department of Statistics) Stat 598 Presentation November 16, 2010 9 / 22
Why the Above Covariance Function?
The fitted model is composed of
Purely Spatial Correlation with nugget effect C (h; 0|β) = 1 ifh = 0;C (h; 0|β) = ϕ (h) , otherwise. Note ϕ ∈ C∞
Purely Temporal Correlation: C (u; 0|β) = ψ−11 (u) . Note ψ1 /∈ C∞
Some reasons:
Intrinsic: instrument variations and highly irregular wind speedsGeneric: evidence from data (see Graphs)
Technical: choice of ϕ fits into the family
C (h; u) =σ2(
a ‖u‖2α + 1)βk/2 exp
− c ‖h‖2γ(a ‖u‖2α + 1
)βγ
Table of Functions
Xiongzhi Chen (Department of Statistics) Stat 598 Presentation November 16, 2010 9 / 22
Why the Above Covariance Function?
The fitted model is composed of
Purely Spatial Correlation with nugget effect C (h; 0|β) = 1 ifh = 0;C (h; 0|β) = ϕ (h) , otherwise. Note ϕ ∈ C∞
Purely Temporal Correlation: C (u; 0|β) = ψ−11 (u) . Note ψ1 /∈ C∞
Some reasons:
Intrinsic: instrument variations and highly irregular wind speedsGeneric: evidence from data (see Graphs)
Technical: choice of ϕ fits into the family
C (h; u) =σ2(
a ‖u‖2α + 1)βk/2 exp
− c ‖h‖2γ(a ‖u‖2α + 1
)βγ
Table of Functions
Xiongzhi Chen (Department of Statistics) Stat 598 Presentation November 16, 2010 9 / 22
Other Strategies and Wrong Claims
All covariance functions in Cressie and Huang (1999) ([1]) andGneiting (2002) ([2]) are FULLY SYMMETRIC
Lagrangian reference frame by Cox and Isham (1988) ([6])
C (h; u) = EVG (‖h− Vu‖) ; (h, u) ∈ R2 ×R
used to model dynamic environmental and atmospheric processes,where
G (r) = λ {D (P1, 1) ∩D (P2, 1) : ‖P1 − P2‖ = r} ;P1,P2 ∈ R3
and λ is the Lebesgue measure.
Perturbation to fully symmetric models
False claims of convexity lead to false PSD functions, as inCressie and Huang 1999 ([1])
Xiongzhi Chen (Department of Statistics) Stat 598 Presentation November 16, 2010 10 / 22
Other Strategies and Wrong Claims
All covariance functions in Cressie and Huang (1999) ([1]) andGneiting (2002) ([2]) are FULLY SYMMETRICLagrangian reference frame by Cox and Isham (1988) ([6])
C (h; u) = EVG (‖h− Vu‖) ; (h, u) ∈ R2 ×R
used to model dynamic environmental and atmospheric processes,where
G (r) = λ {D (P1, 1) ∩D (P2, 1) : ‖P1 − P2‖ = r} ;P1,P2 ∈ R3
and λ is the Lebesgue measure.
Perturbation to fully symmetric models
False claims of convexity lead to false PSD functions, as inCressie and Huang 1999 ([1])
Xiongzhi Chen (Department of Statistics) Stat 598 Presentation November 16, 2010 10 / 22
Other Strategies and Wrong Claims
All covariance functions in Cressie and Huang (1999) ([1]) andGneiting (2002) ([2]) are FULLY SYMMETRICLagrangian reference frame by Cox and Isham (1988) ([6])
C (h; u) = EVG (‖h− Vu‖) ; (h, u) ∈ R2 ×R
used to model dynamic environmental and atmospheric processes,where
G (r) = λ {D (P1, 1) ∩D (P2, 1) : ‖P1 − P2‖ = r} ;P1,P2 ∈ R3
and λ is the Lebesgue measure.
