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ARTICLE IN PRESS
Contents lists available at ScienceDirect
Journal of Statistical Planning and Inference
Journal of Statistical Planning and Inference 140 (2010) 3567–3576
0378-37
doi:10.1
E-m
journal homepage: www.elsevier.com/locate/jspi
Short communication
On the extremal behavior of a nonstationary normal random field
Luısa Pereira
University of Beira Interior, Department of Mathematics, Portugal
a r t i c l e i n f o
Article history:
Received 2 December 2007
Received in revised form
16 November 2009
Accepted 27 April 2010Available online 6 May 2010
Keywords:
Random field
Dependence conditions
Nonstationarity
Normal random field
58/$ - see front matter & 2010 Published by
016/j.jspi.2010.04.049
ail address: [email protected]
a b s t r a c t
Let X¼ fXngn�1 be a nonstationary random field satisfying a long range weak
dependence for each coordinate at a time and a local dependence condition that avoids
clustering of exceedances of high values. For these random fields, the probability of no
exceedances of high values can be approximated by expð�tÞ, where t is the limiting
mean number of exceedances. We present a class of nonstationary normal random
fields for which this result can be applied.
& 2010 Published by Elsevier B.V.
1. Introduction
Let X¼ fXngnZ1 be a random field on Zdþ , where Zþ is the set of all positive integers and dZ2. We shall consider the
conditions and results for d=2 since it is notationally simplest and the results for higher dimensions follow analogousarguments. Random fields in two and three dimensions are encountered in a wide range of sciences such as hydrology,agriculture and geology.
For i=(i1,i2) and j=(j1,j2), irj means ikr jk, k=1,2, and n¼ ðn1,n2Þ-‘ means nk-1, k¼ 1,2.For a family of real levels fun,i : irngnZ1 and a subset I of the rectangle of points Rn ¼ f1, . . . ,n1g � f1, . . . ,n2g, we will
denote the event fXirun,i : i 2 Ig by fMnðIÞrug or simply by fMnrug when I=Rn.We say the pair I and J is in SiðlÞ, for each i=1,2, if the distance between PiðIÞ and PiðJÞ is greater or equal to l, where
Pi, i¼ 1,2, denote the cartesian projections. The distance d(I,J) between sets I and J of Z2þ , is the minimum of distances
dði,jÞ ¼maxfjis�jsj, s¼ 1,2g, i 2 I and j 2 J.The dependence structure used here for nonstationary random fields is a coordinatewise-mixing type condition as the
DðunÞ�condition introduced in Leadbetter and Rootzen (1998), which restrict dependence by limitingjPðMnðI1Þru,MnðI2ÞruÞ�PðMnðI1ÞruÞPðMnðI1ÞruÞj with the two indexes sets I1 and I2 being ‘‘separated’’ from eachother by a certain distance along each coordinate direction.
Definition 1.1. Let F be a family of indexes sets in Rn. The nonstationary random field X on Z2þ satisfies the condition
Dðun,iÞ over F if there exist sequences of integer valued constants fknigni Z1, flni
gni Z1, i=1,2, such that, as n¼ ðn1,n2Þ�!‘,we have
ðkn1,kn2Þ�!‘,
kn1ln1
n1,kn2
ln2
n2
� ��!0,
Elsevier B.V.
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L. Pereira / Journal of Statistical Planning and Inference 140 (2010) 3567–35763568
and ðkn1Dð1Þn,ln1
,kn1kn2
Dð2Þn,ln2Þ�!0, where DðiÞn,lni
, i¼ 1,2, are the components of the mixing coefficient, defined as follows:
Dð1Þn,ln1¼ supjPðMnðI1Þru,MnðI2ÞruÞ�PðMnðI1ÞruÞPðMnðI2ÞruÞj,
where the supremum is taken over pairs of I1 and I2 in S1ðln1Þ \ F ,
Dð2Þn,ln2
¼ supjPðMnðI1Þru,MnðI2ÞruÞ�PðMnðI1ÞruÞPðMnðI2ÞruÞj,
where the supremum is taken over pairs of I1 and I2 in S2ðln2Þ \ F .
This condition was used to guarantee the asymptotic independence for maxima over disjoint rectangles of indexes(Pereira and Ferreira, 2006) which is a fundamental result for extending some results of the extreme value theory ofstationary random fields to nonstationary case.
