Exponentiated Transmuted Modified Weibull Distribution
|
|
- Cameron Conley
- 6 years ago
- Views:
Transcription
1 EUROPEAN JOURNAL OF PURE AND APPLIED MATHEMATICS Vol. 8, No. 1, 2015, 1-14 ISSN Exponentated Transmuted Modfed Webull Dstrbuton Mansha Pal 1,, Montp Tensuwan 2 1 Department of Statstcs, Unversty of Calcutta, Inda 2 Department of Mathematcs, Faculty of Scence, Mahdol Unversty, Thaland Abstract. The paper ntroduces the exponentated transmuted modfed Webull dstrbuton, whch contans a number of dstrbutons as specal cases. The propertes of the dstrbuton are dscussed and explct expressons for the quantles, mean devatons and the relablty are derved. The dstrbuton and moments of order statstcs are also studed. Estmaton of the model parameters by the methods of least squares and maxmum lkelhood are dscussed. Fnally, the usefulness of the dstrbuton for modelng data s llustrated usng real data Mathematcs Subject Classfcatons: 90B25; 62N05 Key Words and Phrases: Relablty functon, moment generatng functon, quantles, mean devaton, order statstcs, least square estmaton, maxmum lkelhood estmaton. 1. Introducton Modellng and analyss of lfetme data have become very crucal n dfferent areas of research, lke engneerng, medcne, relablty, etc. In ths regard, t s observed that the Webull dstrbuton s extensvely used as t s found to provde reasonable ft n many practcal stuatons. Attempts at generalzaton of the dstrbuton have led to the exponentated Webull dstrbuton, the modfed Webull dstrbuton and the exponentated modfed Webull dstrbuton. An nterestng dea of generalzng a dstrbuton, whch s known n the lterature as transmutaton has been used to develop further dstrbutons. A random varable T s sad to have a transmuted dstrbuton f ts dstrbuton functon s gven by Z(t)=(1λ)G(t) λ[g(t)] 2, (1) where G(t) denotes the base dstrbuton, and λ [-1, 1] denotes the transmutng parameter. Aryall and Tsokos[2] ntroduced the transmuted Webull dstrbuton, Ebrahem[4] studed the exponentated transmuted Webull dstrbuton, Pal and Tensuwan[7] developed the beta transmuted Webull dstrbuton, Khan and Kng[6] nvestgated the transmuted modfed Correspondng author. Emal addresses: manshapal2@gmal.com (M. Pal),montp.te@mahdol.ac.th (M. Tensuwan) 1 c 2015 EJPAM All rghts reserved.
2 M. Pal and M. Tensuwan/Eur. J. Pure Appl. Math, 8 (2015), Webull dstrbuton, and Ashour and Eltehwy[3] proposed the transmuted exponentated modfed Webull dstrbuton. In ths paper, we ntroduce and study several mathematcal propertes of a new relablty model referred to as the exponentated transmuted modfed Webull dstrbuton. The modfed Webull dstrbuton, ntroduced by Sarhan and Zandn[8], has the cumulatve dstrbuton functon (c.d.f.) F MW (t)=1 ex p( αt γt β ), t 0,α,β,γ>0. (2) The c.d.f. of the transmuted modfed Webull dstrbuton[6] s gven by F T MW (t)=[1 ex p( αt γt β )][1λex p( αt γt β )], t 0,α,β,γ>0. (3) The above dstrbuton has three shape parametersα,β andγ, andλdenotes the transmutng parameter. The exponentated transmuted modfed Webull dstrbuton generalzes ths dstrbuton by ntroducng another shape parameter. The paper s organzed as follows. In Secton 2 we ntroduce the dstrbuton. In Sectons 3, we obtan the quantle functon of the dstrbuton. The moment generatng functon and the moments are derved n Sectons 4. Mean devaton s dscussed n Secton 5. Order statstcs and ther moments are studed n Sectons 6. In Secton 7, the stress-strength relablty s obtaned. Estmaton of parameters by the least square method and the maxmum lkelhood method are dscussed n Sectons 8 and 9. In Secton 10, a smulaton study s carred out to compare the two methods of estmaton. The usefulness of the dstrbuton for modelng real lfe data s llustrated n Secton 11. Fnally, n Secton 12, we make some concludng remarks on our study. 2. Exponentated Transmuted Modfed Webull Dstrbuton The fve parameter exponentated transmuted modfed Webull (ETMW) dstrbuton s gven by the c.d.f. F(t)=[1 ex p( αt γt β )1λex p( αt γt β )] δ, t 0,α,β,γ>0,λ [ 1,1], (4) whereα,β,γ,δare all shape parameters, andλs the transmutng parameter. The densty functon of the dstrbuton s obtaned as f(t)=δ[{1 ex p( αt γt β )}{1λex p( αt γt β )}] δ 1 (αβγt β 1 )ex p( αt γt β ) [1 λ2λex p( αt γt β )], t 0. The hazard rate and the hazard functon of the dstrbuton are as follows: r(t)=δ[{1 ex p( αt γt β )}1λex p( αt γt β )] δ 1 (αtβγt β 1 )ex p( αt γt β ) [1 λ2λex p( αt γt β )][1 {ex p( αt γt β )} ( δ){1λex p( αt γt β )} δ ] ( 1), t 0, H(t)= ln[1 λ2λex p( αt γt β )][1 { ex p( αt γt β )} δ {1λex p( αt γt β )} δ ], t 0. (5)
3 M. Pal and M. Tensuwan/Eur. J. Pure Appl. Math, 8 (2015), Plots of the p.d.f. and the hazard rate are gven n Fgure 1. Fgure 1a exhbts the dverse shapes of the exponentated transmuted modfed Webull densty for dfferent choces of the parameters. Fgure 1b shows that for almost all the parameter combnatons consdered the dstrbuton exhbts monotonc hazard rate. (a) Probablty densty functon. (b) Hazard rate functon. Fgure 1: Exponentated Transmuted Modfed Webull Dstrbuton whenα=1. By proper selecton of the model parameters we can get a number of dstrbutons as specal cases as shown below: Parameters Dstrbuton δ=1 Transmuted modfed Webull δ=1,α=0 Transmuted Webull δ = 1, β = 1 Transmuted exponental dstrbuton α=0 Exponentated transmuted Webull β= 1 Exponentated transmuted exponental λ=0 Exponentated modfed Webull λ = 0, α = 0 Exponentated Webull λ = 0, β = 1 Exponentated exponental δ=1,λ=0 Modfed Webull δ=1,λ=0,β= 2 Lnear falure rate dstrbuton δ=1,λ=0,α=0 Webull δ=1,λ=0,α=0,β= 2 Raylegh δ=1,λ=0,β= 1 Exponental 3. Quantle Functon and Smulaton For any random varable X wth cumulatve dstrbuton functon F( ), for a gven q, 0 q 1, the quantle functon returns the threshold value x such that F(x)=q. Ths functon s useful n statstcal applcatons and Monte Carlo smulaton. For statstcal applcatons, one needs to know the key percentage ponts of a gven dstrbuton, lke the medan and the 25% and 75% quartles. The quantle functon s also helpful n examnng the ft of a gven data set to a theoretcal dstrbuton. Ths s done by usng the quantle-quantle (Q-Q) plot.
