Abstract
Spatio-temporal data indexed by sampling locations and sampling time points are encountered in many scientific disciplines such as climatology, environmental sciences, and public health. Here, we propose a novel spatio-temporal expanding distance (STED) asymptotic framework for studying the properties of statistical inference for nonstationary spatio-temporal models. In particular, to model spatio-temporal dependence, we develop a new class of locally stationary spatio-temporal covariance functions. The STED asymptotic framework has a fixed spatio-temporal domain for spatio-temporal processes that are globally nonstationary in a rescaled fixed domain and locally stationary in a distance expanding domain. The utility of STED is illustrated by establishing the asymptotic properties of the maximum likelihood estimation for a general class of spatio-temporal covariance functions. A simulation study suggests sound finite-sample properties and the method is applied to a sea-surface temperature dataset.
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Acknowledgements
The authors thank the Editor, the Associate Editor and the referees for their helpful comments. The research of Haonan Wang was partially supported by NSF grants DMS-1737795, DMS-1923142 and CNS-1932413. This work is in part supported by the U.S. Geological Survey under Grant/Cooperative Agreement No. G16AC00344. The views and conclusions contained in this document are those of the authors and should not be interpreted as representing the opinions or policies of the U.S. Geological Survey. Mention of trade names or commercial products does not constitute their endorsement by the U.S. Geological Survey.
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Appendices
Appendix A.1: Proof of Proposition 1
Proof.
First, it can be seen that the generalized spatio-temporal Matérn covariance function in Eq. 1 is bounded and twice continuously differentiable with respect to 𝜃; thus, (LS.4) is satisfied. Next, we will show that the generalized spatio-temporal Matérn covariance function satisfies (LS.1) and (LS.2).
For any u1 and u2, define
For any s and t, let
Then, γn((s, t),(s, t)) = g(0,0,s, t). For all \((\boldsymbol {s},t), (\boldsymbol {s}+{\boldsymbol {u}_{1}}/{\varrho _{1,n}},t+{u_{2}}/{\varrho _{2,n}}) \in \mathcal {R}\times \mathcal {T}\) with ∥u1∥ > 0 or |u2| > 0, we have
uniformly since D(s, t) is bounded on \(\mathcal {R}\times \mathcal {T}\) and |h(u1,u2)|≤ 1. Thus, (LS.1) is satisfied.
For g(s, t) defined in (LS.2), we have g(s, t) = g(0,0,s, t) = D(s, t)2σ2 + τ2. Note that \(\boldsymbol {s}^{\prime }=\boldsymbol {s} + \boldsymbol {u}_{1}/\varrho _{1,n}\) and \(t^{\prime } = t+u_{2}/\varrho _{2,n}\), and we have \(|g(\boldsymbol {s},t) - g(\boldsymbol {s}^{\prime },t^{\prime })| = |D(\boldsymbol {s},t)^{2}-D(\boldsymbol {s}^{\prime },t^{\prime })^{2}|\sigma ^{2} = |D(\boldsymbol {s},t)+D(\boldsymbol {s}^{\prime },t^{\prime })||D(\boldsymbol {s},t)-D(\boldsymbol {s}^{\prime },t^{\prime })|\sigma ^{2} \leq |D(\boldsymbol {s},t)+D(\boldsymbol {s}^{\prime },t^{\prime })| (\widetilde {C}_{1}\Vert \boldsymbol {s} - \boldsymbol {s}^{\prime }\Vert + \widetilde {C}_{2} |t - t^{\prime }|)\sigma ^{2}\). Thus, (LS.2) holds by adjusting the constants.