Proposition 1.1. Suppose that the random field X satisfies the condition D(un,i) over F such that ðI � J4J 2 F Þ ) I 2 F and for
fun,i : irngnZ1 such that
fn1n2 maxfPðXi4un,iÞ : irnggnZ1 is bounded:
If Vr,p ¼ Ir � Jr,p, r¼ 1, . . . ,kn1, p¼ 1, . . . ,kn2
, are disjoint rectangles in F , then, as n-‘,
P\r,p
fMnðVr,pÞrug
!�Yr,p
PðMnðVr,pÞruÞ-0:
Although the maximum may be regarded as the maximum of an approximately independent sequence of submaximathere may be high local dependence (the groups of Xj’s defining a maximum over a rectangle of indexes may be quitedependent) leading to a clustering of high values. In Pereira and Ferreira (2005), in addition to the coordinatewise-mixingcondition, it is restricted the local path behavior with respect to exceedances. It is used the idea of Leadbetter and Rootzen(1998) in combination with Husler (1986) to generalize to the nonstationary case a local dependence condition, D0ðun,iÞ,that avoids clustering of exceedances of un,i.
Definition 1.2. Let Eðun,iÞ denote the family of indexes sets I such that
Xi2I
PðXi4un,iÞr1
kn1kn2
Xirn
PðXi4un,iÞ:
The condition D0ðun,iÞ holds for X if, for each I 2 Eðun,iÞ, we have, as n�!‘,
kn1kn2
Xi,j2I
PðXi4un,i,Xj4un,jÞ-0:
That condition, which bounds the probability of more than one exceedance above the levels un,i in a rectangle with a fewindexes, and the coordinatewise-mixing D(un,i) condition lead to a Poisson approximation for the probability of noexceedances over Rn (Pereira and Ferreira, 2005).
Proposition 1.2. Suppose that the nonstationary random field X satisfies Dðun,iÞ and D0ðun,iÞ over Eðun,iÞ and
fn1n2maxfPðXi4un,iÞ : irnggnZ1 is bounded:
Then,
PðMnrun,iÞ�!n-‘
expð�tÞ, t40,
if and only ifXirn
PðXi4un,iÞ�!n-‘
t:
In Pereira and Ferreira (2006) is discussed the behavior of the maximum when clustering of high values of anonstationary random field is allowed but the local occurrence of two or more crossings of high levels, un,i, is restricted. Foreach one of the eight directions in Z2 the local occurrence of two or more crossings is restricted. These smooth oscillationconditions enabled to compute the asymptotic distribution of the maximum, from the limiting mean number of crossings.It is also proved that only four directions must be inspected since for opposite directions were found the same local pathcrossing behavior and the same limiting mean number of crossings.
In many cases, the coordinatewise-mixing condition is quite difficult to verify. So, it is natural to see if the weakconvergence result mentioned above holds when this condition is dropped and a correlation condition is assumed. The aimof this paper is to establish a correlation condition to ensure that a nonstationary normal random field verifies conditionsD(un,i) and D0ðun,iÞ over Eðun,iÞ, that is, X behaves like an independent normal random field. Normal random fields play animportant role since the specification of their finite-dimensional distributions is simple, they are reasonable models for
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L. Pereira / Journal of Statistical Planning and Inference 140 (2010) 3567–3576 3569
many natural phenomenon, estimation and inference are simple, and the model is specified by expectations andcovariances.
2. Main results
Let X¼ fXngnZ1 be a normal random field on Z2þ , (in general nonstationary) with correlations
ri,j ¼ covðXi,XjÞ, iZ1, jZ1,
and assume, without loss of generality, that, for each i 2 Z2þ ,EðXiÞ ¼ 0 and Var(Xi)=1.
The main tool in the Gaussian extreme value theory, and may be one of the basic important tools of the probabilitytheory, has certainly been the so-called normal comparison theorem. This result, used in the Gaussian case, bounds thedifference between two standardized multidimensional distribution functions by a convenient function of theircovariances. A simple special form of this theorem is given here, for use in next sections.
Lemma 2.1. Let X be a nonstationary normal random field with E(Xn)=0, Var(Xn)=1, nZ1, and d¼ supiajjri,jjo1. Then, for
IDRn,
P\i2I
fXirun,ig
!�Yi2I
PðXirun,iÞ
����������rK
Xi,j2I,ir j,iaj
jri,jjexp �
1
2ðu2
n,iþu2n,jÞ
1þjri,jj
0B@
1CA
and K is a constant (depending on d).
We shall be concerned with conditions under which
P\
irn
fXirun,ig
!�!n-‘
expð�tÞ, toþ1: ð2:1Þ
The case with a stationary normal random field and un,i constant in i was treated by Choi (2002). The result depend on aBerman’s type condition on their correlations. Specifically, writing rm=E(XjXj+ m) the extended version of Berman’scondition considered by Choi (2002) was the following:
rn logðn1n2Þ�!n-‘
0: ð2:2Þ
It was shown along the similar lines to Leadbetter et al. (1983, Proof of Theorem 4.3.3) that
jPðMnrunÞ�Fn1n2 ðunÞjrKn1n2
Xj2A
jrjjexp �u2
n
1þjrjj
� ��!n-‘
0, ð2:3Þ
where A¼ fj¼ ðj1,j2Þ : ja0,0r jirni,i¼ 1,2g, F denotes the standard normal distribution function and fungnZ1 is such thatfn1n2ð1�FðunÞÞgnZ1 is bounded. So, (2.2) implies PðMnrunÞ�!
n-‘expð�tÞ for levels un,nZ1, such that n1n2ð1�FðunÞÞ�!
n-‘t.
