REPLICATION VARIANCE ESTIMATION UNDER TWO-PHASE SAMPLING IN THE PRESENCE OF NON-RESPONSE
|
|
- Emil Holland
- 5 years ago
- Views:
Transcription
1 STATISTICA, anno LXXIV, n. 3, 2014 REPLICATION VARIANCE ESTIMATION UNDER TWO-PHASE SAMPLING IN THE PRESENCE OF NON-RESPONSE Muqaddas Javed 1 Natonal College of Busness Admnstraton and Economcs, Lahore, Pakstan. Zahoor Ahmad Department of Statstcs, Unversty of Gujrat, Gujrat, Pakstan. Muhammad Hanf Natonal College of Busness Admnstraton and Economcs, Lahore, Pakstan. 1. Introducton Two phase samplng ntroduced by Neyman 1938 he gve the concept of use of auxlary nformaton to get maxmum response about the requred nformaton. He also gave the dea of the use of stratfcaton n the second phase. Hansan and Hurwtz 1946 suggest the survey statstcan to get maxmum response by recontactng wth expansve method to noespondent. A smple method of double samplng for stratfcaton s proposed and the classcal non-response theory s obtaned as a specal case by Rao Rato and regresson estmator of the populaton mean was proposed by Cochran 1977 for the study varable n whch nformaton on the auxlary varable s obtaned from all the sample unts. More mprovement n populaton mean n the presence of noesponse usng auxlary nformaton was suggested by Rao Sngh et al proposed a class of estmators based on general samplng desgns for populaton parameter utlzng auxlary nformaton of some other parameters. They also studed the general propertes for the suggested class and fnd the asymptotc lower bound to the mean square error of the estmators belongng to the class. They 1990 also proposed several unbased rato and product estmators wth ther expressons of asymptotc varances usng Jackknfe technque n two-phase samplng. Double expanson estmator DEE and reweghted expanson estmator REE are developed by Kott and Stukel 1997 for regresson estmator n two phase stratfed samplng. Khare and Srvastve 1997 proposed some mproved estmator of Rato and Regresson usng auxlary nformaton n the presence of non response.precse varance estmator s always a choce of survey statstcan; replcaton varance estmaton s a tool whch overcomes ths problem. The concept of the jackknfe was ntroduced by Quenoulle 1956 n connecton wth reducton 1 Correspondng Author. E-mal: muqaddas.javed@uog.edu.pk
2 248 M. Javed, Z. Ahmad and M. Hanf of bas for nonlnear estmaton. The possblty of usng ths technque for the purpose of varance estmaton was proposed by Tukey He 1958 suggested that each jackknfe replcate estmate mght be regarded as an ndependent and dentcally dstrbuted random varable, whch n turn suggests a very smple varance estmator. Jones 1958 modfed the jackknfe varance estmator for the populaton mean under two phase samplng for rato estmator. Durbn 1959 may have been the frst to use t n the context of fnte populatons. Rao and Shao 1992 proposed a consstent jackknfe varance estmator for reweghted expanson estmator n the context of hot deck mputaton. Bredt and Fuller 1993 suggested a replcaton varance estmator for multphase samples. Ther 1993 procedure s partcularly applcable f the frst phase and second phase prmary samplng unts are the same and f there are at least two second phase prmary samplng unts n each frst phase stratum. Rust and Rao 1995 provde comprehensve overvews oeplcaton varance estmaton topc. A jackknfe procedure has been suggested for the rato estmator by Rao and Stter 1995 and for the regresson estmator by Stter Kott 1990 dscuss varance estmaton n a stuaton the stratfed desgn for the second phase dffers from the stratfed desgn for the frst phase, and suggests a jackknfe estmator of varance for a partcular two phase estmator. Kott and Stukel 1997 concluded that the jackknfe varance estmator works well for the reweghted expanson estmator f the frst phase samplng rate s neglgble.fuller 1998 gve the estmaton of the varance of regresson estmator for a two phase sample and replcaton varance estmator s developed n second phase sample. Km and Stter 2003 developed a replcaton varance estmator for two phase samplng when the second phase sample s much smaller than the frst phase sample; Method s appled to DEE and REE. A consstent varance estmator whch s applcable n DEE and REE n two phase samplng was developed by Km, Navarro and Fuller 2006 when the second phase s stratfed. Wolter 2007 provde comprehensve overvews oeplcaton varance estmaton topc. Ramasubramanan et al proposed a two new jackknfe method as the counterparts of two exstng Bootstrap methods of varance estmaton under two phase samplng.farrell and Sngh 2010 dscuss the problem of estmatng the varance of varous estmators of the populaton mean n two phase samplng by jackknfng the two phase calbrated weghts. They 2010 also estmated the varance of the chaato and regresson type estmators due to Chand 1975 usng the jackknfe. Km and Yu 2011 developed a replcaton based bas adjusted varance estmator that extends the method of Km, Navarro and Fuller 2006 under two phase samplng. In case of non-response the sampler has an ncomplete sample data that affects the qualty of estmates of the unknown populaton parameters. The problem was frst consdered by Hansen and Hurwtz 1946, n whch the populaton was dvded nto groups of respondents and non-respondents and the sample sze to be attempted at the frst occason and the proporton of non-respondents to be repeated n the remanng sample was also determned. They constructed the estmate of the populaton mean by combnng the data from the two attempts and derved the expresson for the samplng varance of the estmates and optmum samplng fracton among the noespondents s also obtaned.
3 Replcaton varance estmaton n the presence of non-response 249 In ths paper, we propose some new replcaton varance estmators n the presence of non-response under two phase samplng. The estmators are proposed n two dfferent stuatons, Km and Yu 2011 methodology s used for the replcaton. The rest of the paper s organzed as follows. In secton 2, the four estmators are developed under two phase samplng n the presence of noesponse and ther replcaton varance estmators are developed n the Secton 3. In Secton 4, proposed method s extended for DEE-type estmators and REE-type estmators. In secton 5, a lmted smulaton study s presented. Concludng remarks are made n last secton of the paper. 2. Proposed Estmators of Mean under Two-phase Samplng n the Presence of Non-response In ths secton, we suggest two phase stratfed estmators for estmatng populaton mean of varable of nterest n the presence of noesponse. The estmators are proposed for two dfferent condtons. Estmaton of mean n the presence of non-response at frst phase Estmaton of mean n the presence of non-response at second phase 2.1. Estmaton of Mean n the Presence of Non-response at Frst Phase Sample Here, we suggest two phase stratfed estmators for estmatng populaton mean of the study varable when non-response s present on frst phase under the followng two dfferent stuatons. Estmaton by gnorng non-respondng unts Estmaton by re-contactng noespondng unts Estmaton by Ignorng Non-respondng Unts In ths secton, we smply assume the stuaton the frst phase sample of sze n s selected wth smple random samplng wthout replacement SRSWOR from a fnte populaton of sze N and selected frst phase sample s dvded nto two parts, respondent and non-respondent n r. Usng the nformaton obtaned from frst phase respondng sample, t s stratfed nto L strata for second phase samplng. We have h frst phase respondng sample elements and assume A rh1 be the set of ndces for the frst phase respondng sample elements n stratum h. A stratfed random sample of sze n wth sample sze n rh n stratum h s selected n the second phase samplng. Where n = L n rh and h/n s samplng rate for each stratum.