4 M. Pal and M. Tensuwan/Eur. J. Pure Appl. Math, 8 (2015), The quantle functon correspondng to the ETMW dstrbuton (4) s gven by t q = F 1 (q)= G 1 (q 1/δ ), (6) where G(x)=[1 ex p( αt γt β )][1λex p( αt γt β )] s the cumulatve dstrbuton functon of the transmuted modfed Webull dstrbuton nvestgated by Khan and Kng[6]. Thus, t q s the(q 1/δ )-th quantle of a transmuted modfed Webull dstrbuton, and, from Khan and Kng[6], t q s the real soluton to the equaton where Forβ= 2, t q s gven by γt β q αt q ln(z )=0, (7) z = 1 (1λ) (1λ) 2 4λq 1/δ. (8) 2λ t q = α α 2 4γ ln(z ), (9) 2γ where z s gven by (8). Thus, forβ= 2, the medan of the dstrbuton has the form t 0.5 = α α 2 4γ ln[{ (1λ) /δ λ (1 λ)}/2λ]. 2γ In order to smulate from the ETMW dstrbuton, we have to solve for t q from (7) for a random proporton q. However, forβ= 2, smulaton s straght forward from (9). 4. Moment Generatng Functon We can express the moment generatng functon M(t ) of the ETMW dstrbuton n terms of the moment generatng functon of the modfed Webull dstrbuton as follows: M(t )= 0 ex p(t t)f(t)dt 1 λ =δ A(, j;δ,λ)[ ( j 1) M MW(t ;( j 1)α,( j 1)γ,β) 2λ ( j 2) M MW(t ;( j 2)α,( j 2)γ,β)], where M MW (t ;α,γ,β) denotes the moment generatng functon of a modfed Webull dstrbuton wth c.d.f. (2), and A(, j;δ,λ)=( 1) {Γ(δ 1)} 2 Γ()Γ(j)Γ(δ 1)Γ(δ j 1) λj.
5 M. Pal and M. Tensuwan/Eur. J. Pure Appl. Math, 8 (2015), From Sarhan and Zandn[8], we have M MW (t ( γ) k αγ(kβ 1) γβγ(k 1)β ;α,γ,β)= k! (α t ) kβ1, forα,γ>0,α> t (α t ) (k1)β = t k Γ( k β1 ) γ k β forα=0,γ>0 = α, forγ=0,α> t α t Thus, M(t 1 λ ( ( j 1)γ) k ( j 1)αΓ(kβ 1) )=δ A(, j;δ,λ)[ { ( j 1) k! (( j 1)α t ) kβ1 = ( j 1)γβΓ(k 1)β (( j 1)α t ) (k1)β 2λ ( j 2) ( ( j 2)γ) k k! ( j 2)αΓ(kβ 1) ( j 2)γβΓ(k 1)β { (( j 2)α t ) kβ1 (( j 2)α t ) (k1)β}], forα,γ>0,α> t, 1 λ t k Γ( k β1 =δ A(, j;δ,λ)[ ) ( j 1) {( j 1)γ} k β 2λ t k Γ( k β1 ), for alpha=0,γ>0, ( j 2) {( j 2)γ} k β 1 λ ( j 1)α =δ A(, j;δ,λ)[ ( j 1) {( j 1)α t } 2λ ( j 2)α ( j 2) {( j 2)α t } ], forγ=0,α> t (10) The moments can be ndependently derved as follows: µ r =E{X r } =δ A(, j;δ,λ)[ 1 λ j 1 µmw r (( j 1)α,( j 1)γ,β) 2λ j 2 µmw k (( j 2)α,( j 2)γ,β), whereµ MW r (α,γ,β) denotes the r-th moment of the modfed Webull dstrbuton (2). From Sarhan and Zandn[8] we have µ MW r (α,γ,β)= ( β) k k! Γ( r γ 1) β r γ Γ(kγr1) α kγr βγ Γ(rkγγ), forα,β> 0 α kγγr, forα=0,β> 0 Γ(r1) α r, forα>0,β= 0. (11)
6 M. Pal and M. Tensuwan/Eur. J. Pure Appl. Math, 8 (2015), Hence, we get µ r =δ A(, j;δ,λ)[ 1 λ j 1 ( β) k k! Γ(k( j 1)γ r 1) { {( j 1)α} k(j1)γr Γ(r{k( j 1)1}γ) 2λ ( β) k ( j 1)βγ {( j 1)α} {k(j1)1}γr} j 2 k! Γ(k( j 2)γ r 2) Γ(r{k( j 2)1}γ) {( j 2)α} k(j2)γr( j 2)βγ {( j 2)α} {k(j2)1}γr},forα,β> 0 =δ A(, j;δ,λ)[ 1 λ j 1 ( r ( j 1)γ 1)/β r (j1)γ 2λ j 2 ( r ( j 2)γ 1)/β r (j2)γ, forα=0,β> 0 =δ A(, j;δ,λ)[ 1 λ Γ(r 1) 2λ Γ(r 1) j 1{( j 1)α} r j 2{( j 2)α} r], forα>0,β= 0 5. Mean Devaton The amount of scatter n a populaton s evdently measured to some extent by the totalty of devatons from the mean and the medan. If X has a ETMW dstrbuton, then we can derve the mean devatons about the meanµ= E(X) and about the medan M as η 1 = 0 x µ f(x)d x,η 2 = 0 x M f(x)d x. The mean of the dstrbuton s obtaned from (12) by puttng r= 1, and the medan s obtaned by solvng the equaton γm β αm= ln(ν 0 ), whereν 0 s gven by ν 0 = (1 λ) (1 λ) 2 4λ(1 (0.5) 1/δ ), fλ 0 2λ = 1 (0.5) 1/δ, fλ=0. (12)