Remark 2.1. The subsums in (2.3) that involve rð0,j2Þand rðj1 ,0Þ should be treated from assumptions on these correlations
which are excluded from the hypothesis of Choi (2002). It will be also necessary consider the conditions
rðn1 ,0Þ log n1 �!n1-‘
0 and rð0,n2Þlog n2 �!
n2-‘0,
as we could infer from the proofs of the results of nonstationary case, established ahead.
For further related results concerning stationary normal random fields we refer the readers to Piterbarg (1996), Adler(1981) or Berman (1992), and the references therein.
In the following, under a simple condition on the correlation structure of a general nonstationary random field, we giveconditions under which (2.1) holds.
Assume that the correlations ri,j,iZ1,jZ1, of the nonstationary random field X decay to zero at a rate which is not tooslow, that is, satisfy
jri,jjorðji1�j1 j,ji2�j2 jÞ
for some sequence frngn2N20�f0g
such that
rðn1 ,0Þ log n1 �!n1-1
0, rð0,n2Þlog n2 �!
n2-10, ð2:4Þ
and, for n 2 Z2þ ,
rn logðn1n2Þ�!n-‘
0, ð2:5Þ
a generalization of the conditions rn logðn1n2Þ�!n-‘
0, rðn1 ,0Þ logn1 �!n1-1
0, rð0,n2Þlogn2 �!
n2-10, used in the stationary case.
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Our main results concern conditions on the fun,i : irngnZ1 under which X verifies conditions D(un,i) and D0ðun,iÞ overEðun,iÞ. From such results it will then follow simply that if alsoX
i2I
ð1�Fðun,iÞÞ�!n-‘
t,
then (2.1) holds, generalizing the conclusion obtained in the stationary case.The first result treats the case where minnZ1un,i tends to infinity as fast as some multiple of logðn1n2Þ
1=2.
Proposition 2.1. Suppose that the correlations ri,j, iZ1,jZ1, of the normal random field X are such that jri,jjrrðji1�j1 j,ji2�j2jÞ,
where frngn2N20�f0g
satisfies (2.4) and (2.5) and supn2N20�f0gjrnjo1. Let the constants fun,i : irngnZ1 be such that
fP
irnð1�Fðun,iÞÞgnZ1 is bounded and, for some c40, ln ¼minirnun,iZcðlogðn1n2ÞÞ1=2. If, for each I 2 Eðun,iÞ, the sequence
ðkn1kn2Þ1=2
n1n2]fi 2 I : un,iZuðtÞn g
( )nZ1
is bounded, ð2:6Þ
for some fuðtÞn gnZ1 such that
n1n2ð1�FðuðtÞn ÞÞ�!
n-‘t,
then, X verifies the conditions D(un,i) and D0ðun,iÞ over Eðun,iÞ.
The next result generalizes Proposition 2.1 by removing the restriction minirnun,iZclogðn1n2Þ1=2 requiring only that
minirnun,i-1.
Proposition 2.2. Let the correlations ri,j, iZ1,jZ1, of the normal random field X satisfy jri,jjrrðji1�j1j,ji2�j2 jÞ, where frngn2N2
0�f0g
satisfies (2.4) and (2.5) and supn2N20�f0gjrnjo1. Suppose the constants fun,i : irngnZ1 are such that f
Pirnð1�Fðun,iÞÞgnZ1 is
bounded and ln ¼minirnun,i-1. Then X verifies conditions Dðun,iÞ and D0ðun,iÞ over Eðun,iÞ.
Remark 2.2. For practical purposes the condition that jri,jjrrðji1�j1 j,ji2�j2jÞfor i,j 2 N2,iaj, where frngn2N2
0�f0gsatisfies (2.4)
and (2.5) is as useful and as general as is likely to be needed. In fact this condition is rather close to what is necessary forthe maximum of a nonstationary normal random field to behave like that of the associated independent field.
As we are going to see in the next section, it is the correlation condition which makes it possible to prove D(un,i) and
D0ðun,iÞ over Eðun,iÞ.
