1 kawaguchi p.1/81
|
|
- きみお つつの
- 5 years ago
- Views:
Transcription
1 1 kawaguchi p.1/81
2 AUC 4.4 p.2/81
3 X Z X = α + βz + e α : Z = 0 X ( ) β : Z X ( ) e : 0 σ 2 p.3/81
4 2.1 Z X Z : X : Beckmann p.4/81
5 R ( ) z<-c(1, 2, 4, 6, 7, 8, 10, 15) x<-c(0.045, 0.114, 0.215, 0.346, 0.410, 0.520, 0.670, 0.942) z, x plot(z,x) p.5/81
6 x z p.6/81
7 n (Z 1,X 1 ),...,(Z n,x n ) S 2 = n (X i α βz i ) 2 i=1 a b b = (Zi Z)(X i X) (Zi Z) 2 a = X b Z p.7/81
8 R ( ) lm(x z) Call: lm(formula = x z) Coefficients: (Intercept) z p.8/81
9 SAS ( ) data beckmann; input z datalines; run; proc reg data=beckmann; model x=z ; run; p.9/81
10 SAS ( ) SAS p.10/81
11 X = α + β(z Z) + e α β a = X, b = (Zi Z)(X i X) (Zi Z) 2 Z X a b p.11/81
12 s ZX Z X s ZX = (Zi Z)(X i X) n 1 b = s ZX s X Z X r ( 1 r 1) r = s ZX s Z s X b = r s X s Z s Z = 1 n 1 (Zi Z) 2 s X = 1 n 1 (Xi X) 2 p.12/81
13 R 2 = S2 1 S 2 2 S 2 1 S 2 1 = (X i X) 2, S 2 2 = [X i X b(z i Z)] 2 R 2 = r 2 p.13/81
14 b β U,T R Z X = U +f, Z = T +e, e f R Z = σ2 T σ 2 T + σ2 e, R X = σ2 U σ 2 U + σ2 f β U,T U V Z Z p.14/81
15 e σ 2 s 2 = = (Xi a bz i ) 2 n 2 (Xi X a b(z i Z)) 2 n 2 (E[s 2 ] = σ 2 ) n 2 p.15/81
16 (1) β 100(1 α)% b t n 2,α/2 se(b) β b + t n 2,α/2 se(b) se(b) = s (Zi Z) 2 s t ν,p ν t p% p.16/81
17 (2) H 0 : β = 0 ( α%) t = b se(b) ( ) t > t n 2,α/2 = H 0 reject (H 0 reject 0 ) p.17/81
18 t t = b se(b) = r n 2 1 r 2 H 0 : β = 0 H 0 : ρ = 0 ρ p.18/81
19 (1) α 100(1 α)% a t n 2,α/2 se(a ) α a + t n 2,α/2 se(a ) se(a ) = s 1 n + Z2 (Zi Z) 2 p.19/81
20 (2) H 0 : α = 0 ( α%) t = a se(a ) t > t n 2,α/2 = H 0 reject p.20/81
21 R ( ) coefficients(summary(lm(x z))) Estimate Std.Error t value Pr(> t ) (Intercept) z e p.21/81
22 R ( ) confint(lm(x z)) 2.5 % 97.5 % (Intercept) z p.22/81
23 SAS ( ) (CLB) proc reg data=beckmann; model x=z / CLB; run; p.23/81
24 (1) X = βz + e β ˆβ = Zi X i Z 2 i p.24/81
25 (2) β 100(1 α)% ˆβ t n 2,α/2 se(ˆβ) β ˆβ + t n 2,α/2 se(ˆβ) se(β) = v Z 2 i v = 1 n 1 (Xi ˆβZ i ) 2 p.25/81
26 R ( ) summary(lm(x z-1)) confint(lm(x z-1)) Estimate Std.Error t value Pr(> t ) z < β p.26/81
27 SAS ( ) (NOINT) proc reg data=beckmann; model x=z /NOINT CLB; run; p.27/81
