asymptotic relative efficiency of some joint-tests for location and scale parameters based on...
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Asymptotic relative efficiency of some joint-testsfor location and scale parameters based on selectedorder statisticsA.K. Md. Ehsanesh Saleh a & Pranab Kumar Sen ba Department of Mathematics and Statistics , Carleton university , Ottawa, CANADAb Department of Biostatistics , University of North Carolina , Chapel Hill, H.C., U.S.A.Published online: 27 Jun 2007.
To cite this article: A.K. Md. Ehsanesh Saleh & Pranab Kumar Sen (1985) Asymptotic relative efficiency of some joint-testsfor location and scale parameters based on selected order statistics, Communications in Statistics - Theory and Methods,14:3, 621-633, DOI: 10.1080/03610928508828938
To link to this article: http://dx.doi.org/10.1080/03610928508828938
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Deparrmen-c uf k l a t h ~ m a t i c s and S t a t i s t i c s C a r l e t o n Univers i ty Ottawa, CANADA
Key NO&& t; P b e n : ABLUE; anymp&Ac o p t i m a L ~ y ; a,lympto-tic x e L a t i v e ed&cierzcy; BLUE; g e m a L i z e d L e n n t n q m e ~ ; _ae m d i z e d v a n i a YEP_; RocaRio c d e wu d d ; qua nLLte ~ u m t i a n; b p a c i q n ; nymmdhic d i h t h i b d i u n.
ABSTRACT
For a l o c a t i o n - s c a l e d i s t r i b u t i o n , based on few s e l e c t e d o r d e r s t ~ t i s t i c s ~ . - i o i ~ l t - t e s t s f o r t h e I n r a t i o n and scale parameters a r e cons idered . I n t h e l i g h t o f t h e asympto t ic r e l a t i v e e f f i c i e n c y r e s u l t s , op t imal spac ings o f t h e o r d e r s t a t i s t i c s a r e s t u d i e d (and t h e i r d u a l i t y t o t h e e s t i m a t i o n problem i s d i s c u s s e d ) .
1. INTRODUCTION
L e t X n , l < ..- < X be t h e o r d e r s t a t i s t i c s of a sample n:n
of s i z e n randomly drawn from a l o c a t i o n - s c a l e d i s t r i b u t i o n F ,
where
F i s a s p e c i f i e d d i s t r i b u t i o n f u n c t i o n ( d - f . ) w i t h a cont inuous 0
p r o b a b i l i t y d e n s i t y f u n c t i o n (p.d.f . ) fo, and 0 and y (> 0) a r e
unknown l o c a t i o n and s c a l e parameters . Le t Q0 = CQ ( t ) , 0 < t < l ) , 0
t h e q u a n t i l e f u n c t i o n , d e f i n e d by
Copyright O 1985 by Marcel Dekker, Inc.
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~ e t z = X . , X ) ' he a v e c t o r of k ( 2 1) s e l e c t e d -n n : r
I k s t a t i s t i c s w i t h t h e ranks r
11---' rk, determined by t h e spacing-
v e c t o r X = (X . = = = ; X ! ' bv l e t t i n g - 1' k -
where [s] i s t h e l a r g e s t i n t e g e r con ta ined i n s . We l e t t h e n
= 1 , . , , 1 * and 5 = 81 + ya. - - (1.6) - Then [viz . , M o s t e l l e r (1946) 1, whenever f (a,) > 0 , 1 j 2 k , a s
0 I n i n c r e a s e s
Note t h a t a and a r e known, b u t 5 and y a r e unknown, Ogawa - (1951) [see Sarhan and Greenberg (1962)] i n c o r p o r a t e d (1.4)-(1.7)
i n -&e foL?ulation of a s y m p t o t i c a l l y b e s t l i n e a r unbiased
e s t i m a t o r s (ABLUE) o f ( 8 , y ) , based on Zn, which a r e g iven by
where
- 1 kl j l l Y 1, k12=k21=a'~-11, k 2 2 = ~ 1 ~ - 1 a ( n o n s t o c h a s t i c and known) - - - - - - - - -
c1.9)
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ASXQTOTIC RELATIVE EFFICIEXCY 623
IY = Z and M = a ' ~ / ~ z (stochastic) (1.10) I n - -. -n 2n - .. -n
and hence, by (1.71 and (1 -11) we have
r , e t 2 = [ [ I . . ) ) be t h e Fisher ( loca t ion-sca le) information matrix - - - - 1 3
of F (i=e= of F when 0 = 0 , y = 1). We assume t h a t 1 i s a 0
f i n i t e , p o s i t i v e d e f i n i t e (p.d.j matrix and denote i t s detaLqinant
by / i ! . Tben, t he ABLUE of (0 ,y) ' based on a l l t he n order - -
s t a t i s t i c s [viz. Ang (1955)1, denoted by (8' y j ' , has the n n
following property [viz., Chernoff, Gastwirth and Johns (1967) 1:
d i s t r ibu t io r
Note t h a t 5
To study the asymptotic r e l a t i v e e f f i c i ency (A.RE.) of A A
(en, Y ) with r e spec t t o (8,, y n ) , we make use of (1.12) and (1.131 n
and employ the generalized var iance of t he two asymptotic
IS, which leads t o the A.RE.