3. Proofs
The proofs of Propositions 2.1 and 2.2 will be given by means of several lemmas.The next two lemmas enable us to prove that under the conditions of Proposition 2.1, for IDRn,
SnðIÞ ¼X
i,j2I,ir j,iaj
jri,jjexp �
1
2ðu2
n,iþu2n,jÞ
1þjri,jj
0B@
1CA�!
n-‘0:
Lemma 3.1. Let fun,i : irngnZ1 be such that fP
irnð1�Fðun,iÞÞgnZ1 is bounded and ln ¼minirnun,i�!n-‘þ1. Suppose that
the correlations ri,j satisfy jri,jjrd for iaj, where do1 is a constant. Then, for IDRn,
Sð1Þn ðIÞ ¼X
i,j2I,i r j,iajjj1�i1 j�jj2�i2 jrYn
jri,jjexp �
1
2ðu2
n,iþu2n,jÞ
1þjri,jj
0B@
1CA�!
n-‘0,
where Yn ¼ expðZl2nÞ, for any Zo1=4� ð1�dÞ=ð1þdÞ.
Proof. Clearly,
Sð1Þn ðIÞrdX
i,j2I,i r j,iajjj1�i1 j�jj2�i2 jrYn
exp �
1
2ðu2
n,iþu2n,jÞ
1þd
0B@
1CArd
Xi,j2I,i r j,iaj
jj1�i1 j�jj2�i2 jrYn
exp �u2
n,i
1þd
!þexp �
u2n,j
1þd
! !r2dY2
n
Xi2I
exp �u2
n,i
1þd
!
¼ 2dY2n
Xi2I
u�1n,i exp �
u2n,i
2
!
1�Fðun,iÞð1�Fðun,iÞÞun,iexp �
1
2�
1�d1þd
u2n,i
� �,
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L. Pereira / Journal of Statistical Planning and Inference 140 (2010) 3567–3576 3571
giving for a suitable K,
Sð1Þn ðIÞr2dY2nKXi2I
ð1�Fðun,iÞÞun,iexp �1
2�
1�d1þd
u2n,i
� �,
since un,iZln�!n-‘1. So, by attending that f
Pirnð1�Fðun,iÞÞgnZ1 is bounded and Yn ¼ expðZl2
nÞ, for Zo1=4� 1�d=1þd, itfollows that:
Sð1Þn ðIÞr2K1dlnexp �1
2�
1�d1þd
�2Z� �
l2n
� ��!n-‘
0: &
Remark 3.1. In the above lemma no assumption was made about the correlation structure.
Lemma 3.2. Suppose that the correlations ri,j of the normal random field X are such that jri,jjrrðji1�j1 j,ji2�j2 jÞfor iaj, where
frngn2N20�f0g
satisfies (2.4) and (2.5) and supn2N20�f0gjrnjo1. Let fun,i : irngnZ1 be such that f
Pirnð1�Fðun,iÞÞg is bounded
and ln ¼minirnun,iZcðlogðn1n2ÞÞ1=2, for some c40. Then, for IDRn, we have
Sð2Þn ðIÞ ¼X
i,j2I,i r j,iajjj1�i1 j�jj2�i2 j4Yn
jri,jjexp �
1
2ðu2
n,iþu2n,jÞ
1þjri,jj
0B@
1CA�!
n-‘0, ð3:1Þ
where Yn ¼ expðZl2nÞ, Z is a positive constant.
Proof. Split the sum in (3.1) into three parts, the first for io j, the second for i1 ¼ j14i2o j2 and the third for i2 ¼ j24i1o j1.We will denote them by Sð2Þn,iðIÞ, i=1, 2, 3, respectively.