4 250 M. Javed, Z. Ahmad and M. Hanf The study varable y s observed n the second phase sample; the populaton means of y s estmated by t 1 = 1 L h n y rh, 1 A rh2 rh A rh2 s the set of ndces for the second phase sample elements that belong to stratum h. Usng proof 1 of Appendx, the varance of t 1 can be wrtten as V t 1 = E n 1 r 1 f 1 w h ȳ rh1 ȳ ] rh n 1 rh f 1 whs 2 2 rh1, 2 ȳ 1 = =1 y r/ be the mean of the frst phase sample and the consstent estmator of the varance of t 1 can be derved by replacng ȳ h1 and s 2 h1 by ther estmates ȳ rh2 = rh A rh2 y r and s 2 rh2 = n rh 1 1 A rh2 y r ȳ rh2 2 respectvely n 2. So the consstent estmator of 1 s ˆV t 1 = n 1 r 1 f 1 w h ȳ rh2 ȳ f 1 = N, ȳ 2 = L w hȳ h2 and w h = h. rh n 1 rh f 1 whs 2 2 rh2, Estmaton by Re-contactng non Respondng Unts Here, we develop an estmator by the theory of Hansan and Hurwtz 1946 to re-contact the non-respondng unts wth a dfferent method. In ths stuaton the frst phase sample unts s stratfed for both respondng unts and nonrespondng unts n r nto L strata for second phase samplng.we have h frst phase respondng sample elements and assume A rh1 be the set of ndces for the frst phase respondng sample elements n stratum h and we also have n rh frst phase non-respondng sample elements n stratum h. In the second phase samplng, a stratfed random sample of sze n 1 s selected from respondng unts wth sample sze n 1h n stratum h, and a stratfed random sample of sze n 2 s selected from re-contacted frst phase non-respondng unts wth sample sze n 2h n stratum h, n 1 = L n 1h, n 2 = L n 2h and a fxed samplng rate for each frst phase respondng stratum at second phase s n 1h /h and frst phase non-respondng stratum at second phase s n 2h /n rh. The study varable y s observed n the second phase sample, the populaton mean of y s estmated by t 2 = w 1 h n y rh + w 2 A rh2 1h n r A rh2 n rh n 2h y rh, 4 w 1 = n 1, w 2 = n 2 and A n r rh2 s the set of ndces for the second phase respondng sample elements that belong to stratum h, A rh2 s the set of ndces
5 Replcaton varance estmaton n the presence of non-response 251 for the second phase re-contactng sample elements that belong to stratum h. Usng the result gven n the proof 2 of Appendx, the varance of estmator t 2 can be wrtten as ˆV t 2 = n 1 1 f 1 n 1 r + n 21 f 2 n 1 r w h ȳ rh2 ȳ r2 2 +w1 2 wh ȳ rh2 ȳ r2 2 +w h 1 2h f 1 n 1 whs 2 2 rh2 rh f 2 n 1 wh 2 s 2 rh2, 5 rh 2.2. Estmaton of Mean n the Presence of Non-response at Second Phase Sample In ths secton we agan suggest two new estmators for the populaton mean n two phase stratfed desgn when non-response s present on second phase under the followng stuatons. Estmaton by gnorng non-respondng unts Estmaton by re-contactng noespondng unts Estmaton by Ignorng Non-respondng Unts In ths secton, we assume the stuaton the frst phase sample of sze n s selected wth SRSWOR from a fnte populaton of sze N. Usng the nformaton obtaned from frst phase sample, t s stratfed nto L strata for second phase samplng. We have n h frst phase sample elements and assume A h1 be the set of ndces for the frst phase sample elements n stratum h. A stratfed random sample of sze n wth sample sze n h n stratum h s selected n the second phase samplng of whch n rh respond and n rh non-respondent. Where n = L n h = L n rh + n rh and a fxed samplng rate for each stratum s n rh /n h. The study varable y s observed n the second phase sample; the populatons mean of y s estmated by t 3 = 1 n n h n A rh2 rh y h, 6 A rh2 s the set of ndces for the second phase sample elements that belong to stratum h. The varance of t 3 can be wrtten as V t 3 = E n 1 1 f1 wh ȳ rh1 ȳ ] rh n 1 h f 1 wh 2 s 2 rh1. 7 A consstent estmator of the varance of t 3 can be derved by replacng ȳ h1 and s 2 h1 wth ther estmates ȳ rh2 = rh A rh2 y r and
6 252 M. Javed, Z. Ahmad and M. Hanf s 2 rh2 = n rh 1 1 A rh2 y r ȳ rh2 2 respectvely n 7. So the consstent estmator of 6 s ˆV t 3 = n 1 1 f 1 wh ȳ rh2 ȳ f 1 = n N, ȳ 2 = L w hȳ rh2 and w h = n h n. rh n 1 h f 1 wh 2 s 2 rh2, Estmaton by re-contactng noespondng unts In ths secton, we assume the stuaton the frst phase sample of sze n s selected wth SRSWOR from a fnte populaton of sze N. Usng the nformaton obtaned from frst phase sample, t s stratfed nto L strata for second phase samplng. We have n h frst phase sample elements and assume A h1 be the set of ndces for the frst phase respondng sample elements n stratum h. A stratfed random sample of sze n wth sample sze n h n stratum h s selected n the second phase samplng of whch n rh respond and n rh non-respondent. Where n = L n h = L n rh + n rh and a fxed samplng rate for each stratum respondng unt s n rh /n h and non-respondng unt s n rh /n h. The study varable y s observed n the second phase sample, the populaton mean of y s estmated by t 4 = 1 n w n h h1 A rh2 n rh y rh + 1 n w n h h1 n rh A rh2 y rh, 9 wh1 = n h n and A rh2 s the set of ndces for the second phase respondng sample elements that belong to stratum h and A rh2 s the set of ndces for the second phase re-contactng sample elements that belong to stratum h. The varance of t 4 can be wrtten as ˆV t 4 = + w wh1 2 ] n 1 h + wh1n 2 1 rh n 1 h w f1 wh 2 s 2 rh2 w wh1 2 ] n 1 h + wh1n 2 1 rh n 1 h w f1 wh 2 s 2 rh w n 1 1 f 1 w h ȳ rh2 ȳ ȳ rh2 ȳ 2 2], f1 = n N, ȳ 2 = L w hȳ rh2, w = n2, ȳ n 2 rh2 = rh ȳ rh2 = rh A rh2 y r. A rh2 y r, w h = n h n,
7 Replcaton varance estmaton n the presence of non-response Replcaton Varance Estmaton of Proposed Estmators In ths secton we proposed some replcaton varance estmators for the estmators developed n secton 2, the proposed method of jackknfe replcaton varance estmaton of Km and Yu 2011 by successvely deletng unts from the entre frst phase sample s adopted. In ths method frst phase samplng rate s not necessarly neglgble and does not requre addtonal replcates for bas correcton n the varance estmaton. The full jackknfe varance estmator of 1 s t k 1 = 1 L n r n rhȳk rh2 ˆV J1 = c k t k 1 t 1 2, 11 and k s the ndex of the unts deleted n the jackknfe replcates, A 1 s the set of ndces for the frst phase sample elements and c k s a factor assocated wth replcate k determned by the replcaton method { 1 n nr 1 rh = 1 h 1 f k A rh1 1 1 h f k / A rh1 n r and { n rh2 = h 1 1 n hȳrh2 y rk f k A rh2 ȳ rh2 f k / A rh2. ȳ k The full jackknfe varance estmator of 4 s ˆV J2 = c k t k 2 t 2 2, 12 t k 2 = w1 L n r n rhȳk rh2 + w2 L n r n rhȳk rh2 { 1 n n nr 1 rh = 1 h 1 f k A rh1 r 1 1 h f k / A rh1, { 1 n rh = n r 1 1 n rh 1 f k A rh1 n r 1 1 n rh f k / A rh1, n r and { n rh2 = 1h 1 1 n 1hȳrh2 y rk f k A rh2 ȳ rh2 f k / A rh2 ȳ k { n rh2 = 2h 1 1 n 2hȳ rh2 y rk f k A rh2 ȳ rh2 f k / A rh2. ȳ k Smlarly the full jackknfe varance estmator of 6 s ˆV J3 = c k t k 3 t 3 2, 13
8 254 M. Javed, Z. Ahmad and M. Hanf t k 3 = 1 L n n hȳk h2 1 n n h = { n 1 1 n h 1 f k A h1 n 1 1 n h f k / A h1, { and ȳ k n h2 = rh 1 1 n rhȳh2 y k f k A rh2 ȳ h2 f k / A rh2. Also the full jackknfe varance estmator of 9 s ˆV J4 = c k t k 4 t 4 2, 14 t k 4 = 1 L n u h1n hȳk rh2 + 1 L n u h1n hȳk rh2 ȳ k 1 n n h = { n 1 1 n h 1 f k A h1 n 1 1 n h f k / A h1, { n rh2 = rh 1 1 n rhȳrh2 y rk f k A h2 ȳ rh2 f k / A h2, { n rh2 = rh 1 1 n rhȳ rh2 y rk f k A h2 ȳ rh2 f k / A h2, ȳ k and u h1 = n 1 1 n h 1]. 4. Extenson of Proposed Estmators Here, we consder some extensons of the proposed replcaton method by DEE and REE under the condtons defned n secton 2 for proposed estmators DEE and REE n the Presence of Non-response at Frst Phase Sample The DEE and REE type estmators were developed for the two stuatons whch was dscussed n the secton Estmaton by Ignorng Non-respondng Unts Let w r = π 1 1 π 1 = Pr A rh1 s the frst phase samplng wght for respondng unts and wr = π 1 2 π 2 = Pr A rh2 A rh1 be the nverse of the condtonal probablty of respondng unts n the second phase, then we develop the followng DEE and REE. The proposed DEE for ths stuaton s t 1DEE = 1 N A rh2 w r w ry, 15