Perturbation to fully symmetric models
False claims of convexity lead to false PSD functions, as inCressie and Huang 1999 ([1])
Xiongzhi Chen (Department of Statistics) Stat 598 Presentation November 16, 2010 10 / 22
Other Strategies and Wrong Claims
All covariance functions in Cressie and Huang (1999) ([1]) andGneiting (2002) ([2]) are FULLY SYMMETRICLagrangian reference frame by Cox and Isham (1988) ([6])
C (h; u) = EVG (‖h− Vu‖) ; (h, u) ∈ R2 ×R
used to model dynamic environmental and atmospheric processes,where
G (r) = λ {D (P1, 1) ∩D (P2, 1) : ‖P1 − P2‖ = r} ;P1,P2 ∈ R3
and λ is the Lebesgue measure.
Perturbation to fully symmetric models
False claims of convexity lead to false PSD functions, as inCressie and Huang 1999 ([1])
Xiongzhi Chen (Department of Statistics) Stat 598 Presentation November 16, 2010 10 / 22
Generalized Theorem 1 and Proof: I
Theorem 1 (Generalized): A continuous, bounded, symmetric andintegrable function C (h; u) ,defined on Rk ×Rl ,is a covariance function ifand only if
Cω (u) =∫e−ih
′ωC (h; u) dh, u ∈ Rl (6)
is a covariance function for all most all ω ∈ Rk
Digested Proof: The extension is on u ∈ Rl .The arguments are just acombination of Fubini’s, Bochner’s theorems and the Dirichlet integral.(a) C ∈ R1
(Rk ×Rl
)⇒ C ∈ L1
(Rk ×Rl
)(whenever k + l ≥ 2) and
Cω ∈ L1(Rl),a.s. ω ∈ Rk .
(b) C ∈(Cb ∩ L1
) (Rk+l
)⇒ Cω ∈ Cac
(Rl), ∀ω ∈ Rk ;
(c) C ∈(Cb ∩ L1
) (Rk+l
)and the inversion formula imply that
Inversion Formular
Theorem 2 and Proof
Xiongzhi Chen (Department of Statistics) Stat 598 Presentation November 16, 2010 11 / 22
Generalized Theorem 1 and Proof: II
Digested Proof (continued): C has F-inverse as
f (ω, τ) ∝∫∫
e−ih′ω−iτ′uC (h; u) dhdu ∝
∫e−iτ
′uCω (u) du (7)
where f =dFdλ
and F is a signed, bounded, measure on Rk+l such that
F << λ and λ is the Lebesgue measure on Rk+l . The last equality isjustified by Fubini’s theorem.(d) Now, Bochner’s theorem and Fubini’s together implies the validity ofthe theorem iff f ≥ 0 on Rk ×Rl and f ∈ L1
(Rk+l
). This completes the
proof.Inversion Formular
Xiongzhi Chen (Department of Statistics) Stat 598 Presentation November 16, 2010 12 / 22
Theorem 2 and Proof: Multiply Dominating Factor
Theorem 2 (Generalized): Let k and l be nonnegative integers, and letσ2 > 0. Suppose that ϕ (t) , t ≥ 0, is a completely monotone function,and let ψ (t) , t ≥ 0, be a positive function with a completely monotonederivative. Then
C (h; u) =σ2
ψ(‖u‖2
)k/2 ϕ
‖h‖2
ψ(‖u‖2
) , (h; u) ∈ Rk ×Rl (8)
is a space-time covariance function.Digested Proof: (a) Multiply the target function by dominatingintegral factor. (Case Restricted) Assume ϕ ∈ R1
(Rk)and define
Ca (h; u) = exp(−a ‖u‖2
)C (h; u) (9)
By Theorem 1 (Generalized), (9) is PSD iff (6) is PSD.Theorem 1 and Proof
Xiongzhi Chen (Department of Statistics) Stat 598 Presentation November 16, 2010 13 / 22
Theorem 2 and Proof: Plug in L-Representation of ϕ
(proof continued): (b) Plug the Laplace transform representation ofϕ into the integral. Notice that
ϕ (t) =∫[0,∞)
exp (−tr) dF (r) = L (F ) (10)
and ϕ ∈ R1(Rk), then ϕ is bounded and limt→0 ϕ (t) = 0.Thus F is a
bounded and F is right-continuous at 0 (Otherwise, take tn = n, rn = 1/nin (10)).