Since
Yn ¼ expðZl2nÞZexpðZc2logðn1n2ÞÞ ¼ ðn1n2Þ
a, a¼ c2Z
and
supjj1�i1 j�jj2�i2 j4Yn
i o j
jri,jjr supjj1�i1 j�jj2�i2 j4 ðn1n2 Þ
ai o j
jri,jjr supjj1�i1 j�jj2�i2 j4 ðn1 n2 Þ
ai o j
jri,jjrðji1�j1 j,ji2�j2 jÞ¼ dð1ÞYn
,
the first term, Sð2Þn,1ðIÞ, is dominated by
Sð2Þn,1ðIÞrdð1ÞYn
Xi,j2I,io j
exp �
1
2u2
n,i
1þdð1ÞYn
�
1
2u2
n,j
1þdð1ÞYn
0B@
1CArdð1ÞYn
Xi2I
exp �
1
2u2
n,i
1þdð1ÞYn
0B@
1CA
0B@
1CA
2
:
Now, define un by 1�FðunÞ ¼ 1=n1n2 and split the sum in braces into two parts, for un,iZun, and un,ioun. We obtain
Sð2Þn,1ðIÞ ¼ dð1ÞYn
Xi2I
un,i Z un
exp �12 u2
n,i
1þdð1ÞYn
!þX
i2Iun,i o un
exp �
1
2u2
n,i
1þdð1ÞYn
0B@
1CA
0B@
1CA
2
rdð1ÞYnu2
nexpðu2ndð1ÞYnÞ
1
un
Xi2I
un,i Z un
exp �u2
n
2
� �þX
i2Iun,i o un
u�1n,i exp �
u2n,i
2
!264
375
2
,
which tends to zero since we have
(i)
expð�u2n=2Þ � Kun=n1n2 andffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffip(ii)
un � 2logðn1n2Þand then
dð1ÞYnu2
n � dð1ÞYn2logðn1n2Þ ¼
2
adð1ÞYn
logðn1n2Þa¼
2
a supjj1�i1j�jj2�i2 j4 ðn1n2Þ
arðji1�j1 j,ji2�j2jÞ
logðna1na2Þ
r2
a supjj1�i1j�jj2�i2 j4 ðn1n2Þ
arðji1�j1j,ji2�j2 jÞ
logðjj1�i1j � jj2�i2jÞ�!n-‘
0,
1
un
Xi2I
exp �u2
n
2
� �r
1
un
Xirn
exp �u2
n
2
� ��
n1n2
un� K
un
n1n2¼ K ,
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and
Xi2I
1
un,iexp �
u2n,i
2
!rXirn
1
un,iexp �
u2n,i
2
!rXirn
ð1�Fðun,iÞÞrK 0:
Similarly the second term is dominated by
dð2ÞYnu2
nexpðu2ndð2ÞYnÞ
1
un
Xi2I
un,i Z un
exp �u2
n
2
� �þX
i2Iun,i o un
u�1n,i exp �
u2n,i
2
!264
375
2
,
where dð2ÞYn¼ supjj2�i2j4na
2rð0,jj2�i2jÞ
, which also converges to zero, since rð0,n2Þlogn2 �!
n2-10.
Likewise the third term tends to zero. &
Remark 3.2. The correlation condition implies that for IDRn, SnðIÞ�!n-‘
0, when un,i�!n-‘1 in a manner which is not too
slow. This will be used in verifying Dðun,iÞ and D0ðun,iÞ over Eðun,iÞ.
With these lemmas we state now the proof of Proposition 2.1.
Proof of Proposition 2.1. Let I,J 2 F . Denoting the event fXirun,ig by Ai,n, we have that
supI,J2Sðln1
Þ\Sðln2Þ
P\
i2I,j2J
Ai,nAj,n
0@
1A�P
\i2I
Ai,n
!P\j2J
Aj,n
0@
1A
������������r sup
I,J2Sðln1Þ\Sðln2
Þ
P\
i2I,j2J
Ai,nAj,n
0@
1A�Y
i2I
P Ai,n
� Yj2J
PðAj,nÞ
������������
þ supI,J2Sðln1
Þ\Sðln2Þ
Yi2I
PðAi,nÞ�P\i2I
Ai,n
!����������þ sup
I,J2Sðln1Þ\Sðln2
Þ
Yj2j
PðAj,nÞ�P\j2J
Aj,n
0@
1A
������������r3SnðRnÞ�!
n-‘0:
Let I 2 Eðun,iÞ satisfying (2.6). Then, we have
kn1kn2
Xi,j2I
PðAi,nAj,nÞrkn1kn2
Xi,j2I
jPðAi,nAj,nÞ�PðAi,nÞPðAj,nÞjþkn1kn2
Xi,j2I
PðAi,nÞPðAj,nÞrkn1kn2
SnðIÞ
þkn1kn2
Xi,j2I
ð1�Fðun,iÞÞð1�Fðun,jÞÞrkn1kn2
SnðIÞþkn1kn2
0B@X
i2I
ð1�Fðun,iÞÞ
1CA
2
rkn1kn2
SnðIÞ
þ1
kn1kn2
Xirn
1�Fðun,i
� Þ
!2
�!n-‘
0,
since
kn1kn2
Sð1Þn ðIÞr2dKlnexp �1�d
2ð1þdÞ�2Z
� �l2
n
� �Xirn
ð1�Fðun,iÞÞ�!n-‘
0
and
kn1kn2
Sð1Þn ðIÞrdð1ÞYnu2
nexpðu2ndð1ÞYnÞ
264ðkn1
kn2Þ1=2]fi 2 I : un,iZung �
1
un�
Kun
n1n2
þðkn1kn2Þ1=2
Xi2I
un,i Z un
u�1n,i exp �
1
2u2
n,i
� �1�Fðun,iÞ
� ð1�Fðun,iÞÞ
375
2
�!n-‘
0: &
We return now to the generalization of Proposition 2.1 by removing the restriction minirnun,iZclogðn1n2Þ1=2 requiring
only that minirnun,i-1.We use the technique developed by Husler (1983), tailored for random fields, in obtaining our result. This involves
grouping the un,i,irn, in rectangles as follows. Write c1 ¼ ln ¼minirnun,i and partition Rn into disjoint subsets J1, . . . ,JL asfollows. Define
J1 ¼ fi : c1run,ir2c1g, d1 ¼maxi2J1
un,i, c2 ¼minfun,i : un,i4d1g,
J2 ¼ fi : c2run,ir2c2g, d2 ¼maxi2J2
un,i, c3 ¼minfun,i : un,i4d2g,
and so on, until a set JL which contains the point i with maxirnun,i. Thus Jk is a nonempty subset of Rn such that theminimum and maximum values of un,i, for i 2 Jk, are ck,dk, respectively, where dkr2ck. Clearly also ckþ142ck for each k.