9 Replcaton varance estmaton n the presence of non-response 255 the replcaton varance estmator of 15 s developed by the Km and Yu 2011 method whch s as ˆV J1DEE = 2 t k 1DEE 1DEE t, 16 t k 1DEE = 1 N L c k Ah1 wk r w 1 r A h2 r w 1 r Ah2 wk r y and c k s a factor assocated wth replcate k determned by the replcaton method. The proposed REE estmator for ths stuaton s t 1REE = 1 N wh1 ȳ h2, 17 ȳ h2 = A rh2 w r wr 1 A rh2 w r wr y and w h1 = A rh1 w r. The replcaton varance estmator of 17 s as ˆV J1REE = c k t k 1REE t 1REE 2, 18 and t k w k h1 ȳ k h2 1REE = 1 L N k w h1 = A rh2 r, ȳk h2 = A rh2 r w r 1 A rh2 r w r y Estmaton by Re-contactng Non-respondng Unts Let we consder w r and wr as gven n Stuaton-I, further we let w r = π 1 r1 π r1 = Pr A rh1 s the frst phase samplng weght for re-contacted respondng unts and w r = π 1 r2 π r2 = Pr A rh2 A rh1 be the nverse of the condtonal probablty n the second phase of re-contacted respondng unts, then we develop the followng DEE and REE. The proposed DEE for ths stuaton s t 2DEE = 1 w r w N ry r + w r w r y r 19 A rh2 A rh2 and replcaton varance estmator of 19 s as ˆV J2DEE = c k t k 2DEE t 2DEE 2, 20 t k 2DEE = 1 N A rh1 r w 1 r A rh2 r w 1 r A rh2 r y r
10 256 M. Javed, Z. Ahmad and M. Hanf + w A rh1 k r w 1 r w A rh2 k r w 1 r A rh2 r y r and c k s a factor assocated wth replcate k determned by the replcaton method. The proposed REE for ths stuaton s t 2REE = 1 N wh1 ȳ rh2 + w h1 ȳ rh2, 21 wh1 = w r, ȳ Arh1 rh2 = w rw 1 Arh2 r A rh2 w r wr y r, w h1= A rh1 w r and ȳ rh2 = w r w r 1 w r w A rh2 A rh2 The replcaton varance estmator of 21 s ˆV J2REE = c k t k 2REE = 1 L k N w h1 ȳ k rh2 + h1 ȳ k rh2 ] r y r. t k 2REE t 2REE 2, 22 1 ȳ k rh2 = A rh2 r w r A rh2 r w r y r, h1 = A rh2 k w h1 = A rh2 r and ȳ k rh2 = A rh2 r w r 1 A rh2 r r, w r y r DEE and REE n the presence of non-response at second phase In ths secton we agan develop two new estmators of DEE and REE for the two stuatons dscussed n secton Estmaton by gnorng non-respondng unts Let w = π 1 π = Pr A h1 s the frst phase samplng weght and w = π 1 r π r = Pr A rh2 A h1, be the nverse of the condtonal probablty n the second phase respondng unts, then we developed DEE and REE by gnorng second phase non-respondng unts. The proposed DEE estmator for ths stuaton s t 3DEE = 1 N and replcaton varance estmator of 23 s ˆV J3DEE = c k A h2 w w y 23 t k 3DEE t 3DEE 2, 24
11 Replcaton varance estmaton n the presence of non-response 257 t k 3DEE = 1 N L Ah1 wk w 1 A rh2 w 1 wk Arh2 y and c k s a factor assocated wth replcate k determned by the replcaton method. The proposed REE estmator for ths stuaton s t 3REE = 1 N wh1 ȳ rh2, 25 wh1 = w Ah1 and ȳ h2 = w w 1 Arh2 A rh2 w w y r. The replcaton varance estmator of 25 s ˆV J3REE = c k t k 3REE t 3REE 2, 26 and t k 3REE = 1 L k N w h1 ȳ k rh2, 1 ȳ k rh2 = A rh2 w A rh2 w y r, h1 = A h Estmaton by re-contactng noespondng unts Consder w and w as gven n Stuaton-I, further we let w r = π 1 r π r = Pr A r h2 A h1 be the nverse of the condtonal probablty n the second phase re-contacted unts, then by re-contactng the non-respondng unts we develop DEE and REE. The proposed DEE estmator for ths stuaton s t 4DEE = 1 w w y r + w w r y r 27 N A h2 A h2 and replcaton varance estmator of 27 s ˆV J4DEE t k 4DEE = 1 N = c k t k 4DEE t 4DEE 2, 28 A h1 + A h2 A h1 w 1 A h2 w 1 w 1 w 1 y r A h2 y r A h2 and c k s a factor assocated wth replcate k determned by the replcaton method. ]
12 258 M. Javed, Z. Ahmad and M. Hanf The proposed REE estmator for ths stuaton s t 4REE = 1 N wh1 ȳ rh2 + ȳ rh2, 29 wh1 = w Ah1, ȳ rh2 = w Ah2 w 1 A h2 w w y r, ȳ r h2 = 1 A h2 w w r A h2 w w r y r. The replcaton varance estmator of 29 s ˆV J4REE = c k t k 4REE t 4REE 2, 30 and t k 4REE = 1 L k N w h1 ȳ k rh2 + ȳk r h2 1 ȳ k r h2 = A h2 w r 1 rh2 = A h2 w ȳ k A h2 w r y r, h1 = A h1, A h2 w y r. 5. Smulaton Study We conducted a smulaton study, to analyze the performance of the estmators proposed n Secton 2 to Secton 4. A fnte artfcal populaton of sze N = 1000 was generated wth four varables y, z, q, u, the populaton elements are ndependently generated from z exp1+2; q χ 2 1+2; u Unf 1, 2, 3 and y = β 0 + β 1 z + β 2 q + ε β 0, β 1, β 2 are 0, 1, 1 respectvely and ε N 0, 1 as dscussed by Km and Yu To obtan unequal probablty samples for ths smulaton study, we used SRSWOR, wth selecton probabltes proportonal to the measure of sze varable. The varable z was used as a sze measure for the unequal probablty samplng n the frst phase samplng and q was used as a sze measure for the unequal probablty samplng n the second phase samplng, the stratfcaton was defned usng varable u, t s assumed that the varable z, q, u, y and ε are mutually ndependent. A frst phase sample of sze n = 200 was drawn from the populaton of For frst stuaton of secton 2.1 t s assumed that 30% non-response at frst phase. Frst phase respondng sample of sze was stratfed usng u and stratfed random sample of sze n was taken at second phase. In stuaton-ii frst phase sampled n unts are stratfed usng u for second phase samplng for both assumed respondng and re-contactng elements of frst phase sample and stratfed random sample of sze n = n r + n r was taken. When non-response s present on second phase, then for stuaton-i dscussed n secton 2.2 a sample of sze n = 200 wth SRSWOR was drawn. Frst phase sampled n unts are stratfed nto L stratum. It s assumed that 30% non-responses exst n second phase sample, so gnorng non-respondng unts a second phase
13 Replcaton varance estmaton n the presence of non-response 259 stratfed sample of sze n rh was taken from hth stratum. For stuaton-ii,the estmator s developed by re-contactng second phase non-respondng unts and a stratfed random sample of sze n = L n rh + n rh s used for both assumed respondng and re-contactng elements of second phase sample. We generate S=4000 ndependent samples for smulaton from the fnte populaton generated above. the parameter of nterest s the populaton mean of the varable y. From generated samples, we compute two phase stratfed estmators, DEE and REE wth ther replcaton varances. Relatve bas RB and coeffcent of varaton CV were computed for each estmator and ther replcaton varance wth the followng method. 1. The percent relatve bas of the mean estmators wth respect to the populaton parameter P RB = E t T T 100, The percent relatve bas of the jackknfe varance estmators wth respect to the estmated true mean squared error s estmated by P RB = E V J t MSE true MSE true 100, 32 E V J t = 1 S S =1 V J t and MSE true = 1 S S =1 t T The percent coeffcent of varaton of the jackknfe varance wth respect to the estmated true MSE s estmated by 1 S S =1 P CV = V J t MSE true MSE true Results of proposed estmators wth percent relatve bas and percent coeffcent of varaton are gven n Table 1. Table 2 shows the percent relatve bas and percent coeffcent of varaton of the replcaton varance estmators. 6. Concludng Remarks Table 1 shows that estmators are very close values to populaton parameter wth small relatve bas. Table 2 shows the RB and CV of the replcaton varance of the proposed estmators. The result shows that the varances are wth smaller bas. The man purpose of ths study was to show that the replcaton varance estmator works well n two phase stratfed desgn when non-response s present. Expanson estmators are used n the estmaton strategy and smulaton study supported these results. ACKNOWLEDGEMENTS The authors are hghly thankful to Dr Govanna Galatà Executve Edtor Support and to the referee for ther valuable suggestons regardng mprovement of the paper.