depends on @ and (and hence, on and f 0 ( ' 1 ) . - Dow
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,o, For a given p.d. f. f and k (2 l) , l e t us d e f i n e f = i ( 9 , . . . ,*,I
0 - h. r
responding t o a given A. This cho ice ( A " ) of t h e spac ings of t h e - o r d e r s t a t i s t i c s l e a d t o a maximum of t h e A.X.E. i n (1.14) . For
77-w. ,,,;,,, ,..>" F and s p e c i f i c k (2 I ) , t h e optimum choice o f h0 has been 0 -
s t u d i e d (numer ica l ly ) by v a r i o u s workers [ v i z . , Sarhan and Greenberg
(1962) and Kul ldor f f (1977) 1.
We a r e p r i m a r i l y i n t e r e s t e d h e r e i n t h e ( d u a l problem) j o i n t -
t e s t of
based on Z , where 8 y a r e s p e c i f i e d . i n t h i s c o n t e x t too , o u r - n 0' 0 main emphasis is on t h e A.R.E. r e s u l t s and on a s y m p t o t i c a l l y o p t i -
mal s p a c i n g s a s wel l . The proposed t e s t s and t h e a l l i e d
,: -L. -21 . . .L: _ _ L L _ _ _ _ _ _ _ --.-, ,-,7T+?:--J : - C ~ C + ~ , - , rnh- ,,ir: re=?:!+.; i i i a i i i i i u i i i i i i ;;u;';i; -,, ,,,,;;;c; A;; -,,,l-., -. -..- ------- on A.R.E. and op t imal spac ings a r e p r e s e n t e d i n S e c t i o n 3. Some
g e n e r a l remarks a r e appended i n t h e concluding s e c t i o n .
2. THE PROPOSED JOINT-TESTS
Cons ider f i r s t t h e q u a d r a t i c form
By (1.12) and t h e Cochran theorem, we conclude t h a t under H 0
o r Ln h a s a s y m p t o t i c a l l y t h e c e n t r a l c h i s q u a r e d i s t r i b u t i o n w i t h 2
degrees o f freedom. When H does n o t h o l d , b u t H does, 0 A
-1 0 - 2 2 n Ln converges i n p r o b a b i l i t y t o yo {k (8- 8 ) +
11 0 2
2k12(0-00) (y- yo) + k (y- yo) I = A > 0 , s o t h a t iO tends 22 . n
t o m ( i n p r o b a b i l i t y ) , a s n + T h i s s u g g e s t s t h e use of
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rhe right hand side tail of the discxibution of LO as t h e 0,
appropriark critical re:i=~; tke critical value (of 1 , , I1 , E li
~orres~urldinj r o G s;czified o i g n i ficance level E (iic E < 1) , - - - 7 ' " ' n P C LVfi , --2-- x ~ ( E ) , the cpper it3024 p o i n t sf t.+ie ccntral
chisq~are d.f. with 2 DF.
Along with this asymptoric test, we like to c ~ n s i d e r ,
side by side, another verslon, wnere insiead of die asynptotic
momenis of Z , thc exact ones are used in the construction of the -n
test statistic. For this purpose, .VIE define for every n (2 .- k i ,
For various F and specific (n,k), '3 and V have been 0 - n -n
comp~dted and tabulated [viz. Sarhan and Greenberg (19623 1. Then,
by the generalized least squares (GLS) principle, the BLUE of
( 8,y) based on Z is given by -, n
where
Parallel to (2.11, we consider then tne test statistic
0 * (2.6) To study the affinity of L and L we denote by
n n
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Then, we have by 12.3)-(2.5) and (2.7);
so that by (1.11) and (2.8),
At this stage, we make use of the moment-convergence results of
sample yuaniiies [see, for example, Sen (1959); and conclude that
under tne assumed regularity conditions,
so that by (2.9)-(2.12), A
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Havinq obtained t h l s asymtotic equivalence, we conclude that &
L i has asymptotically the same distribution (under H ) as 0
LO .