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Finally, by way of notation write
Pk ¼Xi2Jk
ð1�Fðun,iÞÞ, k¼ 1,2, . . . ,L,
and define
A¼ k : PkZexp �c2
k
4
!,1rkrL
( ): ð3:2Þ
Of course L,ck,dk,Pk and the sets Jk all depend naturally on n, but this dependence is suppressed in the notation whichwill be used without comment.
The next lemma shows that we have to consider only sets I and J which are subsets ofS
k2AJk.
Lemma 3.3. With the above notation write I� ¼ I \ ðS
k2AJkÞ for any IDRn, where A is defined in (3.2). Suppose that
ln ¼minirnun,i-1 andP
irnð1�Fðun,iÞ is bounded. Then
0rP\i2I�fXirun,ig
!�P
\i2I
fXirun,ig
!�!n-‘
0: ð3:3Þ
Proof. The difference in probabilities in (3.3) is dominated by
P[
i2I��I
fXi4un,ig
!rXk=2A
Pk: ð3:4Þ
But if k=2A and k41, since ck42ck�1, we have
Pkoexp �c2
k
4
!ock�1exp �
1
2c2
k�1
� � exp �1
2c2
k�1
� �ck�1
rKlnexp �1
2l2
n
� �ð1�Fðck�1ÞÞrKlnexp �
1
2l2
n
� �Pk�1,
since x expð�x2=2Þ decreases for large x and ð1�Fðck�1ÞÞ is one of the terms contributing to Pk�1.
If 1=2A, P1rexpð�c21=4Þrexpð�l2
n=4Þ, so that
Xk2A
PkrKlnexp �1
2l2
n
� � X1rkr L
Pkþexp �l2
n
4
!�!n-‘
0,
sinceP
1rkrLPk ¼P
irnð1�Fðun,iÞÞ is bounded. Hence (3.3) follows from (3.4). &
Remark 3.3. Since we do not assume any condition on the dependence of Xi, i 2 N20�f0g, Lemma 3.3 holds obviously for
the associated random field of independent variables.
In view of this lemma and Lemma 2.1 it is sufficient, in obtaining, as n-‘,
P\
i2I,j2J
fXirun,i,Xjrun,jg
0@
1A�P
\i2I
fXirun,ig
!P\j2J
fXjrun,jg
0@
1A-0,
to show that
Xi2I� ,j2J�
jri,jjexp�
1
2ðu2
n,iþu2n,jÞ
1þjri,jj
0B@
1CA�!
n-‘0,
where I� and J� are subsets ofS
k2AJk.Since each term of the sum is greater or equal to zero, the supremum on such I� and J� is bounded by
Sn ¼X
i r j r n
i,j2S
k2AJk
jri,jjexp�
1
2ðu2
n,iþu2n,jÞ
1þjri,jj
0B@
1CA, ð3:5Þ
so, it will be shown, by means of the next two lemmas, that Sn�!n-‘
0.
Lemma 3.4. Suppose that the correlations ri,j of the normal random field X satisfy jri,jjrrðji1�j1 j,ji2�j2jÞfor iaj, where
frngn2N20�f0g
is such that rn�!n-‘0,rðn1 ,0Þ �!n1-1
0 and rð0,n2Þ�!
n2-10.
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Suppose that ln ¼minirnun,i�!n-‘1 and f
Pirnð1�Fðun,iÞÞgnZ1 is bounded. Then, for k,m 2 A,krm,
Sð1Þk,m ¼X
i2Jk ,j2Jm ,i r j,iajYn o ji1�j1 j�ji2�j2 jo gn,m
jri,jjexp �
1
2ðu2
n,iþu2n,jÞ
1þjri,jj
0B@
1CArKexp �
l2n
16
!PkPm,
where Yn ¼ expðZl2nÞ, for Z as in Lemma 3.1 and gn,m ¼ expðc
2m
16Þ.