14 260 M. Javed, Z. Ahmad and M. Hanf REFERENCES B. B. Khare, S. Srvastava Transformed rato type estmators for populaton mean n presence of non-response, Commu. Statst. Theory Meth., 26, pp H. L. Jones The jackknfe method, Proceedngs of the IBM scentfc computaton and symposum on statstcs, pp H. P. Sngh, L. N. Upadhyaya, R. Iachan On applyng the jackknfe technque to the rato and product estmators n two-phase samplng, Vkram Math. J., X, pp J. Bredt, W.A. Fuller 1993.Regresson weghtng for multplcatve samples, Sankhya, 55, pp J. Durbn A note on the applcaton of Quenoulle s method of bas reducton to the estmaton of ratos, Bometrka, 46, pp J. K. Km, A. Navarro, W. A. Fuller Replcaton varance estmaton for two phase stratfed samplng, Journal of the Amercan statstcal assocaton, 101, pp J. K. Km, R. R. Stter Effcent replcaton varance estmaton for two phase samplng, Statstca Snca, 13, pp J. K. Km, C. L. Yu Replcaton varance estmaton under two-phase samplng, Survey methodology, 37, pp J. Neyman Contrbuton to the theory of samplng human populatons, Journal of the Amercan Statstcal Assocaton, 33, pp J. N. K. Rao On double samplng for stratfcaton and analytcal surveys, Bometrka, 60, pp J. N. K. Rao, J. Shao Jackknfe varance estmaton wth survey data under hot deck mputaton, Bometrka, 79, pp J. N. K. Rao, R. R. Stter Varance estmaton under two-phase samplng wth applcaton to mputaton for mssng data, Bometrka, 82, pp J. Tukey Bas and Confdence n not qute large samples, Ann. Math. Statst., 29, pp K. F. Rust, J. N. K. Rao Varance estmaton under two phase samplng wth applcaton to mputaton for mssng data, Bometrka, 82, pp K. Wolter Introducton to Varance Estmaton. 2 nd Edton, New York: Sprnger. L. Chand Some rato type estmators based on two or more auxlary varables, PhD Thess, Iowa State Unversty, Ames, Iowa, USA.
15 Replcaton varance estmaton n the presence of non-response 261 M. H. Hansen, W. N. Hurwts The problem of non-response n sample surveys, Journal of the Amercan Statstcal Assocaton, 41, pp M. H. Quenoulle Notes on bas n estmaton, Bometrka, 43, pp P. J. Farrell, S. Sngh Some Contrbutons to Jackknfng Two-phase Samplng Estmators, Survey Methodology, 36, pp P. S. Kott Varance estmaton when a frst-phase area sample s restratfed, Survey Methodology, 16, pp P. S. Kott, D. M. Stukel Can the jackknfe be used wth a two phase sample, Survey Methodology, 23, pp P. S. R. S. Rao Rato estmaton wth subsamplng the non-respondents, Survey Meth., 12, pp R. R. Stter Varance estmaton for the regresson estmator n twophase samplng, Journal of the Amercan Statstcal Assocaton, 92, pp V. Ramasubramanan, A. Ra, R. Sng Jackknfe varance estmaton under two phase samplng, Model Asssted Statstcs and Applcaton, 2, pp W. G. Cochran Samplng Technques, New York: John Wley & Sons, lnc. W. A. Fuller Replcaton varance estmaton for two phase samples, Sta- tstca snca, 8, pp SUMMARY Replcaton Varance Estmaton under Two-phase Samplng n the Presence of Non-response Km and Yu 2011 dscussed replcaton varance estmator for two-phase stratfed samplng. In ths paper estmators for mean have been proposed n two-phase stratfed samplng for dfferent stuaton of exstence of non-response at frst phase and second phase. The expressons of varances of these estmators have been derved. Furthermore, replcaton-based jackknfe varance estmators of these varances have also been derved. Smulaton study has been conducted to nvestgate the performance of the suggested estmators. Keywords: Two-phase stratfed samplng; Jackknfe varance estmator; Non-response
16 262 M. Javed, Z. Ahmad and M. Hanf Appendx Proof of 2: As we know n the case of two phase samplng, n general the varance of an estmator can be expressed as Consderng E 1 V 2 t 1 ] from above Eq. 34 or V t 1 = V 1 E 2 t 1 ] + E 1 V 2 t 1 ] E 1 V 2 t 1 ] = E 1 V 2 E 1 V 2 t 1 ] = E 1 = E 1 V 2 L A rh2 nrh ] h ȳ rh 2 1 n rh ] h n y rh rh 1 ] s 2 rh1, 35 h s 2 rh1 = h 1 1 y ȳ rh1 2 and ȳ rh1 = n 1 rh y r. A rh1 A rh1 Now consderng V 1 E 2 t 1 ] fromeq V 1 E 2 t 1 ] = V 1 E 2 = V 1 ȳ ] h ȳ rh or = N N S2 As f 1 = N, S2 = N 1 1 N V 1 E 2 t 1 ] = n 1 r 1 f 1 S 2 36 =1 y ȳ N 2. Usng Eq. 35 and Eq. 36 n Eq. 34, we get Then V t 1 = n 1 r 1 f 1 S 2 + E n 1 r S 2 = E V t 1 = 1 f 1 E n 1 r n 1 r L nrh 2 1 n rh 1 ] s 2 rh1. h w h ȳ rh1 ȳ srh1 ] 2. w h ȳ ] rh1 ȳ s 2 h1
17 Replcaton varance estmaton n the presence of non-response 263 or = E n 1 r f 1 V t 1 = E +E L n 1 r 1 f 1 nrh w h s 2 rh1+ n 1 r 1 f n rh 1 ] s 2 rh1 h w h ȳ rh1 ȳ n 1 r rh w 2 hs 2 rh1 w h s 2 rh1 w h ȳ rh1 ȳ 1 2 n 1 r f 1 rh w 2 hs 2 rh1 ]. n 1 rh w2 hs 2 rh1 ] w h s 2 rh1 Solvng above equaton we can obtaequred result gven n Eq.2. Proof of 5: Estmator gven n 4 can be wrtten as t 2 = w 1 t 1 + w 2 t 2, 37 t 1 = 1 L h A rh2 n y rh, t 2 = 1 L n rh 1h n r A rh2 n y rh, w 1 = n 1 2h and w 2 = n 2. n r As t 1 and t 2 are ndependent, the varance expresson of Eq. 37 can be wrtten as V t 2 = w 2 1V t 1 + w 2 2V t Consderng V t 1 from Eq. 38, we can wrte V t 1 = V 1 E 2 t 1] + E 1 V 2 t 1]. 39 or Now consderng E 1 V 2 t 1] from Eq. 39, we can wrte ] E 1 V 2 t 1 1] = E 1 V 2 h ȳ rh L 2 E 1 V 2 t nrh 1 1] = E n 1 ] s 2 rh1, 40 1h h s 2 rh1 = h 1 1 A rh1 y r ȳ rh1 2 andȳ rh1 = n 1 rh A rh1 y r. Now consderng V 1 E 2 t 1] from Eq. 39, we can wrte ] V 1 E 2 t 1 1] = V 1 E 2 h ȳ rh
18 264 M. Javed, Z. Ahmad and M. Hanf or = V 1 ȳ V 1 E 2 t 1] = n 1 r 1 f 1 S 2 41 f 1 = nr N S2 = N 1 1 N =1 y ȳ N 2. Usng Eq. 40 and Eq. 41 n Eq. 39, we get ˆV t 1 = n 1 r 1 f 1 w h ȳ rh2 ȳ r2 2 + From Eq. 38, now we consder 1h n 1 rh f 1 whs 2 2 rh2. 42 or or V t 2 = V 1 E 2 t 2] + E 1 V 2 t 2] 43 Now consderng E 1 V 2 t 2] from Eq. 43, we can wrte E 1 V 2 t 1 2] = E 1 V 2 E 1 V 2 t 2] = E L n rh n r ] n rh ȳ rh n r 2 1 n 2h 1 ] s 2 rh1 n rh Now consderng V 1 E 2 t 2] from Eq. 43, we can wrte V 1 E 2 t 1 2] = V 1 E 2 = V 1 ȳ] ] n rh ȳ rh n r 44 V 1 E 2 t 2] = n 1 r 1 f 2 S 2 45 Usng Eq. 44 and Eq. 45 n Eq. 43, we get ˆV t 2 = n 1 r 1 f 2 wh ȳ rh2 ȳ r h n 1 rh f 2 wh 2 s 2 rh2 46 Usng Eq. 42 and Eq. 46 n Eq. 37, we get ˆV t 2 = w1 2 n 1 r 1 f 1 w h ȳ rh2 ȳ r h n 1 rh f 1 whs 2 2 rh2 + w 2 2 n 1 r 1 f 2 wh ȳ rh2 ȳ r h n 1 rh f 2 wh 2 s 2 rh2 Solvng Eq. 47 we can obtaequred result gven n Eq.5. 47
19 Replcaton varance estmaton n the presence of non-response 265 TABLE 1 RB and CV of Proposed Estmators Estmator Parameter Estmated Mean RB CV t t t t t 1DEE t 2DEE t 3DEE t 4DEE t 1REE t 2REE t 3REE t 4REE TABLE 2 RB and CV of Replcaton Varance Estmators Estmator RB CV V J t V J t V J t V J t V J t 1DEE V J t 2DEE V J t 3DEE V J t 4DEE V J t 1REE V J t 2REE V J t 3REE V J t 4REE
USE OF DOUBLE SAMPLING SCHEME IN ESTIMATING THE MEAN OF STRATIFIED POPULATION UNDER NON-RESPONSE
STATISTICA, anno LXXV, n. 4, 015 USE OF DOUBLE SAMPLING SCHEME IN ESTIMATING THE MEAN OF STRATIFIED POPULATION UNDER NON-RESPONSE Manoj K. Chaudhary 1 Department of Statstcs, Banaras Hndu Unversty, Varanas,