Further, we will show that the generalized spatio-temporal Matérn covariance function (1) satisfies (LS.3) and (LS.5). For all \((\boldsymbol {s},t), (\boldsymbol {s}^{\prime },t^{\prime }) \in \mathcal {R}\times \mathcal {T}\), we have
Thus, to show (LS.3), it suffices to find γ0(∥u1∥) and γ1(|u2|) to bound h(u1,u2). Moreover, straightforward calculation yields that all first- and second-order partial derivatives of γn, denoted by γn, k and \(\gamma _{n,kk^{\prime }}\), can be bounded by the partial derivatives of h(u1,u2) up to some constant scales, which enables us to obtain γ2(∥u1∥) and γ3(|u2|) in (LS.5).
In addition, we have
where m = m(u1,u2;𝜃) and
For (LS.3), it can be seen that \(m(\boldsymbol {u}_{1},u_{2};\boldsymbol {\theta }) \leq \max \limits \left \{\theta _{2} \theta _{3}^{-1/2},\theta _{2}\right \}\Vert \boldsymbol {u}_{1}\Vert \). Thus, we have
where \(\widetilde {m}(\boldsymbol {u}_{1}) = \max \limits \left \{\theta _{2} \theta _{3}^{-1/2},\theta _{2}\right \}\Vert \boldsymbol {u}_{1}\Vert \). We can see that, up to some constant scales,
Here, γ0(∥u1∥) is a linear combination of a polynomial of ∥u1∥ with degree ν and a modified Bessel function of the second kind and γ1(|u2|) is a polynomial of |u2| with degree − 2ν − d.
For (LS.5), we focus on the first-order partial derivatives in detail and omit details for the second-order partial derivatives, as similar arguments can be applied. Straightforward calculation shows that the (absolute value of) partial derivatives of h(u1,u2) can be bounded by products of two positive functions, \(\widetilde {\gamma }_{2}(\Vert \boldsymbol {u}_{1}\Vert )\) and \(\widetilde {\gamma }_{3}(|u_{2}|)\). Moreover, \(\widetilde {\gamma }_{2}(\Vert \boldsymbol {u}_{1}\Vert )\) is a linear combination of a polynomial of ∥u1∥ with degree at least ν and a modified Bessel function of the second kind, and \(\widetilde {\gamma }_{3}(|u_{2}|)\) is a polynomial of |u2| with degree at most − 2ν − d.
Since the partial derivatives of h(u1,u2) with respect to 𝜃 is continuous in ∥u1∥ and |u2|, it is bounded if ∥u1∥ and |u2| are bounded. To show (LS.3) and (LS.5), it suffices to show that, for k, l > 0, there exists M > 0 such that
-
(i)
\({\int \limits }_{M}^{\infty } u^{k}K_{l}(u)du<\infty \),
-
(ii)
ukKl(u) is bounded by a nonincreasing function on \((M,\infty )\).
Since d ≥ 1 and k > 0, u− 2k−d is bounded on \((M,\infty )\) and \({\int \limits }_{M}^{\infty } u^{-2k-d}du=M^{-2k-d+1}/(2k+d-1) <\infty \). The last two conditions hold. By the property of Bessel function, \(K_{l}(u)\propto e^{-u}u^{-1/2}\{1+\mathcal {O}(1/u)\}\), as \(|u|\to \infty \). We can find M1,M2 such that Kl(u) ≤ M1e−uu− 1/2(1 + M2/u), when u ≥ M2. So (i) holds since
For (ii), we have ukKl(u) ≤ M1e−uuk− 1/2(1 + M2/u) ≤ 2M1e−uuk− 1/2, when u ≥ M2. Since e−uuk− 1/2 is decreasing on \((k-1/2,\infty )\), (ii) is satisfied. □
Appendix A.2: Generalized Exponential Spatio-temporal Covariance Function
In this section, we show that the following exponential spatio-temporal covariance function used in a simulation study satisfies conditions (LS.1)–(LS.5). The covariance function can be written as
where 𝜃 = (cs,ct,σ2,τ2)⊤ is the vector of spatio-temporal parameters with the scaling parameter in space, cs ≥ 0, and the scaling parameter in time, ct ≥ 0. In addition, \(\boldsymbol {u}_{1} = \varrho _{1,n}(\boldsymbol {s}-\boldsymbol {s}^{\prime })\) is the spatial lag scaled to the spatially expanding domain, and \(u_{2} = \varrho _{2,n}(t-t^{\prime })\) is the temporal lag scaled to the temporally expanding domain, where ϱ1,n and ϱ2,n are positive constants. Further, D(s, t) is some fixed positive spatio-temporal function with D(0,0) = 1. Note that D(s, t)2σ2 + τ2 is the variance of Y (s, t).