Proof. We partition the sum Sk,m(1) into three subsums, for io j, for i1 ¼ j14i2o j2 and for i2 ¼ j24i1o j1. We will denote
them by Sk,m,i(1) , i=1, 2, 3, respectively. Since
supjj1�i1 j�jj2�i2 j4Yn
i o j
jri,jjr supjj1�i1 j�jj2�i2 j4Yn
i o j
rðji1�j1 j,ji2�j2jÞ¼ dð1ÞYn
,
the first term Sk,m,1(1) is dominated by
dð1ÞYn
Xjj1�i1 j�jj2�i2 j4Yn
i2Jk ,j2Jm ,i o j
exp �
1
2ðu2
n,iþu2n,jÞ
1þdð1ÞYn
0B@
1CA:
Now the exponential term does not exceed
exp �
1
2ðu2
n,iþu2n,jÞ
1þdð1ÞYn
0B@
1CArexp �
1
2ðu2
n,iþu2n,jÞð1�d
ð1ÞYnÞ
� �rexp �
1
2u2
n,i
� �
� exp �c2m
1
2�
1
2dð1ÞYn�
1
2dð1ÞYn
d2k
c2m
! !rexp �
1
2u2
n,i
� �� exp �c2
m
1
2�
5
2dð1ÞYn
� �� �,
since dkr2ckr2cm.
Hence, we have
Sð1Þk,m,1rdð1ÞYn
Xjj1�i1 j�jj2�i2 jo gn,m
i2Jk ,j2Jm ,i o j
exp �1
2u2
n,i
� �� exp �c2
m
1
2�
5
2dð1ÞYn
� �� �
rdð1ÞYn
Xjj1�i1 j�jj2�i2 jo gn,m
i2Jk ,j2Jm ,i o j
dk
un,iexp �
1
2u2
n,i
� �� exp �c2
m
1
2�
5
2dð1ÞYn
� �� �
rdð1ÞYng2
n,mdk
Xi2Jk
exp �1
2u2
n,i
� �u�1
n,i exp �c2m
1
2�
5
2dð1ÞYn
� �� �
rdð1ÞYng2
n,mdkPkexp �c2m
1
2�
5
2dð1ÞYn
� �� �rKcmexp �c2
m
1
2�
1
4�
1
8�
5
2dð1ÞYn
� �� �PkPmrKexp �
l2n
16
!PkPm,
since PmZexpð�c2m=4Þ, gn,m ¼ expðc2
m=16Þ, dkr2ckr2cm, cmZln and dð1ÞYn�!n-‘
0.
To deal with the second and third sums we define
dð2ÞYn¼ supjj2�i2 j4Yn
rð0,ji2�j2 jÞ, dð3ÞYn
¼ supjj1�i1j4Yn
rðji1�j1j,0Þ,
and note that, for i=1, 2,
Sð1Þk,m,irdðiÞYncmexp �c2
m
1
2�
1
4�
1
8�
5
2dð2ÞYn
� �� �PkPmrKiexp �
l2n
16
!PkPm
for some K2,K3, since cmZln, dð2ÞYn�!
n2-10, dð3ÞYn
�!n1-1
0. &
Lemma 3.5. Suppose that the correlations ri,j of the normal random field X are such that jri,jjrrðji1�j1j,ji2�j2 jÞfor iaj, where
frngn2N20�f0g
satisfies (2.4) and (2.5). Let fun,i : irngnZ1 be such that fP
irnð1�Fðun,iÞÞgnZ1 is bounded and
ln ¼minirnun,i-1. Then, for krm, we have
Sð2Þk,m ¼X
i2Jk ,j2Jm ,i r j,iajgn,m o ji1�j1 j�ji2�j2 jr n1 n2
jri,jjexp �
1
2ðu2
n,iþu2n,jÞ
1þjri,jj
0B@
1CArbnPkPm, ð3:6Þ
where gn,m ¼ expðc2m=16Þ and bn-0, bn depending only on n.
ARTICLE IN PRESS
L. Pereira / Journal of Statistical Planning and Inference 140 (2010) 3567–3576 3575
Proof. Split the sum in (3.6) into partial sums, S(2)k,m,i, i=1, 2, 3, the first for io j, the second for i1 ¼ j14i2o j2 and the third
for i2 ¼ j24i1o j1. Since
supjj1�i1 j�jj2�i2 j4 gn,m
i o j
jri,jjr supjj1�i1 j�jj2�i2 j4 gn,m
i o j
rðji1�j1j,ji2�j2jÞ¼ dð1Þgn,m
,
the first sum, Sk,m,1(2) , is dominated by
dð1Þgn,m
Xjj1�i1 j�jj2�i2 jr n1n2
i2Jk ,j2Jm ,i o j
exp �
1
2u2
n,iþu2n,j
�1þdð1Þgn,m
0B@
1CArdð1Þgn,m
Xjj1�i1 j�jj2�i2 jr n1 n2
i2Jk ,j2Jm ,i o j
exp �1
2ðu2
n,iþu2n,jÞð1�d
ð1Þgn,mÞ
� �
rdð1Þgn,m
Yl ¼ k,m
dl
Xi2Jl
expu2
n,i
2dð1Þgn,m
! exp �u2
n,i
2
!