More informationEfficient nonresponse weighting adjustment using estimated response probability
Effcent nonresponse weghtng adjustment usng estmated response probablty Jae Kwang Km Department of Appled Statstcs, Yonse Unversty, Seoul, 120-749, KOREA Key Words: Regresson estmator, Propensty score,
More informationEstimation: Part 2. Chapter GREG estimation
Chapter 9 Estmaton: Part 2 9. GREG estmaton In Chapter 8, we have seen that the regresson estmator s an effcent estmator when there s a lnear relatonshp between y and x. In ths chapter, we generalzed the
More informationMultivariate Ratio Estimator of the Population Total under Stratified Random Sampling
Open Journal of Statstcs, 0,, 300-304 ttp://dx.do.org/0.436/ojs.0.3036 Publsed Onlne July 0 (ttp://www.scrp.org/journal/ojs) Multvarate Rato Estmator of te Populaton Total under Stratfed Random Samplng
More informationImprovement in Estimating the Population Mean Using Exponential Estimator in Simple Random Sampling
Bulletn of Statstcs & Economcs Autumn 009; Volume 3; Number A09; Bull. Stat. Econ. ISSN 0973-70; Copyrght 009 by BSE CESER Improvement n Estmatng the Populaton Mean Usng Eponental Estmator n Smple Random
More informationA note on regression estimation with unknown population size
Statstcs Publcatons Statstcs 6-016 A note on regresson estmaton wth unknown populaton sze Mchael A. Hdroglou Statstcs Canada Jae Kwang Km Iowa State Unversty jkm@astate.edu Chrstan Olver Nambeu Statstcs
More informationParametric fractional imputation for missing data analysis
Secton on Survey Research Methods JSM 2008 Parametrc fractonal mputaton for mssng data analyss Jae Kwang Km Wayne Fuller Abstract Under a parametrc model for mssng data, the EM algorthm s a popular tool
More informationA general class of estimators for the population mean using multi-phase sampling with the non-respondents
Hacettepe Journal of Mathematcs Statstcs Volume 43 3 014 511 57 A general class of estmators for the populaton mean usng mult-phase samplng wth the non-respondents Saba Raz Gancarlo Dana Javd Shabbr Abstract
More informationA Bound for the Relative Bias of the Design Effect
A Bound for the Relatve Bas of the Desgn Effect Alberto Padlla Banco de Méxco Abstract Desgn effects are typcally used to compute sample szes or standard errors from complex surveys. In ths paper, we show
More informationExponential Type Product Estimator for Finite Population Mean with Information on Auxiliary Attribute
Avalable at http://pvamu.edu/aam Appl. Appl. Math. ISSN: 193-9466 Vol. 10, Issue 1 (June 015), pp. 106-113 Applcatons and Appled Mathematcs: An Internatonal Journal (AAM) Exponental Tpe Product Estmator
More informationParametric fractional imputation for missing data analysis. Jae Kwang Kim Survey Working Group Seminar March 29, 2010
Parametrc fractonal mputaton for mssng data analyss Jae Kwang Km Survey Workng Group Semnar March 29, 2010 1 Outlne Introducton Proposed method Fractonal mputaton Approxmaton Varance estmaton Multple mputaton
More informationProduct and Exponential Product Estimators in Adaptive Cluster Sampling under Different Population Situations
Proceedngs of the Pakstan Academy of Scences: A. Physcal and Computatonal Scences 53 (4): 447 457 (06) Copyrght Pakstan Academy of Scences ISSN: 58-445 (prnt), 58-453 (onlne) Pakstan Academy of Scences
More informationA FAMILY OF ESTIMATORS FOR ESTIMATING POPULATION MEAN IN STRATIFIED SAMPLING UNDER NON-RESPONSE
Florentn marache A FAMILY OF ETIMATOR FOR ETIMATIG POPULATIO MEA I TRATIFIED AMPLIG UDER O-REPOE MAOJ K. CHAUDHARY, RAJEH IGH, RAKEH K. HUKLA, MUKEH KUMAR, FLORETI MARADACHE Abstract Khoshnevsan et al.
More informationA General Class of Selection Procedures and Modified Murthy Estimator
ISS 684-8403 Journal of Statstcs Volume 4, 007,. 3-9 A General Class of Selecton Procedures and Modfed Murthy Estmator Abdul Bast and Muhammad Qasar Shahbaz Abstract A new selecton rocedure for unequal
More informationComputation of Higher Order Moments from Two Multinomial Overdispersion Likelihood Models
Computaton of Hgher Order Moments from Two Multnomal Overdsperson Lkelhood Models BY J. T. NEWCOMER, N. K. NEERCHAL Department of Mathematcs and Statstcs, Unversty of Maryland, Baltmore County, Baltmore,
More informationOn Outlier Robust Small Area Mean Estimate Based on Prediction of Empirical Distribution Function
On Outler Robust Small Area Mean Estmate Based on Predcton of Emprcal Dstrbuton Functon Payam Mokhtaran Natonal Insttute of Appled Statstcs Research Australa Unversty of Wollongong Small Area Estmaton
More informationOn The Estimation of Population Mean in Current Occasion in Two- Occasion Rotation Patterns
J. Stat. Appl. Pro. 4 No. 305-33 (05) 305 Journal of Statstcs Applcatons & Probablt An Internatonal Journal http://d.do.org/0.785/jsap/0405 On The stmaton of Populaton Mean n Current Occason n Two- Occason
More informationSampling Theory MODULE VII LECTURE - 23 VARYING PROBABILITY SAMPLING
Samplng heory MODULE VII LECURE - 3 VARYIG PROBABILIY SAMPLIG DR. SHALABH DEPARME OF MAHEMAICS AD SAISICS IDIA ISIUE OF ECHOLOGY KAPUR he smple random samplng scheme provdes a random sample where every
More informationEcon107 Applied Econometrics Topic 3: Classical Model (Studenmund, Chapter 4)
I. Classcal Assumptons Econ7 Appled Econometrcs Topc 3: Classcal Model (Studenmund, Chapter 4) We have defned OLS and studed some algebrac propertes of OLS. In ths topc we wll study statstcal propertes
More informationNon-Mixture Cure Model for Interval Censored Data: Simulation Study ABSTRACT
Malaysan Journal of Mathematcal Scences 8(S): 37-44 (2014) Specal Issue: Internatonal Conference on Mathematcal Scences and Statstcs 2013 (ICMSS2013) MALAYSIAN JOURNAL OF MATHEMATICAL SCIENCES Journal
More informationDurban Watson for Testing the Lack-of-Fit of Polynomial Regression Models without Replications
Durban Watson for Testng the Lack-of-Ft of Polynomal Regresson Models wthout Replcatons Ruba A. Alyaf, Maha A. Omar, Abdullah A. Al-Shha ralyaf@ksu.edu.sa, maomar@ksu.edu.sa, aalshha@ksu.edu.sa Department
More informationSampling Theory MODULE V LECTURE - 17 RATIO AND PRODUCT METHODS OF ESTIMATION
Samplng Theory MODULE V LECTURE - 7 RATIO AND PRODUCT METHODS OF ESTIMATION DR. SHALABH DEPARTMENT OF MATHEMATICS AND STATISTICS INDIAN INSTITUTE OF TECHNOLOG KANPUR Propertes of separate rato estmator:
More informationA Comparative Study for Estimation Parameters in Panel Data Model
A Comparatve Study for Estmaton Parameters n Panel Data Model Ahmed H. Youssef and Mohamed R. Abonazel hs paper examnes the panel data models when the regresson coeffcents are fxed random and mxed and
More informationLinear Approximation with Regularization and Moving Least Squares
Lnear Approxmaton wth Regularzaton and Movng Least Squares Igor Grešovn May 007 Revson 4.6 (Revson : March 004). 5 4 3 0.5 3 3.5 4 Contents: Lnear Fttng...4. Weghted Least Squares n Functon Approxmaton...