By arguments similar to Section Appendix, we show (LS.1), (LS.2) and (LS.4). For (LS.3), we can see that, for all \((\boldsymbol {s},t), (\boldsymbol {s}^{\prime },t^{\prime }) \in \mathcal {R}\times \mathcal {T}\),
Here, both γ0(∥u1∥) and γ1(|u2|) are nonincreasing positive functions. Moreover, we have \({\int \limits }_{0}^{\infty } e^{-u/c_{s}} du = 1/c_{s} < \infty \) and \({\int \limits }_{0}^{\infty } e^{-u/c_{t}} du = 1/c_{t} < \infty \). Thus, (LS.3) is satisfied.
Further, we have
Here, all the first- and second-order partial derivatives are continuous in ∥u1∥ and |u2| and hence bounded when ∥u1∥ and |u2| are bounded. In addition, they are bounded by a product of two functions \(\widetilde {\gamma }_{2}(\Vert \boldsymbol {u}_{1}\Vert )\) and \(\widetilde {\gamma }_{3}(|u_{2}|)\), where \(\widetilde {\gamma }_{2}(u)\) and \(\widetilde {\gamma }_{3}(u)\) are products of a polynomial of u and an exponential function of u. (LS.5) is satisfied, since for k > 0, uke−u is nonincreasing on \([k,\infty )\), and \({\int \limits }_{k}^{\infty } u^{k}e^{-u}du<\infty \).
Appendix A.3: A Remark on Assumption (C.1)
In this section, we provide two sufficient conditions for (C.1). Further, we will demonstrate that, if 𝜃3 > 1, the generalized spatio-temporal Matérn covariance function (1) satisfies Assumption (C.1). The two sufficient conditions are stated as follows:
-
(E.1)
For 1 ≤ k ≤ q, \(|\gamma _{n,k}((\boldsymbol {s},t), (\boldsymbol {s}^{\prime },t^{\prime }))|\) satisfies one of the following two conditions: (i) |γn, k((s, t),(s, t))| > 0; (ii) For \(\|\boldsymbol {u}_{1}\|, |u_{2}| \in [M,\infty )\) for some constant M > 0 such that \((\boldsymbol {s},t), (\boldsymbol {s}+{\boldsymbol {u}_{1}}/{A_{n}},t+{u_{2}}/{B_{n}}) \in \mathcal {R}\times \mathcal {T}\), we have \(|\gamma _{n,k}((\boldsymbol {s},t), (\boldsymbol {s}+{\boldsymbol {u}_{1}}/{A_{n}},t+{u_{2}}/{B_{n}}))| \geq C_{3}\exp (-C_{4}\Vert \boldsymbol {u}_{1}\Vert - C_{5}|u_{2}|)\) for all n, where C3,C4,C5 > 0 are constants.
-
(E.2)
(i) For any two given positive constants M1, M2, there exist \(M_{1}^{\prime }\) and \(M_{2}^{\prime }\) with \(M_{1} < M_{1}^{\prime } < \infty \) and \(M_{2} < M_{2}^{\prime } < \infty \) such that \({\sum }_{i}{\sum }_{j} {1}(\Vert \boldsymbol {s}_{i} - \boldsymbol {s}_{j}\Vert \in [M_{1}\delta _{n},M_{1}^{\prime }\delta _{n}]){1}(|t_{i}-t_{j}| \in [M_{2}\zeta _{n},M_{2}^{\prime }\zeta _{n}]) \geq C_{6}N_{n}^{1/2+\iota _{1}}\) for some C6 > 0 and ι1 > 0. (ii) \(A_{n}\delta _{n} = \mathcal {O}(b_{n})\) and \(B_{n}\zeta _{n} = \mathcal {O}(b_{n})\), where \(b_{n} = \log \log N_{n}\).