7 M. Pal and M. Tensuwan/Eur. J. Pure Appl. Math, 8 (2015), Order Statstcs Let T (1) < T (2) <...< T (n) be the ordered observatons n a random sample of sze n drawn from the exponentated transmuted modfed Webull dstrbuton wth cdf F(t), gven by (4) and densty f(t), gven by (5). The pdf of T(r), 1 r n, s gven by n! f (r) (t)= (r 1)!(n r)! [F(t)]r 1 [1 F(t)] n r f(t) n! = (r 1)!(n r)! δ[{1 ex p( αt γtβ )}{1λex p( αt γt β }] δr 1 [1 {1 ex p( αt γt β )} δ {1λex p( αt γt β )} δ ] n r (αtβγt β 1 )ex p( αt γt β ) [1 λ2λex p( αt γt β )], t 0,α,β,δ>0,λ [ 1,1]. Hence the pdf of the smallest and the largest order statstcs are as follows: f (1) (t)=nδ[{1 ex p( αt γt β )}{1λex p( αt γt β )}] δ 1 [1 {1 ex p( αt γt β )} δ {1λex p( αt γt β )} δ ] n 1 (αtβγt β 1 )ex p( αt γt β ) [1 λ2λex p( αt γt β )], f (n) (t)=nδ[{1 ex p( αt γt β )}{1λex p( αt γt β )}] δn 1 (αtβγt β 1 ) [1 λ2λex p( αt γt β ], t 0,α,β,δ>0,λ [ 1,1]. The densty of the(r 1)-th order statstc can be expressed as a functon of the densty of the r-th order statstc from the followng relaton: f (r1) (t)= n r r {1 (1 ex p( αt γt β )) δ (1λex p( αt γt β )) δ }] 1 1 f (r) (t). The moments of the order statstcs can be easly wrtten n terms of the moments of the modefed Webull dstrbuton by proceedng as follows: We can wrte f (r) (t) as n! f (r) (t)= (r 1)!(n r)! δ =0 ( 1) n r [{1 ex p( αt γt β )}{1λex p( αt γt β )}] δ(r) 1 (αγβ t β 1 )ex p( αt γt β )[1 λ2λex p( αt γt β )] n! n r = ( 1) g(t;α,γ,β,λ,δ(r)), t 0,α,β,γ,δ>0,λ [ 1,1], (r 1)!(n r)! =0 where g(t;α,γ,β,λ,δ(r)) denote the densty functon of an exponentated transmuted modfed Webull dstrbuton wth shape paameters(α, β, γ), transmutng parameter λ and exponentatnf parameterδ(r).
8 M. Pal and M. Tensuwan/Eur. J. Pure Appl. Math, 8 (2015), Hence, usng (12) we have E T r (s) n! = (us)δ (s 1)!(n s)! u=0 [ A(, j;(us)δ,λ)[ 1 λ j 1 ( β) k k! Γ(k( j 1)γ r 1) { {( j 1)α} k(j1)γr Γ(r{k( j 1)1}γ) 2λ ( β) k ( j 1)βγ {( j 1)α} {k(j1)1}γr} j 2 k! Γ(k( j 2)γ r 2) Γ(r{k( j 2)1}γ) { {( j 2)α} k(j2)γr( j 2)βγ {( j 2)α} {k(j2)1}γr}], forα,β> 0 n! = (us)δ[ A(, j;(us)δ,λ) (s 1)!(n s)! u=0 { 1 λ j 1 ( r ( j 1)γ 1)/β r 2λ (j1)γ j 2 ( r ( j 2)γ 1)/β r (j2)γ}], forα=0,β> 0 n! = (us)δ[ A(, j;(us)δ,λ){ 1 λ Γ(r 1) (s 1)!(n s)! j 1{( j 1)α} r u=0 2λ Γ(r 1) j 2{( j 2)α} r}]tex t, f orα>0,β= 0. In addton, we can calculate the L-moments[5], whch are summary statstcs for probablty dstrbutons and data samples but have several advantages over ordnary moments. For example, they apply for any dstrbuton havng a fnte mean and no hgher-order moments need be fnte. The rth L-moment s computed from the lnear combnatons of the ordered data values as gven below: ρ r = r 1 r u 1 ( 1) r u 1 θ u, u u u=0 whereθ u = E[T F(T) u ]. Thus,ρ 1 =θ 0,ρ 2 = 2θ 1 θ 0,ρ 3 = 6θ 2 6θ 1 θ 0, andρ 4 = 20θ 3 30θ 2 12θ 1 θ 0. In general,θ k =(k 1) 1 E(T k1:k1 ), whch can be computed from (6) by substtutng n=s=k 1 and r= 1.
9 M. Pal and M. Tensuwan/Eur. J. Pure Appl. Math, 8 (2015), Relablty A stress-strength model descrbes the lfe of a component havng a random strength X 1 and subjected to a random stress X 2. The component functons satsfactorly for X 1 > X 2 and fals when X 1 < X 2. The probablty R= Pr(X 1 > X 2 ) defnes the component relablty. Stressstrength models have many applcatons especally n engneerng concepts such as structures, deteroraton of rocket motors, statc fatgue of ceramc components, fatgue falure of arcraft structures and the agng of concrete pressure vessels. Consder X 1 and X 2 to be ndependently dstrbuted, wth X 1 ET MW(α 1,γ 1,β,λ 1,δ 1 ) and X 2 ET MW(α 2,γ 2,β,λ 2,δ 2 ). The c.d.f. F 1 of X 1 and the pdf f 2 of X 2 are obtaned from (4) and (5), respectvely. Then, where and A(k, l)= = 0,j=0 R=Pr(X 1 > X 2 )= =1 w (1) k,l =( 1)k δ1 k k,l=0 δ1 l 0 w (1) A(k, l), k,l f 2 (y)ex p( (kl)α 1 y (kl)γ 2 y β )d y f 2 (y)[1 F 1 (y)]d y λ l 1, w(2) k,l=( 1) k δ2 1 δ2 1 λ l 2 k l, w (2) (α,j 2 γ 2 β y β 1 )ex p( {(kl)α 1 ( j 1)α 2 }y 0 {(kl)γ 1 ( j 1)γ 2 }y β )(1 λ 2 2λ 2 ex p( α 2 y γ 2 y β ))d y = w (2),j [α 2{(1 λ 2 )µ MW 1 ((kl)α 1 ( j 1)α 2,(kl)γ 1 ( j 1)γ 2,β),j=0 2λ 2 µ MW 1 ((kl)α 1 ( j 2)α 2,(kl)γ 1 ( j 2)γ 2,β)} γ 2 {(1 λ 2 )µ MW β ((kl)α 1 ( j 1)α 2,(kl)γ 1 ( j 1)γ 2,β) 2λ 2 µ MW β ((kl)α 1 ( j 2)α 2,(kl)γ 1 ( j 2)γ 2,β)}], wthµ MW r (α, γ, β) gven by (11). In partcular, fα 1 =α 2 andγ 1 =γ 2, we have A(k, l)=,j=0 w (2),j [ (1 λ 2 ) ( jkl 1) 2λ 2 ( jkl 2) ].