More informationSimulated Power of the Discrete Cramér-von Mises Goodness-of-Fit Tests
Smulated of the Cramér-von Mses Goodness-of-Ft Tests Steele, M., Chaselng, J. and 3 Hurst, C. School of Mathematcal and Physcal Scences, James Cook Unversty, Australan School of Envronmental Studes, Grffth
More informationTesting for seasonal unit roots in heterogeneous panels
Testng for seasonal unt roots n heterogeneous panels Jesus Otero * Facultad de Economía Unversdad del Rosaro, Colomba Jeremy Smth Department of Economcs Unversty of arwck Monca Gulett Aston Busness School
More informationANOMALIES OF THE MAGNITUDE OF THE BIAS OF THE MAXIMUM LIKELIHOOD ESTIMATOR OF THE REGRESSION SLOPE
P a g e ANOMALIES OF THE MAGNITUDE OF THE BIAS OF THE MAXIMUM LIKELIHOOD ESTIMATOR OF THE REGRESSION SLOPE Darmud O Drscoll ¹, Donald E. Ramrez ² ¹ Head of Department of Mathematcs and Computer Studes
More informationLecture 4 Hypothesis Testing
Lecture 4 Hypothess Testng We may wsh to test pror hypotheses about the coeffcents we estmate. We can use the estmates to test whether the data rejects our hypothess. An example mght be that we wsh to
More informationLINEAR REGRESSION ANALYSIS. MODULE IX Lecture Multicollinearity
LINEAR REGRESSION ANALYSIS MODULE IX Lecture - 30 Multcollnearty Dr. Shalabh Department of Mathematcs and Statstcs Indan Insttute of Technology Kanpur 2 Remedes for multcollnearty Varous technques have
More informationAn (almost) unbiased estimator for the S-Gini index
An (almost unbased estmator for the S-Gn ndex Thomas Demuynck February 25, 2009 Abstract Ths note provdes an unbased estmator for the absolute S-Gn and an almost unbased estmator for the relatve S-Gn for
More informationDr. Shalabh Department of Mathematics and Statistics Indian Institute of Technology Kanpur
Analyss of Varance and Desgn of Experment-I MODULE VIII LECTURE - 34 ANALYSIS OF VARIANCE IN RANDOM-EFFECTS MODEL AND MIXED-EFFECTS EFFECTS MODEL Dr Shalabh Department of Mathematcs and Statstcs Indan
More informationx = , so that calculated
Stat 4, secton Sngle Factor ANOVA notes by Tm Plachowsk n chapter 8 we conducted hypothess tests n whch we compared a sngle sample s mean or proporton to some hypotheszed value Chapter 9 expanded ths to
More informationOn New Selection Procedures for Unequal Probability Sampling
Int. J. Oen Problems Comt. Math., Vol. 4, o. 1, March 011 ISS 1998-66; Coyrght ICSRS Publcaton, 011 www.-csrs.org On ew Selecton Procedures for Unequal Probablty Samlng Muhammad Qaser Shahbaz, Saman Shahbaz
More informationSample Correlation Coef cients Based on Survey Data Under Regression Imputation
Sample Correlaton Coef cents Based on Survey ata Under Regresson Imputaton Jun Shao Hansheng Wang Regresson mputaton s commonly used to compensate for tem nonresponse when auxlary data are avalable. It
More informationOn the Influential Points in the Functional Circular Relationship Models
On the Influental Ponts n the Functonal Crcular Relatonshp Models Department of Mathematcs, Faculty of Scence Al-Azhar Unversty-Gaza, Gaza, Palestne alzad33@yahoo.com Abstract If the nterest s to calbrate
More informationChapter 3 Describing Data Using Numerical Measures
Chapter 3 Student Lecture Notes 3-1 Chapter 3 Descrbng Data Usng Numercal Measures Fall 2006 Fundamentals of Busness Statstcs 1 Chapter Goals To establsh the usefulness of summary measures of data. The
More informationNUMERICAL DIFFERENTIATION
NUMERICAL DIFFERENTIATION 1 Introducton Dfferentaton s a method to compute the rate at whch a dependent output y changes wth respect to the change n the ndependent nput x. Ths rate of change s called the
More informationPopulation element: 1 2 N. 1.1 Sampling with Replacement: Hansen-Hurwitz Estimator(HH)
Chapter 1 Samplng wth Unequal Probabltes Notaton: Populaton element: 1 2 N varable of nterest Y : y1 y2 y N Let s be a sample of elements drawn by a gven samplng method. In other words, s s a subset of
More informationEcon Statistical Properties of the OLS estimator. Sanjaya DeSilva
Econ 39 - Statstcal Propertes of the OLS estmator Sanjaya DeSlva September, 008 1 Overvew Recall that the true regresson model s Y = β 0 + β 1 X + u (1) Applyng the OLS method to a sample of data, we estmate
More informationISSN: ISO 9001:2008 Certified International Journal of Engineering and Innovative Technology (IJEIT) Volume 3, Issue 1, July 2013
ISSN: 2277-375 Constructon of Trend Free Run Orders for Orthogonal rrays Usng Codes bstract: Sometmes when the expermental runs are carred out n a tme order sequence, the response can depend on the run
More informationRobust Small Area Estimation Using a Mixture Model
Robust Small Area Estmaton Usng a Mxture Model Jule Gershunskaya U.S. Bureau of Labor Statstcs Partha Lahr JPSM, Unversty of Maryland, College Park, USA ISI Meetng, Dubln, August 23, 2011 Parameter of
More informationDr. Shalabh Department of Mathematics and Statistics Indian Institute of Technology Kanpur
Analyss of Varance and Desgn of Exerments-I MODULE III LECTURE - 2 EXPERIMENTAL DESIGN MODELS Dr. Shalabh Deartment of Mathematcs and Statstcs Indan Insttute of Technology Kanur 2 We consder the models
More informationSmall Area Estimation for Business Surveys
ASA Secton on Survey Research Methods Small Area Estmaton for Busness Surveys Hukum Chandra Southampton Statstcal Scences Research Insttute, Unversty of Southampton Hghfeld, Southampton-SO17 1BJ, U.K.