To see the sufficiency of (E.1) and (E.2), we first note that if \(A_{n}\delta _{n} = \mathcal {O}(1)\) and \(B_{n}\zeta _{n} = \mathcal {O}(1)\), then \( \|{{~}^{n}\boldsymbol {\Gamma }}_{k}\|_{F}^{2} \geq CN_{n}^{1/2+\iota _{1}} \) for some C > 0. Thus, (C.1) is satisfied with ι = ι1. If \(A_{n}\delta _{n} \to \infty \) or \(B_{n}\zeta _{n} \to \infty \), by (E.1)–(E.2), we have \( \|{{~}^{n}\boldsymbol {\Gamma }}_{k}\|_{F}^{2} \geq CN_{n}^{1/2+\iota _{1}^{\prime }} \) for some C > 0 and any \(\iota _{1}^{\prime }\) such that \(0<\iota _{1}^{\prime }<\iota _{1}\), so (C.1) is satisfied with \(\iota = \iota _{1}^{\prime }\).
Next, we will show that the generalized spatio-temporal Matérn covariance function (1) satisfies (E.1), when 𝜃3 > 1. Since \(\left |\frac {\partial \gamma _{n}((\boldsymbol {s},t),(\boldsymbol {s},t))}{\partial \sigma ^{2}}\right | = D(\boldsymbol {s},t)^{2} > 0\) and \(\left |\frac {\partial \gamma _{n}((\boldsymbol {s},t),(\boldsymbol {s},t))}{\partial \tau ^{2}}\right | = 1\), ∂γn/∂σ2 and ∂γn/∂τ2 satisfy (E.1)(i).
Further, we show that ∂γn/∂𝜃i satisfies (E.1)(ii) for i = 1,2,3. Recall that for all \((\boldsymbol {s},t), (\boldsymbol {s}+{\boldsymbol {u}_{1}}/{\varrho _{1,n}},t+{u_{2}}/{\varrho _{2,n}}) \in \mathcal {R}\times \mathcal {T}\) with ∥u1∥ > 0 or |u2| > 0, we have
Up to some constant scale, we have
since \(\theta _{2}\theta _{3}^{-1/2}\|\boldsymbol {u}_{1}\|\leq m(\boldsymbol {u}_{1},u_{2};\boldsymbol {\theta })\leq \theta _{2}\|\boldsymbol {u}_{1}\|\). In addition, by property of Bessel function, \(K_{l}(u)\propto e^{-u}u^{-1/2}\{1+\mathcal {O}(1/u)\}\), as \(|u|\to \infty \). We can find M1,M2 such that Kl(u) ≥ M1e−uu− 1/2, when u ≥ M2; thus, (E.1)(ii) follows.
Remark 1.
It can be seen that the generalized exponential covariance function also satisfies (E.1). Note that \(\left |\frac {\partial \gamma _{n}((\boldsymbol {s},t),(\boldsymbol {s},t))}{\partial \sigma ^{2}}\right | = D(\boldsymbol {s},t)^{2} > 0\) and \(\left |\frac {\partial \gamma _{n}((\boldsymbol {s},t),(\boldsymbol {s},t))}{\partial \tau ^{2}}\right | = 1\), and (E.1)(i) holds. Next, ∂γn/∂σ2, ∂γn/∂cs and ∂γn/∂ct are positive when ∥u1∥ > 2cs and |u2| > 2ct and can be written as linear combinations of products of \(|u_{2}|^{j}\exp (-a_{1}|u_{2}|)\) and \(\Vert \boldsymbol {u}_{1}\Vert ^{k} \exp (-a_{2}\Vert \boldsymbol {u}_{1}\Vert )\) for j, k ≥ 0 and some constants a1,a2 > 0. Hence, (E.1)(ii) follows.