10 M. Pal and M. Tensuwan/Eur. J. Pure Appl. Math, 8 (2015), Least Squares Estmaton Let T (1) < T (2) <...< T (n) denote the ordered observatons n a random sample of sze n drawn from the ETMW(α, γ, β, λ, δ) dstrbuton wth dstrbuton functon F( ), gven by (4). Then, E[F(T () )]=, = 1,2,..., n. n1 The least square estmators are obtaned by mnmzng D(θ)= = F(T () ) 2 n1 (1 ex p( αt () γt β () ))δ (1λex p( αt () γt β () ))δ 2. n1 Wrtng V = ex p( αt () γt β ), the normal equatons to be satsfed by the estmators are as () follows: (1 V ) δ (1λV ) δ n1 (1 V ) δ (1λV ) δ n1 (1 V ) δ (1λV ) δ n1 (1 V ) δ (1λV ) δ n1 (1 V ) δ (1λV ) δ n1 (1 V ) δ 1 (1λV ) δ 1 T () V (1 λ2λv )=0 (1 V ) δ 1 (1λV ) δ 1 T β () V (1 λ2λv )=0 (1 V ) δ 1 (1λV ) δ 1 T β () ln(t ())V (1 λ2λv )=0 (1 V ) δ (1λV ) δ 1 V = 0 (1 V ) δ (1λV ) δ [ln(1 V )ln(1λv )]=0. 9. Maxmum Lkelhood Method of Estmaton Consder a random sample(t 1, T 2,..., T n ) of sze n taken from the dstrbuton ETMW(α,γ,β,λ,δ) wth densty functon (5). For gven T = t, = 1,2,..., n, the log-lkelhood functon forθ=(α,γ,β,λ,δ) s l(θ)=n lnδ(δ 1){ ln(1 ex p( αt γt β )) ln(1λex p( αt γt β ))} ln(αγβ t β 1 ) ln(1 λ2λex p( αt γt β )) (αt γt β ).
11 M. Pal and M. Tensuwan/Eur. J. Pure Appl. Math, 8 (2015), Wrtngν = ex p( αt γt β )), = 1,2,..., n, the log-lkelhood equatons are obtaned as follows: t = 2λ t β = 2λ t β ln t = 2λ t ν (1 λ2λν ) (1 δ) t β ν (1 λ2λν ) (1 δ) (t β ln t )ν (1 λ2λν ) (1 δ) t ν (1 λ2λν ) (1 ν )(1λν ) t β ν (1 λ2λν ) (1 ν )(1λν ) β 1 (αγβ t β 1 ) (13) (t β ln t )ν (1 λ2λν ) (1 ν )(1λν ) t β 1 (αγβ t β 1 ) (14) (15) t β 1 (1β ln t ) (αγβ t β 1 ) (16) ν 1 2ν (δ 1) = 1λν 1 λ2λν (17) ln(1 ν ) ln(1λex pν )= n δ. (18) Solvng the non-lnear system of equatons (13)-(18) we obtan the maxmum lkelhood estmate ˆθ=(ˆα, ˆγ, ˆβ, ˆλ, ˆδ) ofθ. Under certan regularty condtons, n(ˆθ θ) d Normal(0, I 1 (θ)) (here d stands for convergence n dstrbuton), where I(θ) denotes the nformaton matrx gven by 2 l(θ) I(θ)= E. (19) θ θ Ths nformaton matrx I(θ) may be approxmated by the observed nformaton matrx 2 l(θ) I(ˆθ)= E. (20) θ θ Hence, usng the approxmaton n(ˆθ θ) Normal(0, I 1 (ˆθ)), one can carry out tests and fnd confdence regons for functons of some or all of the parameters nθ. θ=ˆθ 10. Smulaton Study A smulaton study s carred out to nvestgate the performance of the least square (LS) estmators and the ML estmators. We take sample szes to be n=15,25,50,100,250,500 and generate observatons from a ETMW dstrbuton wth parametersα=1,γ=1,β= 2.5, λ=0.5,δ=0.75. For each sample we compute the estmates of the parameters usng the
12 M. Pal and M. Tensuwan/Eur. J. Pure Appl. Math, 8 (2015), two methods. The process s repeated N= 1000 tmes, and the average mean squared error s computed as follows: AMSE(T)= 1 N N (ˆθ (T) θ) (ˆθ (T) θ), (21) where T denotes the method used to estmate θ =(α, γ, β, λ, δ), denotes the sample repetton number, = 1,2,..., N, and ˆθ (T) s the correspondng estmate. Table 1 gves the AMSEs for the two methods of estmaton. Table 1: Average Mean Squared Errors for the Method of Least Squares and Maxmum Lkelhood Method for Estmatngθ Sample sze AMSE(LS) AMSE(ML) The above table shows that as the sample sze ncreases, the average mean squared errors decrease. Ths verfes the consstency propertes of the estmates. Further, for each sample sze AMSE(LS)>AMSE(M L). Thus, we may conclude that the maxmum lkelhood method provdes better estmators than the least square method. However, the dfference between AMSE(LS) and AMSE(M L) decrease as the sample sze ncreases. 11. Applcaton of the Exponentated Transmuted Modfed Webull Dstrbuton In ths secton we llustrate the usefulness of the exponentated transmuted modfed Webull dstrbuton for modellng real lfe data. The data set relates to the tme-to-falure of 50 devces, and s taken from Aarset[1]: Table 2: The tme-to-falure of 50 devces The Webull (W), modfed Webull (M), transmuted modfed Webull(T) and exponentated transmuted modfed Webull (E) dstrbutons are ftted to the data and the MLEs of the
13 M. Pal and M. Tensuwan/Eur. J. Pure Appl. Math, 8 (2015), parameters are gven n Table 3. The values of the log-lkelhood, Kolmogorov-Smrnov statstc (K-S), Akake nformaton crteron (AIC) and Bayesan nformaton crteron (BIC) for the dfferent ftted dstrbutons are also gven, and show that the ETMW dstrbuton gves a better ft than the others. The same s also evdent from Fgure 2, whch compares the cumulatve dstrbuton curves of the ftted dstrbutons wth that of the emprcal dstrbuton. Table 3: The estmated parameters and the log-lkelhood, K-S, AIC, BIC values for the dfferent ftted dstrbutons α γ β λ δ -l(θ) K-S AIC BIC W M T E Fgure 2: Comparson of the CDFs of the Ftted Dstrbutons wth the Emprcal CDF 12. Dscusson In ths paper, we ntroduce a new generalzaton of the Webull dstrbuton called exponentated transmuted modfed Webull dstrbuton and dscuss ts ntrnsc propertes. The dstrbuton s very flexble n the sense that t exhbts both ncreasng and decreasng falure rates dependng on ts parameters. ACKNOWLEDGEMENTS The authors thank the anonymous referees for ther frutful suggestons, whch mmensely helped to mprove the presentaton of the paper.