For notational simplicity, let ψu = ψ(‖u‖2
). Then by Fubini theorem,
Ca,ω (u) =∫e−ih
′ωCa (h; u) dh (11)
= exp(−a ‖u‖2
) σ2
ψk/2u
∫(0,∞)
dF (r)∫(0,∞)
fu,r ,ω (h) dh
where fu,r ,ω (h) = e−ih′ω exp
(−(r ‖h‖2
)/ψu
)Xiongzhi Chen (Department of Statistics) Stat 598 Presentation November 16, 2010 14 / 22
Theorem 2 and Proof: Obtain L-Representation of Ca,ω(proof continued): and (c1) that
Ca,ω (u) = ϕa,ω
(‖u‖2
), u ∈ Rk (12)
can be assumed, where
ϕa,ω (t) = σ2πk/2 exp (−at)∫(0,∞)
exp (−sψ (t)) dGω,a (s) ; t ≥ 0 (13)
and Gω,a is a nondecreasing, bounded function. This is just the Laplacetransform of the measure induced by composing the measures F byψ.Since Ca,ω is spherically symmetric and ϕa,ω is cm, Shoenberger’s theorem(Shoenberger 1938 [5]) asserts that Ca,ω (·) is PSD and so is each Ca byTheorem 1. Since lima→0+ Ca = C pointwise and C is continuous at 0, Cis PSD.
Theorem 2 and Proof 3
Xiongzhi Chen (Department of Statistics) Stat 598 Presentation November 16, 2010 15 / 22
Theorem 2 and Proof: Still by Dominating Factor
(proof continued): (Case General) Given a cm function ϕ (t) , t ≥ 0,then hb (t) = exp (−bt) ϕ (t) , b > 0, t ≥ 0 is still cm (by Tonelli’stheorem and since exp (− (b+ r) t) is integrable and F in theL-representation of ϕ is a bounded measure). Further hb is dominated byexp (−bt) , hence hb ∈ L1 (R) and hb ∈ Rk when t = ‖h‖ .Thus
Cb (h; u) =σ2
ψ(‖u‖2
)k/2 exp
− b ‖h‖2
ψ(‖u‖2
) ϕ
‖h‖2
ψ(‖u‖2
) (14)
is PSD by the previous arguments. Again, limb→0+ Cb = C pointwise andC is continuous at 0, C is PSD.
Acknowledgements
Xiongzhi Chen (Department of Statistics) Stat 598 Presentation November 16, 2010 16 / 22
Details On Equivalences and Spectral Representation
f positive definite ⇒ Gw = (f (wi − wj )) a positive-definite matrix⇒ a characteristic function (ch.f) hw (t) = exp
(−12t ′Gw t
)⇔
hw (s) =∫e−i 〈t ,s〉hw (t) dt a finite measure. Take a process Z (w)
(subtracted its mean function) with hw as its distribution.
when f ∈ L1(Rd+1
), F is absolute continuous and f ,F are inverse
Fourier transformations (modulo a constant). Based on the inversionformula
F (a, b] = limn→∞
12π
∫ T
−Tdt∫ b
ae−itsds
via Dirichlet integral lima→−∞,b→+∞∫ basin xxdx = π
Every psd function is equivalent to a double integral withnon-negative integrand.