un,i
0BBBB@
1CCCCArdð1Þgn,m
dkdmPkPmexp1
2ðd2
kþd2mÞd
ð1Þgn,m
� �
rKdð1Þgn,md2
mPkPmexpðd2mdð1Þgn,mÞ:
Now
dð1Þgn,md2
mr4dð1Þgn,mc2
m ¼ 64dð1Þgn,mloggn,m,
where gn,m ¼ expðc2m=16ÞZexpðl2
n=16Þ�!n-1
0. Similarly the second and third sums are dominated by
Sð2Þk,m,2rdð2Þgn,md2
m expðd2mdð2Þgn,mÞPkPm and Sð2Þk,m,3rdð3Þgn,m
d2mexpðd2
mdð3Þgn,mÞPkPm,
where dð2Þgn,m¼ supji2�j2j4gn,m
rð0,ji2�j2jÞand dð3Þgn,m
¼ supji1�j1j4gn,mrðji1�j1 j,0Þ
, from which the result follows. &
By collecting these lemmas we can now show Proposition 2.2.
Proof of Proposition 2.2. Letting A defined as in (3.2) we see from Lemmas 3.1, 3.4, 3.5 that
Sn ¼X
i r j r n
i,j2S
k2AJk
jri,jjexp�
1
2ðu2
n,iþu2n,jÞ
1þjri,jj
0B@
1CAren
Xk,m2A
PkPmþoð1Þ,
where en-0 as n-‘. ButP
k,m2APkPmrfP
irnð1�Fðun,iÞÞg2 which is bounded, so Sn�!n-‘
0. It thus follows conditionsDðun,iÞ and D0ðun,iÞ over Eðun,iÞ. &
Those results about the asymptotic behavior of the maximum of a nonstationary normal random field can be applied tosimple forms of nonstationarity like periodic random fields. However, in this case we could consider slightly weakercovariance conditions (Pereira, 2008).
4. Example
The main results may be used to give the asymptotic distribution of the maximum in many cases of interest.Let us consider an isotropic standardized normal random field, fYngnZ1, that is EðYsÞ ¼ 0,VarðYsÞ ¼ 1 and CovðYs,YtÞ
depends alone on distance Jt�sJ, where JUJ denotes the Euclidean norm. Suppose that the correlation function of fYngnZ1
is given by
CovðYs,YtÞ ¼ expð�Jt�sJ2Þ:
From fYngnZ1 we shall define two nonstationary and isotropic random fields whose correlations decay to zero at a ratewhich is not too slow, that is, jri,jjorðji1�j1j,ji2�j2jÞ
, for some sequence frngn2N20�f0g
verifying (2.4) and (2.5).Let fXngnZ1 be such that
Xs ¼msþYs,
where ms is a real valued function. Its covariance function and expectation are
CovðXs,XtÞ ¼ CovðYs,YtÞ, EðXsÞ ¼ms,
and
jCovðYs,YtÞj ¼ expð�½ðt1�s1Þ2þðt2�s2Þ
2�Þorðjt1�s1j,jt2�s2jÞ
,
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L. Pereira / Journal of Statistical Planning and Inference 140 (2010) 3567–35763576
with
rðn1 ,n2Þ¼
expð�n1n2Þ, n1,n2 2 N,
expð�n1Þ, n1 2 N4n2 ¼ 0,
expð�n2Þ, n1 ¼ 04n2 2N,
8><>:
which verifies the conditions (2.4) and (2.5).Now, consider the normal random field
Ws ¼ ssYsþZs,
where ss is a real valued function such that, for each s 2 Z2þ , jssjrK , K is a constant, Zs are Gaussian random variables
independent of Ys, with covariance function rðJt�sJÞ ¼ expð�Jt�sJ2Þ. The variance and covariance function of fWsgsZ1 are
VarðWsÞ ¼ s2s , covðWt,WsÞ ¼ ðssstþ1ÞcovðYt,YsÞÞoðK2þ1Þrðjt1�s1j,jt2�s2 jÞ
,
and frngn2N20�f0g
verifies (2.4) and (2.5).
Acknowledgements
We would like to thank the referee’s careful reading of the manuscript which has resulted in improvements to the finalform of this paper. Work partially supported by FCT/POCI2010/FEDER (EVT Project).
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