14 REFERENCES 14 References [1] M. V. Aarset. How to dentfy bathtub hazard rate. IEEE Tranactons on Relablty, 36(1): , [2] G. R. Aryall and C. P. Tsokos. Transmuted Webull dstrbuton: A Generalzaton of the Webull Probablty Dstrbuton. European Journal of Pure and Appled Mathematcs, 4(2): , [3] S.K. Ashour and M.A. Eltehwy. Transmuted exponentated modfed Webull dstrbuton, Internatonal Journal of Basc and Appled Scences, 2 (3) [4] A.E. Hady and N. Ebrahem. Exponentated Transmuted Webull Dstrbuton: A Generalzaton of the Webull Dstrbuton. Internatonal Journal of Mathematcal, Computatonal, Physcal, Nuclear Scence and Engneerng, 8(6): , [5] J.R.M. Hoskng. L-moments: Analyss and estmaton of dstrbutons usng lnear combnatons of order statstcs. Journal of the Royal Statstcal Socety: Seres B, 52(1): , [6] M.S. Khan and R. Kng. Transmuted modfed Webull dstrbuton: A Generalzaton of the Modfed Webull Probablty Dstrbuton. European Journal of Pure and Appled Mathematcs, 6(1): 66-88, [7] M. Pal, and M. Tensuwan. Beta transmuted Webull dstrbuton. Austran Journal of Statstcs, 43(2): , [8] A.M. Sarhan and M. Zandn. Modfed Webull dstrbuton, Appled Scences, 11: , 2009.
Parameters Estimation of the Modified Weibull Distribution Based on Type I Censored Samples
Appled Mathematcal Scences, Vol. 5, 011, no. 59, 899-917 Parameters Estmaton of the Modfed Webull Dstrbuton Based on Type I Censored Samples Soufane Gasm École Supereure des Scences et Technques de Tuns
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 informationOn the Transmuted Additive Weibull Distribution
AUSTRIAN JOURNAL OF STATISTICS Volume 42 213, Number 2, 117 132 On the Transmuted Addtve Webull Dstrbuton Ibrahm Elbatal 1 and Gokarna Aryal 2 1 Mathematcal Statstcs, Caro Unversty, Egypt 2 Mathematcs,
More informationCOMPARISON OF SOME RELIABILITY CHARACTERISTICS BETWEEN REDUNDANT SYSTEMS REQUIRING SUPPORTING UNITS FOR THEIR OPERATIONS
Avalable onlne at http://sck.org J. Math. Comput. Sc. 3 (3), No., 6-3 ISSN: 97-537 COMPARISON OF SOME RELIABILITY CHARACTERISTICS BETWEEN REDUNDANT SYSTEMS REQUIRING SUPPORTING UNITS FOR THEIR OPERATIONS
More informationSystem in Weibull Distribution
Internatonal Matheatcal Foru 4 9 no. 9 94-95 Relablty Equvalence Factors of a Seres-Parallel Syste n Webull Dstrbuton M. A. El-Dacese Matheatcs Departent Faculty of Scence Tanta Unversty Tanta Egypt eldacese@yahoo.co
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 informationDERIVATION OF THE PROBABILITY PLOT CORRELATION COEFFICIENT TEST STATISTICS FOR THE GENERALIZED LOGISTIC DISTRIBUTION
Internatonal Worshop ADVANCES IN STATISTICAL HYDROLOGY May 3-5, Taormna, Italy DERIVATION OF THE PROBABILITY PLOT CORRELATION COEFFICIENT TEST STATISTICS FOR THE GENERALIZED LOGISTIC DISTRIBUTION by Sooyoung
More informationInterval Estimation of Stress-Strength Reliability for a General Exponential Form Distribution with Different Unknown Parameters
Internatonal Journal of Statstcs and Probablty; Vol. 6, No. 6; November 17 ISSN 197-73 E-ISSN 197-74 Publshed by Canadan Center of Scence and Educaton Interval Estmaton of Stress-Strength Relablty for
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 informationNew Extended Weibull Distribution
Crculaton n Computer Scence Vol No6 pp: (4-9) July 7 https:doorg6ccs-7-5- New Extended Webull Dstrbuton Zubar Ahmad Research Scholar: Department of Statstcs Quad--Aam Unversty 45 Islamabad 44 Pastan Zawar
More informationASYMPTOTIC PROPERTIES OF ESTIMATES FOR THE PARAMETERS IN THE LOGISTIC REGRESSION MODEL
Asymptotc Asan-Afrcan Propertes Journal of Estmates Economcs for and the Econometrcs, Parameters n Vol. the Logstc, No., Regresson 20: 65-74 Model 65 ASYMPTOTIC PROPERTIES OF ESTIMATES FOR THE PARAMETERS
More informationGoodness of fit and Wilks theorem
DRAFT 0.0 Glen Cowan 3 June, 2013 Goodness of ft and Wlks theorem Suppose we model data y wth a lkelhood L(µ) that depends on a set of N parameters µ = (µ 1,...,µ N ). Defne the statstc t µ ln L(µ) L(ˆµ),
More informationChapter 5. Solution of System of Linear Equations. Module No. 6. Solution of Inconsistent and Ill Conditioned Systems
Numercal Analyss by Dr. Anta Pal Assstant Professor Department of Mathematcs Natonal Insttute of Technology Durgapur Durgapur-713209 emal: anta.bue@gmal.com 1 . Chapter 5 Soluton of System of Lnear Equatons
More informationUsing T.O.M to Estimate Parameter of distributions that have not Single Exponential Family
IOSR Journal of Mathematcs IOSR-JM) ISSN: 2278-5728. Volume 3, Issue 3 Sep-Oct. 202), PP 44-48 www.osrjournals.org Usng T.O.M to Estmate Parameter of dstrbutons that have not Sngle Exponental Famly Jubran
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 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 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 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 informationRandić Energy and Randić Estrada Index of a Graph
EUROPEAN JOURNAL OF PURE AND APPLIED MATHEMATICS Vol. 5, No., 202, 88-96 ISSN 307-5543 www.ejpam.com SPECIAL ISSUE FOR THE INTERNATIONAL CONFERENCE ON APPLIED ANALYSIS AND ALGEBRA 29 JUNE -02JULY 20, ISTANBUL
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 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 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 information2E Pattern Recognition Solutions to Introduction to Pattern Recognition, Chapter 2: Bayesian pattern classification
E395 - Pattern Recognton Solutons to Introducton to Pattern Recognton, Chapter : Bayesan pattern classfcaton Preface Ths document s a soluton manual for selected exercses from Introducton to Pattern Recognton
More informationOn an Extension of Stochastic Approximation EM Algorithm for Incomplete Data Problems. Vahid Tadayon 1