To find the asymptotic distribution theory under HA in (1.16), n
we coilsider a seyueilce of alternatives {A f , where under A , n n
where 6 = (6 6 ) ' ( f 0 ) is some fixed vector. Using (1.12) , 1' 2 -
!2.15), (2.11 and the Cochran theorem, one aqain claims that
under {A j , LO (or L* ) has asymptotically non-central n
chi square distribution 2 DF and non-centrality parameter
- - Side by side, if we would have used the ABLUE (8 ,
n Yn) in (1.13) and a quadratic form in this vector (as in (2.6)),
- then we have a test statistic L- (based on the entire set of
1,
order statistics) which, under (A_} , will have asymptotically I I
non-central chisquare distribution with 2 DF and non-centrality
parameter
where ? is defined after (2.12) .
3. A.R.E. RESULTS
0 TO compare L (or L* and , we note that the classical
n n n Pitman-A.R.E. result is applicable here (both having the same
asymptotic size and similar non-central distributions), so that,
we have by (2.16) and (2.17),
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Vnl ike t h e c a s e of unigarameter t e s t s : h e r e (3 .1 ) depends: I n
g e n e r a l , on t h e d i r e c t i o n - c o s i n e s of 6 , s a t h a t ( 3 . 1 ) i s a - f u n c t i o n of K I and v i where 6 = 6 cos 1) and 8 = 6 s i n v - - 1 2 ( 0 2 V 2 2 n ) . One may t h e r e f o r e be i n t e r e s t e d i n s tudying t h e
range of v a r i a t i o n of (3.1) over t h e range of v a r i a t i o n of V.
Note t h a t by t h e Courant theorem on t h e extrema of t h e r a t i o
of two q u a d r a t i c f o r m [ c ; f = R.ao (1973, p ; 5 (? ) ] ; we have
0 - -1 i n £ A.R .E . (1 , i j = e i K i I ) = ch ( K 1 ) = e say ( 3 , 2 ) V 0 - - 2 -- 2
0 -1 SUP R.R .E . i ~ O , i ) = e (K,I) = ch ( K T ) = e , say - - 1 -- 1
( 3 . 3 ) v
wnere cn ( a ) and ch ( ' 1 s t a n d f o r t h e l a r g e s t and s m a l l e s t 1 2
c h a r a c t e r i s t i c r o o t s . Thus.
and % = K T - ' / ' - - , ( 3 . 5 )
With t h e s e r e s u l t s i n hand, we proceed now t o c o n s i d e r t h e
a s y m p t o t i c a l l y op t lmal cho lce of: t h e spac lng A, f o r a given - k(, 2) and F . - 0
(i) Max-min o p t i m a i i t y : For a g iven k
A , i n such a way t h a t f o r t h e corresponding - and F we choose
0
K ( = K ( A ) ) ,
Thus, t h i s op t imal cho ice of r e l a t e s t o t h e maximization of t h e
minimum A.R.E. (over V €[0,2n]) i n ( 3 . 2 ) .
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( i i j fi-oUtiTi-?:L... I a i r i v . Note t h a t r h e Gaussian c u r v a t u r e of
t h e asympto t ic power f u n c t i o n of 1': under ] i n ( 2 . 1 5 ) , n
a t t h e null p i n k ,3 = 3 , is maximize2 W ~ E E i s a maximum,
4 . e . , 1 KT-' i s a rna:<i~:Grn ( a s 1 does n o t &pen6 on A , b u t -- - - K does s o ) . By (3 .5 ) , t h i s amounts t o maximizing - 7 4 - 1,
Je e = - ( j j, / I , j '? by ttle d e s i r e d ~ h c . i , c ~ _ of ). . For 1 2 -- - - -
t h e D - o p t i m a l i t y , we may r e f e r t o I saacson (1951) , f o r a very
e l a b o r a t e discussion. i n t h i s s e n s e , ~ i i e opilitiai cho ice of
X a g r e e s w i t h t h a t i n (1.14) -( 1 . l 5 ) , and hence, t h e d i s c u s s i o n - fo l lowing (1.15) a l s o p e r t a i n s t o h e r e .
(iii) Trace-op t imal i ty : We conceive of a p a r t i t i o n of t h e
parameter space of (under ( 2 . 1 5 ) ) by means of t h e e l l i p t i c a l
con tours :
where H i s d e f i n e d by (2.17) . Note t h a t i = c <=> 6 ' I6 = c y i = c* * - --
( O - < c < m! On t h e s u r f a c e of t h i s e l l i p s e we a s s i g n a uniform - , - - p r i o r d i s t r i b u t i o n of 6 . Note t h a t on a -contours , t h e a s y n p t o t i c
G * - power of L ( o r 1 ) may depend on V . I n t e g r a t i n g o u t (3 .1 )
7 'l
w i t h r e s p e c t t o t h e uniform p r i o r d i s t r i b u t i o n of 6 on a - A-contour, we o b t a i n an average (over L') A.P.E., and t h i s reduces
t o t h e t r a c e c r i t e r i o n :
Thus, one may choose t h e spac ings 1 i n such a way t h a t (3 .8 ) i s - a maximum i . e . , we have an a s y m p t o t i c a l l y op t imal average A.R.E.