Appendix A.4: Proof of Theorem 1
Proof.
To prove Theorem 1, it suffices to show that \(\|\boldsymbol {\Gamma }\|_{2}=\mathcal {O}(1)\), \(\|\boldsymbol {\Gamma }_{k}\|_{2} = \mathcal {O}(1)\) and \(\|\boldsymbol {\Gamma }_{kk^{\prime }}\|_{2} = \mathcal {O}(1)\), for all \(k,k^{\prime } = 1,\ldots , q\) (Mardia and Marshall, 1984). Note that \(\|\boldsymbol {A}\|_{2}\leq \|\boldsymbol {A}\|_{\infty }\) for any positive definite matrix A. We only need to show that \(\|\boldsymbol {\Gamma }\|_{\infty } = \mathcal {O}(1)\), \(\|\boldsymbol {\Gamma }_{k}\|_{\infty } = \mathcal {O}(1)\) and \(\|\boldsymbol {\Gamma }_{kk^{\prime }}\|_{\infty } = \mathcal {O}(1)\), for all \(k,k^{\prime } = 1,\ldots , q\).
For each i, let \(\mathcal {A}_{1,i}=\{j: \Vert \boldsymbol {s}_{i}-\boldsymbol {s}_{j}\Vert \leq C_{s,n}\}\) and \(\mathcal {A}_{2,i}=\{j: |t_{i}-t_{j}|\leq C_{t,n}\}\). Let a1 = Cs, n/δn, a2 = δnAn, b1 = Ct, n/ζn and b2 = ζnBn. Then,
where Γij is the (i, j)th entry of Γ.
Denote \(\text {Card}(\mathcal {A})\) as the cardinality of the set \(\mathcal {A}\), then
To show \(\Vert \boldsymbol {\Gamma } \Vert _{\infty }= \mathcal {O}(1)\), it suffices to show that
-
(i)
\({a_{1}^{d}}b_{1}\in [C_{1},C_{2}]\) for some constants C1,C2 > 0,
-
(ii)
\(\mathcal {O}(1/{a_{1}^{d}}{a_{2}^{d}}){\int \limits }_{a_{1}a_{2}}^{\infty } u^{d-1}\gamma _{0}(u)du = \mathcal {O}(1)\),
-
(iii)
\(\mathcal {O}(1/b_{1}b_{2}) {\int \limits }_{b_{1}b_{2}}^{\infty } \gamma _{1}(u)du = \mathcal {O}(1)\).
Let Cs, n = 1/An and Ct, n = 1/Bn. By (A.3), \({a_{1}^{d}}b_{1} = ({\delta _{n}^{d}}{A_{n}^{d}}\zeta _{n}B_{n})^{-1} \leq c_{3}^{-1} = \mathcal {O}(1)\), the above requirements are fulfilled. By (LS.5),
uniformly for all n and \(1< k,k^{\prime } < q\). Thus, we have \(\|\boldsymbol {\Gamma }\|_{2} = \mathcal {O}(1)\), and similar arguments can be applied to show that \(\|\boldsymbol {\Gamma }_{k}\|_{2} = \mathcal {O}(1)\) and \(\|\boldsymbol {\Gamma }_{kk^{\prime }}\|_{2}= \mathcal {O}(1)\).
Together with (C.1)–(C.3) and by Theorem 1 of Sweeting (1980), we have the result of Theorem 1. □
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Chu, T., Liu, J., Zhu, J. et al. Spatio-Temporal Expanding Distance Asymptotic Framework for Locally Stationary Processes. Sankhya A 84, 689–713 (2022). https://doi.org/10.1007/s13171-020-00213-4
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DOI: https://doi.org/10.1007/s13171-020-00213-4
Keywords
- Covariance functions
- Nonstationary processes
- Random fields
- Spatial statistics
- Spatio-temporal statistics