On an Extenson of Stochastc Approxmaton EM Algorthm for Incomplete Data Problems Vahd Tadayon Abstract: The Stochastc Approxmaton EM (SAEM algorthm, a varant stochastc approxmaton of EM, s a versatle tool
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 informationSmall Area Interval Estimation
.. Small Area Interval Estmaton Partha Lahr Jont Program n Survey Methodology Unversty of Maryland, College Park (Based on jont work wth Masayo Yoshmor, Former JPSM Vstng PhD Student and Research Fellow
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 informationStatistical analysis using matlab. HY 439 Presented by: George Fortetsanakis
Statstcal analyss usng matlab HY 439 Presented by: George Fortetsanaks Roadmap Probablty dstrbutons Statstcal estmaton Fttng data to probablty dstrbutons Contnuous dstrbutons Contnuous random varable X
More informationDagum Distribution: Properties and Different Methods of Estimation
Internatonal Journal of Statstcs and Probablty; Vol. 6, No. 2; March 27 ISSN 927-732 E-ISSN 927-74 Publshed by Canadan Center of Scence and Educaton Dagum Dstrbuton: Propertes and Dfferent Methods of Estmaton
More informationNumerical Heat and Mass Transfer
Master degree n Mechancal Engneerng Numercal Heat and Mass Transfer 06-Fnte-Dfference Method (One-dmensonal, steady state heat conducton) Fausto Arpno f.arpno@uncas.t Introducton Why we use models and
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 informationDouble Acceptance Sampling Plan for Time Truncated Life Tests Based on Transmuted Generalized Inverse Weibull Distribution
J. Stat. Appl. Pro. 6, No. 1, 1-6 2017 1 Journal of Statstcs Applcatons & Probablty An Internatonal Journal http://dx.do.org/10.18576/jsap/060101 Double Acceptance Samplng Plan for Tme Truncated Lfe Tests
More informationThe RS Generalized Lambda Distribution Based Calibration Model
Internatonal Journal of Statstcs and Probablty; Vol. 2, No. 1; 2013 ISSN 1927-7032 E-ISSN 1927-7040 Publshed by Canadan Center of Scence and Educaton The RS Generalzed Lambda Dstrbuton Based Calbraton
More informationEstimation of the Mean of Truncated Exponential Distribution
Journal of Mathematcs and Statstcs 4 (4): 84-88, 008 ISSN 549-644 008 Scence Publcatons Estmaton of the Mean of Truncated Exponental Dstrbuton Fars Muslm Al-Athar Department of Mathematcs, Faculty of Scence,
More informationISSN X Reliability of linear and circular consecutive-kout-of-n systems with shock model
Afrka Statstka Vol. 101, 2015, pages 795 805. DOI: http://dx.do.org/10.16929/as/2015.795.70 Afrka Statstka ISSN 2316-090X Relablty of lnear and crcular consecutve-kout-of-n systems wth shock model Besma
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 informationThe Quadratic Trigonometric Bézier Curve with Single Shape Parameter
J. Basc. Appl. Sc. Res., (3541-546, 01 01, TextRoad Publcaton ISSN 090-4304 Journal of Basc and Appled Scentfc Research www.textroad.com The Quadratc Trgonometrc Bézer Curve wth Sngle Shape Parameter Uzma
More informationAn Application of Fuzzy Hypotheses Testing in Radar Detection
Proceedngs of the th WSES Internatonal Conference on FUZZY SYSEMS n pplcaton of Fuy Hypotheses estng n Radar Detecton.K.ELSHERIF, F.M.BBDY, G.M.BDELHMID Department of Mathematcs Mltary echncal Collage
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 informationLecture Notes on Linear Regression
Lecture Notes on Lnear Regresson Feng L fl@sdueducn Shandong Unversty, Chna Lnear Regresson Problem In regresson problem, we am at predct a contnuous target value gven an nput feature vector We assume
More informationBayesian predictive Configural Frequency Analysis
Psychologcal Test and Assessment Modelng, Volume 54, 2012 (3), 285-292 Bayesan predctve Confgural Frequency Analyss Eduardo Gutérrez-Peña 1 Abstract Confgural Frequency Analyss s a method for cell-wse
More informationGeneralized Linear Methods
Generalzed Lnear Methods 1 Introducton In the Ensemble Methods the general dea s that usng a combnaton of several weak learner one could make a better learner. More formally, assume that we have a set
More informationPower law and dimension of the maximum value for belief distribution with the max Deng entropy
Power law and dmenson of the maxmum value for belef dstrbuton wth the max Deng entropy Bngy Kang a, a College of Informaton Engneerng, Northwest A&F Unversty, Yanglng, Shaanx, 712100, Chna. Abstract Deng
More informationSimulation and Probability Distribution
CHAPTER Probablty, Statstcs, and Relablty for Engneers and Scentsts Second Edton PROBABILIT DISTRIBUTION FOR CONTINUOUS RANDOM VARIABLES A. J. Clark School of Engneerng Department of Cvl and Envronmental
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 informationFUZZY GOAL PROGRAMMING VS ORDINARY FUZZY PROGRAMMING APPROACH FOR MULTI OBJECTIVE PROGRAMMING PROBLEM
Internatonal Conference on Ceramcs, Bkaner, Inda Internatonal Journal of Modern Physcs: Conference Seres Vol. 22 (2013) 757 761 World Scentfc Publshng Company DOI: 10.1142/S2010194513010982 FUZZY GOAL
More informationTurbulence classification of load data by the frequency and severity of wind gusts. Oscar Moñux, DEWI GmbH Kevin Bleibler, DEWI GmbH
Turbulence classfcaton of load data by the frequency and severty of wnd gusts Introducton Oscar Moñux, DEWI GmbH Kevn Blebler, DEWI GmbH Durng the wnd turbne developng process, one of the most mportant
More informationResearch Article The Generalized Inverse Generalized Weibull Distribution and Its Properties
Hndaw Publshng Corporaton Probablty, Artcle ID 73611, 11 pages http://dx.do.org/1.1155/14/73611 Research Artcle The Generalzed Inverse Generalzed Webull Dstrbuton and Its Propertes Kanchan Jan, Neetu Sngla,