Note t h a t does n o t depend on t h e cho ice of 5 ( b u t , K does s o ) , - and hence, we need t o choose 1 , i n such a way t h a t -
1 , , d l 1 22 -[i- in, r i 2k (A) 112 + 011 1 = maximum 2 11 - 12 - D
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SALEH AND SEN
I n g e n e r a i , t h e s o l u r i o n s i n (i) , ( i i j and (iii! a r e nor
rhe s a x e . Ir, a rna3orir.i of tne c a s e s , r i s a s y i m e t r i c 6. f . , 0
~ . e . ,
s o t h a t
(3.12)
Moreover; by irn.posing i n v a r i a n c e and symmetrv on t h e BLUE; T,qe
may r e s t r i c t o u r s e l v e s t o t h e c l a s s of A f o r which A + A ,=l, -" i k + l - I
f o r every j = 1 , 2 , , . . , [ (k+1) /2], and t h i s would imply , -by v i r t u e
of ( 1 . 4 ) , (1 .51 , (1.9) and (3.10) t h a t k = k = 0. So t h a t 12 2 1
(3.121 reduces t o
AS such (i) Maximum o p t i m a l i t y i s ob ta ined by maximizing -1
k22722 over X .
(ii) D-optimali ty i s o b t a i n e d by maximizing / k l - l l over A, - - and
( i i i ) Trace-op t imal i ty i s ob ta ined by maximizing k 1-1 + 11 11
k I-' over . 2 2 22 D
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rhem wlrh r h r e e examples.
(a! Normal case; Here i = ii i = 2, 1 = 1 = 0. 11 . . 2 2 21 12 -. 1 7. ,Inen, for maxi-mi? 3 p t i i ~ , a l i t y we maximize - 5 Pis r e s u l t s
2 22 a r e a v a i l a b l e i n Oqawa (1951) [ v i z . s e e Sarhan and Greemberg
1962 T a X e 10 .I2 - 4 1 . The r?a:*_,rr.&~ efficiencies f o r k = 2 (2) 6 a r e
f o r t r a c e op t imal l t i ; we maximize k + L k . 'Thc op t imal 11 2 22
spac ings d i f f e r from t h a t of D-optimali ty r e s u l t s and t h e
e f f i c i e n c i e s f o r k = 2 ( 2 ) 1 0 are ,6407, .8286, .9009, .9359 and
.9552. A l l t h e t h r e e o p t i m a l i t y r e s u l t s a r e d i f f e r e n t i n t h i s
c a s e
(b j c a u c h y ~ : Here 1 = i = ' i = i = O . Then, 0 11 22 2' 12 21
f o r maxi-min o p t i m a l i t y we maximize 2k9?. This has been done L. L
by Chan (1970) . For k = 2 ( 2 ) 10 , t h e e f f i c i e n c i e s a r e .8106,
4kllkl2. For k = 2 ( 2 ) 1 0 , t h e e f f i c i e n c i e s a r e -4677, .7659,
.8735, .931? and ,9469, and f i n a l l y , f o r t r a c e o p t i m a l i r y w e
maximize k + k which maximizes k k ( s e e Cane, 1 9 7 4 ) . li 12 11 22 - - ~. r u r k = 2 ( 2 ) 1 0 t h e e f f i c i e n c i e s a r e .6840, ,8752, .9346, .9600 and
.9732. The D-optimali ty and Trace-op t imal i ty g i v e t h e same spac ing
and t h e A m i s unique.
( c ) Double-exponential F : Here = I =1, 7 = I =o, 0 I11 22 12 21
Then f o r maxi-min o p t i m a l i t y , we maximize k This h a s been done 22'
by Cheng (1978) . For k = 2 ( 2 ) 10 t h e e f f i c i e n c i e s a r e .6476,
.8202, .8910, 9269 and -9476. For D-optimali ty , we maximize
k k The r e s u l t s may be o b t a i n e d from Cheng (1978) . 11 12 '
For k = 3 ( 2 ) 1 1 , t h e e f f i c i e n c i e s a r e -6476, -8202, .8910, .9269
and .9476 and f i n a l l y f o r t r a c e - o p t i m a l i t y we maximize k + k 11 1 2 '
The average e f f i c i e n c i e s a r e then .8238, .9101, .9455, .9639,
.9738. The optimum s p a c i c g s may be ob ta ined by us ing t h e r e l a t i o n Dow
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between optimum spac ing of doulole-exponential d i s ~ r i b u c i o n and
t h e e x p o n e n t i a l d i s t r i b u t i o n given by Cheng (i978j.
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Sen , P.K. (1559). On moments of s m p i e q u a n t i l e s . C a l c u t c a S t a t i s t i c a l A s s t n . B u l l e ~ i n 9, pp. 1-9.
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