More informationEfficient estimation in missing data and survey sampling problems
Graduate Theses and Dssertatons Iowa State Unversty Capstones, Theses and Dssertatons 2012 Effcent estmaton n mssng data and survey samplng problems Sxa Chen Iowa State Unversty Follow ths and addtonal
More informationANSWERS. Problem 1. and the moment generating function (mgf) by. defined for any real t. Use this to show that E( U) var( U)
Econ 413 Exam 13 H ANSWERS Settet er nndelt 9 deloppgaver, A,B,C, som alle anbefales å telle lkt for å gøre det ltt lettere å stå. Svar er gtt . Unfortunately, there s a prntng error n the hnt of
More informationConditional and unconditional models in modelassisted estimation of finite population totals
Unversty of Wollongong Research Onlne Faculty of Informatcs - Papers Archve) Faculty of Engneerng and Informaton Scences 2011 Condtonal and uncondtonal models n modelasssted estmaton of fnte populaton
More informationNonparametric Regression Estimation. of Finite Population Totals. under Two-Stage Sampling
Nonparametrc Regresson Estmaton of Fnte Populaton Totals under Two-Stage Samplng J-Yeon Km Iowa State Unversty F. Jay Bredt Colorado State Unversty Jean D. Opsomer Iowa State Unversty ay 21, 2003 Abstract
More informationDiscussion of Extensions of the Gauss-Markov Theorem to the Case of Stochastic Regression Coefficients Ed Stanek
Dscusson of Extensons of the Gauss-arkov Theorem to the Case of Stochastc Regresson Coeffcents Ed Stanek Introducton Pfeffermann (984 dscusses extensons to the Gauss-arkov Theorem n settngs where regresson
More informationImproved Class of Ratio Estimators for Finite Population Variance
Global Journal of Scence Fronter Research: F Mathematcs and Decson Scences Volume 6 Issue Verson.0 Year 06 Tpe : Double lnd Peer Revewed Internatonal Research Journal Publsher: Global Journals Inc. (USA)
More informationThe Multiple Classical Linear Regression Model (CLRM): Specification and Assumptions. 1. Introduction
ECONOMICS 5* -- NOTE (Summary) ECON 5* -- NOTE The Multple Classcal Lnear Regresson Model (CLRM): Specfcaton and Assumptons. Introducton CLRM stands for the Classcal Lnear Regresson Model. The CLRM s also
More informationChapter 9: Statistical Inference and the Relationship between Two Variables
Chapter 9: Statstcal Inference and the Relatonshp between Two Varables Key Words The Regresson Model The Sample Regresson Equaton The Pearson Correlaton Coeffcent Learnng Outcomes After studyng ths chapter,
More informationComputing MLE Bias Empirically
Computng MLE Bas Emprcally Kar Wa Lm Australan atonal Unversty January 3, 27 Abstract Ths note studes the bas arses from the MLE estmate of the rate parameter and the mean parameter of an exponental dstrbuton.
More informationChapter 13: Multiple Regression
Chapter 13: Multple Regresson 13.1 Developng the multple-regresson Model The general model can be descrbed as: It smplfes for two ndependent varables: The sample ft parameter b 0, b 1, and b are used to
More informationMaximizing Overlap of Large Primary Sampling Units in Repeated Sampling: A comparison of Ernst s Method with Ohlsson s Method
Maxmzng Overlap of Large Prmary Samplng Unts n Repeated Samplng: A comparson of Ernst s Method wth Ohlsson s Method Red Rottach and Padrac Murphy 1 U.S. Census Bureau 4600 Slver Hll Road, Washngton DC
More informationAssignment 5. Simulation for Logistics. Monti, N.E. Yunita, T.
Assgnment 5 Smulaton for Logstcs Mont, N.E. Yunta, T. November 26, 2007 1. Smulaton Desgn The frst objectve of ths assgnment s to derve a 90% two-sded Confdence Interval (CI) for the average watng tme
More informationBasically, if you have a dummy dependent variable you will be estimating a probability.
ECON 497: Lecture Notes 13 Page 1 of 1 Metropoltan State Unversty ECON 497: Research and Forecastng Lecture Notes 13 Dummy Dependent Varable Technques Studenmund Chapter 13 Bascally, f you have a dummy
More informationLINEAR REGRESSION ANALYSIS. MODULE IX Lecture Multicollinearity
LINEAR REGRESSION ANALYSIS MODULE IX Lecture - 31 Multcollnearty Dr. Shalabh Department of Mathematcs and Statstcs Indan Insttute of Technology Kanpur 6. Rdge regresson The OLSE s the best lnear unbased
More informationDr. Shalabh Department of Mathematics and Statistics Indian Institute of Technology Kanpur
Analyss of Varance and Desgn of Experment-I MODULE VII LECTURE - 3 ANALYSIS OF COVARIANCE Dr Shalabh Department of Mathematcs and Statstcs Indan Insttute of Technology Kanpur Any scentfc experment s performed
More informationJoint Statistical Meetings - Biopharmaceutical Section
Iteratve Ch-Square Test for Equvalence of Multple Treatment Groups Te-Hua Ng*, U.S. Food and Drug Admnstraton 1401 Rockvlle Pke, #200S, HFM-217, Rockvlle, MD 20852-1448 Key Words: Equvalence Testng; Actve
More informationThe written Master s Examination
he wrtten Master s Eamnaton Opton Statstcs and Probablty SPRING 9 Full ponts may be obtaned for correct answers to 8 questons. Each numbered queston (whch may have several parts) s worth the same number
More informationInterval Estimation in the Classical Normal Linear Regression Model. 1. Introduction
ECONOMICS 35* -- NOTE 7 ECON 35* -- NOTE 7 Interval Estmaton n the Classcal Normal Lnear Regresson Model Ths note outlnes the basc elements of nterval estmaton n the Classcal Normal Lnear Regresson Model
More informationECONOMICS 351*-A Mid-Term Exam -- Fall Term 2000 Page 1 of 13 pages. QUEEN'S UNIVERSITY AT KINGSTON Department of Economics
ECOOMICS 35*-A Md-Term Exam -- Fall Term 000 Page of 3 pages QUEE'S UIVERSITY AT KIGSTO Department of Economcs ECOOMICS 35* - Secton A Introductory Econometrcs Fall Term 000 MID-TERM EAM ASWERS MG Abbott
More informationModule 3 LOSSY IMAGE COMPRESSION SYSTEMS. Version 2 ECE IIT, Kharagpur
Module 3 LOSSY IMAGE COMPRESSION SYSTEMS Verson ECE IIT, Kharagpur Lesson 6 Theory of Quantzaton Verson ECE IIT, Kharagpur Instructonal Objectves At the end of ths lesson, the students should be able to:
More informationInductance Calculation for Conductors of Arbitrary Shape
CRYO/02/028 Aprl 5, 2002 Inductance Calculaton for Conductors of Arbtrary Shape L. Bottura Dstrbuton: Internal Summary In ths note we descrbe a method for the numercal calculaton of nductances among conductors
More informationNonparametric model calibration estimation in survey sampling
Ames February 18, 004 Nonparametrc model calbraton estmaton n survey samplng M. Govanna Ranall Department of Statstcs, Colorado State Unversty (Jont work wth G.E. Montanar, Dpartmento d Scenze Statstche,
More informationNotes on Frequency Estimation in Data Streams
Notes on Frequency Estmaton n Data Streams In (one of) the data streamng model(s), the data s a sequence of arrvals a 1, a 2,..., a m of the form a j = (, v) where s the dentty of the tem and belongs to
More informationUsing the estimated penetrances to determine the range of the underlying genetic model in casecontrol
Georgetown Unversty From the SelectedWorks of Mark J Meyer 8 Usng the estmated penetrances to determne the range of the underlyng genetc model n casecontrol desgn Mark J Meyer Neal Jeffres Gang Zheng Avalable
More informationESTIMATES OF TECHNICAL INEFFICIENCY IN STOCHASTIC FRONTIER MODELS WITH PANEL DATA: GENERALIZED PANEL JACKKNIFE ESTIMATION
ESIMAES OF ECHNICAL INEFFICIENCY IN SOCHASIC FRONIER MODELS WIH PANEL DAA: GENERALIZED PANEL JACKKNIFE ESIMAION Panutat Satchacha Mchgan State Unversty Peter Schmdt Mchgan State Unversty Yonse Unversty
More information/ n ) are compared. The logic is: if the two
STAT C141, Sprng 2005 Lecture 13 Two sample tests One sample tests: examples of goodness of ft tests, where we are testng whether our data supports predctons. Two sample tests: called as tests of ndependence
More informationGeneralized Multiplicity-Adjusted Horvitz-Thompson Estimation as a Unified Approach to Multiple Frame Surveys
Journal of Offcal Statstcs, Vol. 7, No. 4, 011, pp. 633 650 Generalzed Multplcty-Adjusted Horvtz-Thompson Estmaton as a Unfed Approach to Multple Frame Surveys Avnash C. Sngh 1 and Fulva Mecatt The avalable
More informationMaximum Likelihood Estimation of Binary Dependent Variables Models: Probit and Logit. 1. General Formulation of Binary Dependent Variables Models
ECO 452 -- OE 4: Probt and Logt Models ECO 452 -- OE 4 Maxmum Lkelhood Estmaton of Bnary Dependent Varables Models: Probt and Logt hs note demonstrates how to formulate bnary dependent varables models
More informationComparison of the Population Variance Estimators. of 2-Parameter Exponential Distribution Based on. Multiple Criteria Decision Making Method
Appled Mathematcal Scences, Vol. 7, 0, no. 47, 07-0 HIARI Ltd, www.m-hkar.com Comparson of the Populaton Varance Estmators of -Parameter Exponental Dstrbuton Based on Multple Crtera Decson Makng Method
More informationCoordinating the PRN: Combining Sequential and Bernoulli-Type Sampling Schemes in Business Surveys
Coordnatng the PRN: Combnng Sequental and Bernoull-Type Samplng Schemes n Busness Surveys Ront Nrel, Aryeh Reter, Tzah Makovky and Moshe Kelner Central Bureau of Statstcs, Israel 66 Kanfey Nesharm St.,
More information4 Analysis of Variance (ANOVA) 5 ANOVA. 5.1 Introduction. 5.2 Fixed Effects ANOVA
4 Analyss of Varance (ANOVA) 5 ANOVA 51 Introducton ANOVA ANOVA s a way to estmate and test the means of multple populatons We wll start wth one-way ANOVA If the populatons ncluded n the study are selected
More informationMultivariate Ratio Estimation With Known Population Proportion Of Two Auxiliary Characters For Finite Population
Multvarate Rato Estmaton Wth Knon Populaton Proporton Of To Auxlar haracters For Fnte Populaton *Raesh Sngh, *Sachn Mal, **A. A. Adeara, ***Florentn Smarandache *Department of Statstcs, Banaras Hndu Unverst,Varanas-5,
More informationA Monte Carlo Study for Swamy s Estimate of Random Coefficient Panel Data Model
A Monte Carlo Study for Swamy s Estmate of Random Coeffcent Panel Data Model Aman Mousa, Ahmed H. Youssef and Mohamed R. Abonazel Department of Appled Statstcs and Econometrcs, Instute of Statstcal Studes
More informationNEW ASTERISKS IN VERSION 2.0 OF ACTIVEPI
NEW ASTERISKS IN VERSION 2.0 OF ACTIVEPI ASTERISK ADDED ON LESSON PAGE 3-1 after the second sentence under Clncal Trals Effcacy versus Effectveness versus Effcency The apprasal of a new or exstng healthcare
More information3.1 Expectation of Functions of Several Random Variables. )' be a k-dimensional discrete or continuous random vector, with joint PMF p (, E X E X1 E X
Statstcs 1: Probablty Theory II 37 3 EPECTATION OF SEVERAL RANDOM VARIABLES As n Probablty Theory I, the nterest n most stuatons les not on the actual dstrbuton of a random vector, but rather on a number
More informationChapter 2 - The Simple Linear Regression Model S =0. e i is a random error. S β2 β. This is a minimization problem. Solution is a calculus exercise.