More informationMarshall-Olkin Log-Logistic Extended Weibull Distribution : Theory, Properties and Applications
Journal of Data Scence 15(217), 691-722 Marshall-Olkn Log-Logstc Extended Webull Dstrbuton : Theory, Propertes and Applcatons Lornah Lepetu 1, Broderck O. Oluyede 2, Bokanyo Makubate 3, Susan Foya 4 and
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 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 informationLinear Regression Analysis: Terminology and Notation
ECON 35* -- Secton : Basc Concepts of Regresson Analyss (Page ) Lnear Regresson Analyss: Termnology and Notaton Consder the generc verson of the smple (two-varable) lnear regresson model. It s represented
More information8/25/17. Data Modeling. Data Modeling. Data Modeling. Patrice Koehl Department of Biological Sciences National University of Singapore
8/5/17 Data Modelng Patrce Koehl Department of Bologcal Scences atonal Unversty of Sngapore http://www.cs.ucdavs.edu/~koehl/teachng/bl59 koehl@cs.ucdavs.edu Data Modelng Ø Data Modelng: least squares Ø
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 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 informationCHAPTER-5 INFORMATION MEASURE OF FUZZY MATRIX AND FUZZY BINARY RELATION
CAPTER- INFORMATION MEASURE OF FUZZY MATRI AN FUZZY BINARY RELATION Introducton The basc concept of the fuzz matr theor s ver smple and can be appled to socal and natural stuatons A branch of fuzz matr
More informationDUE: WEDS FEB 21ST 2018
HOMEWORK # 1: FINITE DIFFERENCES IN ONE DIMENSION DUE: WEDS FEB 21ST 2018 1. Theory Beam bendng s a classcal engneerng analyss. The tradtonal soluton technque makes smplfyng assumptons such as a constant
More informationEngineering Risk Benefit Analysis
Engneerng Rsk Beneft Analyss.55, 2.943, 3.577, 6.938, 0.86, 3.62, 6.862, 22.82, ESD.72, ESD.72 RPRA 2. Elements of Probablty Theory George E. Apostolaks Massachusetts Insttute of Technology Sprng 2007
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 informationDISCRETE GENERALIZED RAYLEIGH DISTRIBUTION
Pak. J. Statst. 06 Vol. 3(), -0 DISCRETE GENERALIZED RAYLEIGH DISTRIBUTION M.H. Alamatsaz, S. Dey, T. Dey 3 and S. Shams Harand 4 Department of Statstcs, Unversty of Isfahan, Isfahan, Iran Naghshejahan
More informationUSE 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 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 informationHydrological statistics. Hydrological statistics and extremes
5--0 Stochastc Hydrology Hydrologcal statstcs and extremes Marc F.P. Berkens Professor of Hydrology Faculty of Geoscences Hydrologcal statstcs Mostly concernes wth the statstcal analyss of hydrologcal
More informationCS 2750 Machine Learning. Lecture 5. Density estimation. CS 2750 Machine Learning. Announcements
CS 750 Machne Learnng Lecture 5 Densty estmaton Mlos Hauskrecht mlos@cs.ptt.edu 539 Sennott Square CS 750 Machne Learnng Announcements Homework Due on Wednesday before the class Reports: hand n before
More informationDr. Shalabh Department of Mathematics and Statistics Indian Institute of Technology Kanpur
Analyss of Varance and Desgn of Experments- MODULE LECTURE - 6 EXPERMENTAL DESGN MODELS Dr. Shalabh Department of Mathematcs and Statstcs ndan nsttute of Technology Kanpur Two-way classfcaton wth nteractons
More informationA PROBABILITY-DRIVEN SEARCH ALGORITHM FOR SOLVING MULTI-OBJECTIVE OPTIMIZATION PROBLEMS
HCMC Unversty of Pedagogy Thong Nguyen Huu et al. A PROBABILITY-DRIVEN SEARCH ALGORITHM FOR SOLVING MULTI-OBJECTIVE OPTIMIZATION PROBLEMS Thong Nguyen Huu and Hao Tran Van Department of mathematcs-nformaton,
More informationChapter 20 Duration Analysis
Chapter 20 Duraton Analyss Duraton: tme elapsed untl a certan event occurs (weeks unemployed, months spent on welfare). Survval analyss: duraton of nterest s survval tme of a subject, begn n an ntal state
More informationModeling and Simulation NETW 707
Modelng and Smulaton NETW 707 Lecture 5 Tests for Random Numbers Course Instructor: Dr.-Ing. Magge Mashaly magge.ezzat@guc.edu.eg C3.220 1 Propertes of Random Numbers Random Number Generators (RNGs) must
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 informationThe lower and upper bounds on Perron root of nonnegative irreducible matrices
Journal of Computatonal Appled Mathematcs 217 (2008) 259 267 wwwelsevercom/locate/cam The lower upper bounds on Perron root of nonnegatve rreducble matrces Guang-Xn Huang a,, Feng Yn b,keguo a a College
More informationThe Ordinary Least Squares (OLS) Estimator
The Ordnary Least Squares (OLS) Estmator 1 Regresson Analyss Regresson Analyss: a statstcal technque for nvestgatng and modelng the relatonshp between varables. Applcatons: Engneerng, the physcal and chemcal
More informationUNIVERSITY OF TORONTO Faculty of Arts and Science. December 2005 Examinations STA437H1F/STA1005HF. Duration - 3 hours
UNIVERSITY OF TORONTO Faculty of Arts and Scence December 005 Examnatons STA47HF/STA005HF Duraton - hours AIDS ALLOWED: (to be suppled by the student) Non-programmable calculator One handwrtten 8.5'' x
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 informationOn mutual information estimation for mixed-pair random variables
On mutual nformaton estmaton for mxed-par random varables November 3, 218 Aleksandr Beknazaryan, Xn Dang and Haln Sang 1 Department of Mathematcs, The Unversty of Msssspp, Unversty, MS 38677, USA. E-mal:
More informationThe Order Relation and Trace Inequalities for. Hermitian Operators
Internatonal Mathematcal Forum, Vol 3, 08, no, 507-57 HIKARI Ltd, wwwm-hkarcom https://doorg/0988/mf088055 The Order Relaton and Trace Inequaltes for Hermtan Operators Y Huang School of Informaton Scence
More informationMATH 829: Introduction to Data Mining and Analysis The EM algorithm (part 2)