PSD Functions
Proof of Theorem1 Proof of Theorem1 (II)
Xiongzhi Chen (Department of Statistics) Stat 598 Presentation November 16, 2010 17 / 22
Proof of Bochner’s Theorem
Digested Proof (Feller [3], p58):∑ki ,j=1 f (wi − wj ) aia∗j ≥ 0⇒∫∫
f (α− β) ρ (α) ρ (β)dµαdµβ ≥ 0, ∀ρ ∈ L1
Fix x and ε > 0 and put ρ (α) = e−2ε|α|2e2π〈α−β,x 〉. Do transformationα− β = γ, α+ β = δ to obtain∫ (∫
e−ε|δ|2dµδ
)e−ε|γ|2 f (γ) e2πi 〈γ,x 〉dµγ ≥ 0 =⇒ fε (γ) =
e−ε|γ|2 f (γ) ∈ L1 and has non-negative F -inverse. Hence fε has spectralrepresentation and limε→0 fε = f completes the proof by weak andcomplete convergence.Covariance Functions
Xiongzhi Chen (Department of Statistics) Stat 598 Presentation November 16, 2010 18 / 22
Details on Completely Monotone Functions
Theorem(Feller [3], p. 439): ϕ : (0,∞)→ (0,∞) is said to becompletely monotone iff (−1)n ϕn (t) ≥ 0, t > 0, n ≥ 0 iff
ϕ (t) =∫[0,∞)
exp (−tr) dF (r) = L (F )
with F being a measure on [0,∞].Digested Proof (Feller [3], p440).
ϕ∗ (s) = ϕ (a− as) = ∑(−a)n ϕn (a)
n!sn =⇒ ϕa (λ) = ϕ
(a− ae−λ/a) =
∑(−a)n ϕn (a)
n!e−nλ/a.And lima→∞ ϕa = ϕ ⇐⇒ lima→∞ Fa = F . ϕ is a
Laplace transform.Moreover under the above settings, it holds
F (x) = lima→∞ ∑n≤ax(−a)n ϕn (a)
n!the family of cm functions is closed under multiplication andcomposition, justified by induction via definition.
Construction of PDS Functions
Xiongzhi Chen (Department of Statistics) Stat 598 Presentation November 16, 2010 19 / 22
Theorem 2 and Proof: Contour integral of fu,r ,ω(h)
(proof continued): (c) Derive the Laplace transform from Cω. LetD = 2diag {r/ψu , · · · , r/ψu}. Notice that D > 0 andfu,r ,ω (h) ∝ e−ih
′ω−h′Dh/2, then rectangle contour integral by Cauchyintegral formular shows
fu,r (ω) =∫(0,∞)
fu,r ,ω (h) dh =(
πrψu
)−k/2
exp
(−‖ω‖
2
4rψu
)and
Cω (u) = σ2 exp(−a ‖u‖2
)exp
(−‖ω‖
2
4rψu
) ∫(0,∞)
1r k/2 dF (r) (15)
The continuity of C0 (·) and (15) implies∫(0,∞)
1r k/2 dF (r) =
C0 (0)σ2πk/2 < ∞
Theorem 2 and Proof 4
Xiongzhi Chen (Department of Statistics) Stat 598 Presentation November 16, 2010 20 / 22
References
Cressie, N., and Huang, H.-C. (1999), Classes of Nonseparable,Spatiotemporal Stationary Covariance Functions, JASA, 94, 1330-1340
Tilmann Gneiting (2002), Nonseparable, Stationary Covariance Functions forSpace-Time Data, JASA, Vol. 97, No. 458 (Jun., 2002), pp. 590-600
Feller, W. (1966), An Introduction to Probability Theory and Its Applications(Vol. II), New York: Wiley
John Haslett and Adrian E. Raftery (1989), Space-Time Modelling withLong-Memory Dependence: Assessing Ireland’s Wind Power, JRSS. Ser C(Applied Statistics), Vol. 38, No. 1(1989), pp. 1-50
Schoenberg, I. J. (1938), Metric Spaces and Completely MonotoneFunctions, Annals of Mathematics, 39, 811-841.
Cox, D. R., and Isham, V. (1988), A Simple Spatial-Temporal Model ofRainfall, in Proceedings of the Royal Society of London, Ser. A, 415, 317-328
Xiongzhi Chen (Department of Statistics) Stat 598 Presentation November 16, 2010 21 / 22
Acknowledgements
Thank you for being so PATIENT!
Irish Wind
Thoerem2 and Proof 5
Xiongzhi Chen (Department of Statistics) Stat 598 Presentation November 16, 2010 22 / 22