Chapter - The Smple Lnear Regresson Model The lnear regresson equaton s: where y + = β + β e for =,..., y and are observable varables e s a random error How can an estmaton rule be constructed for the
More informationPARTIALLY BALANCED INCOMPLETE BLOCK DESIGNS
PARTIALLY BALANCED INCOMPLETE BLOCK DESIGNS V.K. Sharma I.A.S.R.I., Lbrary Avenue, New Delh-00. Introducton Balanced ncomplete block desgns, though have many optmal propertes, do not ft well to many expermental
More informatione i is a random error
Chapter - The Smple Lnear Regresson Model The lnear regresson equaton s: where + β + β e for,..., and are observable varables e s a random error How can an estmaton rule be constructed for the unknown
More informationA Robust Method for Calculating the Correlation Coefficient
A Robust Method for Calculatng the Correlaton Coeffcent E.B. Nven and C. V. Deutsch Relatonshps between prmary and secondary data are frequently quantfed usng the correlaton coeffcent; however, the tradtonal
More informationStatistical inference for generalized Pareto distribution based on progressive Type-II censored data with random removals
Internatonal Journal of Scentfc World, 2 1) 2014) 1-9 c Scence Publshng Corporaton www.scencepubco.com/ndex.php/ijsw do: 10.14419/jsw.v21.1780 Research Paper Statstcal nference for generalzed Pareto dstrbuton
More informationComposite Hypotheses testing
Composte ypotheses testng In many hypothess testng problems there are many possble dstrbutons that can occur under each of the hypotheses. The output of the source s a set of parameters (ponts n a parameter
More informationFactor models with many assets: strong factors, weak factors, and the two-pass procedure
Factor models wth many assets: strong factors, weak factors, and the two-pass procedure Stanslav Anatolyev 1 Anna Mkusheva 2 1 CERGE-EI and NES 2 MIT December 2017 Stanslav Anatolyev and Anna Mkusheva
More informationGlobal Sensitivity. Tuesday 20 th February, 2018
Global Senstvty Tuesday 2 th February, 28 ) Local Senstvty Most senstvty analyses [] are based on local estmates of senstvty, typcally by expandng the response n a Taylor seres about some specfc values
More information1. Inference on Regression Parameters a. Finding Mean, s.d and covariance amongst estimates. 2. Confidence Intervals and Working Hotelling Bands
Content. Inference on Regresson Parameters a. Fndng Mean, s.d and covarance amongst estmates.. Confdence Intervals and Workng Hotellng Bands 3. Cochran s Theorem 4. General Lnear Testng 5. Measures of
More informationA new Approach for Solving Linear Ordinary Differential Equations
, ISSN 974-57X (Onlne), ISSN 974-5718 (Prnt), Vol. ; Issue No. 1; Year 14, Copyrght 13-14 by CESER PUBLICATIONS A new Approach for Solvng Lnear Ordnary Dfferental Equatons Fawz Abdelwahd Department of
More informationLimited Dependent Variables
Lmted Dependent Varables. What f the left-hand sde varable s not a contnuous thng spread from mnus nfnty to plus nfnty? That s, gven a model = f (, β, ε, where a. s bounded below at zero, such as wages
More informationLOGIT ANALYSIS. A.K. VASISHT Indian Agricultural Statistics Research Institute, Library Avenue, New Delhi
LOGIT ANALYSIS A.K. VASISHT Indan Agrcultural Statstcs Research Insttute, Lbrary Avenue, New Delh-0 02 amtvassht@asr.res.n. Introducton In dummy regresson varable models, t s assumed mplctly that the dependent
More informationLecture 3 Stat102, Spring 2007
Lecture 3 Stat0, Sprng 007 Chapter 3. 3.: Introducton to regresson analyss Lnear regresson as a descrptve technque The least-squares equatons Chapter 3.3 Samplng dstrbuton of b 0, b. Contnued n net lecture
More informationSee Book Chapter 11 2 nd Edition (Chapter 10 1 st Edition)
Count Data Models See Book Chapter 11 2 nd Edton (Chapter 10 1 st Edton) Count data consst of non-negatve nteger values Examples: number of drver route changes per week, the number of trp departure changes
More informationStatistics for Economics & Business
Statstcs for Economcs & Busness Smple Lnear Regresson Learnng Objectves In ths chapter, you learn: How to use regresson analyss to predct the value of a dependent varable based on an ndependent varable
More informationChapter 12 Analysis of Covariance
Chapter Analyss of Covarance Any scentfc experment s performed to know somethng that s unknown about a group of treatments and to test certan hypothess about the correspondng treatment effect When varablty
More informationStatistics Chapter 4
Statstcs Chapter 4 "There are three knds of les: les, damned les, and statstcs." Benjamn Dsrael, 1895 (Brtsh statesman) Gaussan Dstrbuton, 4-1 If a measurement s repeated many tmes a statstcal treatment
More informationEconomics 130. Lecture 4 Simple Linear Regression Continued
Economcs 130 Lecture 4 Contnued Readngs for Week 4 Text, Chapter and 3. We contnue wth addressng our second ssue + add n how we evaluate these relatonshps: Where do we get data to do ths analyss? How do
More informationCredit Card Pricing and Impact of Adverse Selection
Credt Card Prcng and Impact of Adverse Selecton Bo Huang and Lyn C. Thomas Unversty of Southampton Contents Background Aucton model of credt card solctaton - Errors n probablty of beng Good - Errors n
More informationChapter 11: Simple Linear Regression and Correlation
Chapter 11: Smple Lnear Regresson and Correlaton 11-1 Emprcal Models 11-2 Smple Lnear Regresson 11-3 Propertes of the Least Squares Estmators 11-4 Hypothess Test n Smple Lnear Regresson 11-4.1 Use of t-tests
More informationSmall Area Estimation with Auxiliary Survey Data
Small Area Estmaton wth Auxlary Survey Data by Sharon L. Lohr 1 and N.G.N. Prasad 2 1 Department of Mathematcs, Arzona State Unversty, Tempe, AZ 85287-1804. Research partally supported by a grant from
More informationAdaptive Estimation of Heteroscedastic Linear Regression Models Using Heteroscedasticity Consistent Covariance Matrix
ISSN 1684-8403 Journal of Statstcs Volume 16, 009, pp. 8-44 Adaptve Estmaton of Heteroscedastc Lnear Regresson Models Usng Heteroscedastcty Consstent Covarance Matrx Abstract Muhammad Aslam 1 and Gulam
More information