1/16 MATH 829: Introducton to Data Mnng and Analyss The EM algorthm (part 2) Domnque Gullot Departments of Mathematcal Scences Unversty of Delaware Aprl 20, 2016 Recall 2/16 We are gven ndependent observatons
More informationStatistical Hypothesis Testing for Returns to Scale Using Data Envelopment Analysis
Statstcal Hypothess Testng for Returns to Scale Usng Data nvelopment nalyss M. ukushge a and I. Myara b a Graduate School of conomcs, Osaka Unversty, Osaka 560-0043, apan (mfuku@econ.osaka-u.ac.p) b Graduate
More informationFirst Year Examination Department of Statistics, University of Florida
Frst Year Examnaton Department of Statstcs, Unversty of Florda May 7, 010, 8:00 am - 1:00 noon Instructons: 1. You have four hours to answer questons n ths examnaton.. You must show your work to receve
More informationImproved Approximation Methods to the Stopped Sum Distribution
Internatonal Journal of Mathematcal Analyss and Applcatons 2017; 4(6): 42-46 http://www.aasct.org/journal/jmaa ISSN: 2375-3927 Improved Approxmaton Methods to the Stopped Sum Dstrbuton Aman Al Rashd *,
More informationThe Jacobsthal and Jacobsthal-Lucas Numbers via Square Roots of Matrices
Internatonal Mathematcal Forum, Vol 11, 2016, no 11, 513-520 HIKARI Ltd, wwwm-hkarcom http://dxdoorg/1012988/mf20166442 The Jacobsthal and Jacobsthal-Lucas Numbers va Square Roots of Matrces Saadet Arslan
More informationCIS526: Machine Learning Lecture 3 (Sept 16, 2003) Linear Regression. Preparation help: Xiaoying Huang. x 1 θ 1 output... θ M x M
CIS56: achne Learnng Lecture 3 (Sept 6, 003) Preparaton help: Xaoyng Huang Lnear Regresson Lnear regresson can be represented by a functonal form: f(; θ) = θ 0 0 +θ + + θ = θ = 0 ote: 0 s a dummy attrbute
More informationDegradation Data Analysis Using Wiener Process and MCMC Approach
Engneerng Letters 5:3 EL_5_3_0 Degradaton Data Analyss Usng Wener Process and MCMC Approach Chunpng L Hubng Hao Abstract Tradtonal relablty assessment methods are based on lfetme data. However the lfetme
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 informationRandom Partitions of Samples
Random Parttons of Samples Klaus Th. Hess Insttut für Mathematsche Stochastk Technsche Unverstät Dresden Abstract In the present paper we construct a decomposton of a sample nto a fnte number of subsamples
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 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 informationU-Pb Geochronology Practical: Background
U-Pb Geochronology Practcal: Background Basc Concepts: accuracy: measure of the dfference between an expermental measurement and the true value precson: measure of the reproducblty of the expermental result
More informationPredictive Analytics : QM901.1x Prof U Dinesh Kumar, IIMB. All Rights Reserved, Indian Institute of Management Bangalore
Sesson Outlne Introducton to classfcaton problems and dscrete choce models. Introducton to Logstcs Regresson. Logstc functon and Logt functon. Maxmum Lkelhood Estmator (MLE) for estmaton of LR parameters.
More informationAppendix B. The Finite Difference Scheme
140 APPENDIXES Appendx B. The Fnte Dfference Scheme In ths appendx we present numercal technques whch are used to approxmate solutons of system 3.1 3.3. A comprehensve treatment of theoretcal and mplementaton
More informationWhich estimator of the dispersion parameter for the Gamma family generalized linear models is to be chosen?
STATISTICS Dalarna Unversty D-level Master s Thess 007 Whch estmator of the dsperson parameter for the Gamma famly generalzed lnear models s to be chosen? Submtted by: Juan Du Regstraton Number: 8096-T084
More informationLiu-type Negative Binomial Regression: A Comparison of Recent Estimators and Applications
Lu-type Negatve Bnomal Regresson: A Comparson of Recent Estmators and Applcatons Yasn Asar Department of Mathematcs-Computer Scences, Necmettn Erbaan Unversty, Konya 4090, Turey, yasar@onya.edu.tr, yasnasar@hotmal.com
More informationBOOTSTRAP METHOD FOR TESTING OF EQUALITY OF SEVERAL MEANS. M. Krishna Reddy, B. Naveen Kumar and Y. Ramu
BOOTSTRAP METHOD FOR TESTING OF EQUALITY OF SEVERAL MEANS M. Krshna Reddy, B. Naveen Kumar and Y. Ramu Department of Statstcs, Osmana Unversty, Hyderabad -500 007, Inda. nanbyrozu@gmal.com, ramu0@gmal.com
More informationProcess Monitoring of Exponentially Distributed Characteristics. Through an Optimal Normalizing Transformation
Process Montorng of Exponentally Dstrbuted Characterstcs Through an Optmal Normalzng Transformaton Zhenln Yang Department of Statstcs and Appled Probablty Natonal Unversty of Sngapore, Kent Rdge, Sngapore
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 informationn α j x j = 0 j=1 has a nontrivial solution. Here A is the n k matrix whose jth column is the vector for all t j=0
MODULE 2 Topcs: Lnear ndependence, bass and dmenson We have seen that f n a set of vectors one vector s a lnear combnaton of the remanng vectors n the set then the span of the set s unchanged f that vector
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 informationThe optimal delay of the second test is therefore approximately 210 hours earlier than =2.
THE IEC 61508 FORMULAS 223 The optmal delay of the second test s therefore approxmately 210 hours earler than =2. 8.4 The IEC 61508 Formulas IEC 61508-6 provdes approxmaton formulas for the PF for smple
More informationLOW BIAS INTEGRATED PATH ESTIMATORS. James M. Calvin
Proceedngs of the 007 Wnter Smulaton Conference S G Henderson, B Bller, M-H Hseh, J Shortle, J D Tew, and R R Barton, eds LOW BIAS INTEGRATED PATH ESTIMATORS James M Calvn Department of Computer Scence
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 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 information