28 Z = Z 0 α + βz 0 100(1 α)% a + bz 0 ± t n 2,α/2 s 1 n + (Z 0 Z) 2 (Zi Z) 2 Z 0 = 0 p.28/81
29 ( 1) Z = Z i (i = 1, 2,... ) = (Bonferroni ) P {a + bz (α + βz)} ( ) 2 M s 2 1 (Z Z) 2 α, Z = 1 α n + (Zi Z) 2 M α p.29/81
30 ( 2) P max Z {a + bz (α + βz)} ( ) 2 s 2 1 n + (Z Z) 2 (Zi Z) 2 M α = 1 α M α = ( X E[ X]) 2 σ 2 /n + (b β)2 σ 2 / (Z i Z) 2 s 2 /σ 2 2F 2,n 2 p.30/81
31 α + βz 100(1 α)% L(Z ) < α + βz < U(Z ) Z Z L(Z ) = X + b(z Z) A(Z ) U(Z ) = X + b(z Z) + A(Z ) ( 1 A(Z ) = 2F 2,n 2,α s 2 n + (Z Z) ) 2 (Zi Z) 2 p.31/81
32 R ( 2.8) 1 n<-length(z) new.z<- seq(2, 12, by=0.02) ones<-rep(1, length(new.z)) pre.z<-rbind(ones, new.z) a<-lm(x z)$coefficients plot(new.z, a%*%pre.z, ylim=c(0,1), type="l", lwd=2, xlab="z", ylab="x") p.32/81
33 R ( 2.8) 2 sz<-sum((z-mean(z))ˆ2) s2<-sum((lm(x z)$residuals)ˆ2)/(n-2) s1<-1/n+(new.z-mean(z))ˆ2/sz U<-a%*%pre.z+sqrt(2*qf(0.95,2,6)*s2*s1) L<-a%*%pre.z-sqrt(2*qf(0.95,2,6)*s2*s1) points(new.z, U, type="l") points(new.z, L, type="l") points(z, x) p.33/81
34 2.8 x z p.34/81
35 R ( ) p.u<-a%*%pre.z+sqrt(qt(0.95,2,6)*s2*s1) p.l<-a%*%pre.z-sqrt(qt(0.95,2,6)*s2*s1) points(new.z, p.u, type="l",lty=3) points(new.z, p.l, type="l",lty=3) p.35/81
36 x z p.36/81
37 ( ) ( 2.1 ) X( ) Z( ) Ẑ = Z + X X b Z = Fieller p.37/81
38 Fieller U N(µ,sa 1 ), V N(ν,sa 2 ), s : g = t2 m,α/2 s2 a 2 2 V 2 g < 1 (V 0 ) µ/ν 100(1 α)% ( 1 U 1 g V ± t ) m,α/2s (1 g)a 2 1 V + U2 a 2 2 V 2 p.38/81
39 Fieller θ = µ/ν E[U θv ] = 0, ˆV [U θv ] = s 2 (a θ 2 a 2 2) θ 100(1 α)% { (U θv ) 2 } θ : s 2 (a θ2 a 2 2 ) t2 m,α/2 t m,α/2 s 2 a 2 2 /V 2 < 1 p.39/81
40 Z (Fieller ) U = X X V = b n+1 s se(u) = s n se(v ) = (Zi Z) 2 = a 2 1 = (n + 1)/n a 2 2 = 1/ (Z i Z) 2 g = t2 m,α/2 s2 a 2 2 V 2 = t2 n 2,α/2 s2 b 2 (Z i Z) 2 p.40/81
41 Z (Fieller ) Fieller = (Z Z) 100(1 α)% E[U] E[V ] = β(z Z) β X X b(1 g) ±t n 2,α/2s b(1 g) (1 g)(n + 1) n + (X X) 2 b 2 (Z i Z) 2 Z Z 100(1 α)% p.41/81
42 R (Z ) new.x< hat.z<-mean(z)+(new.x-mean(x))/a[2] g1<-s2*(qt(0.975, (length(z)-2)))ˆ2 g2<-a[2]ˆ2*sum((z-mean(z))ˆ2) g<-g1/g2 m1<-mean(z)+(new.x-mean(x))/(a[2]*(1-g)) m2<-qt(0.975, (n-2))*sqrt(s2)/(a[2]*(1-g)) m31<-((1-g)*(n+1))/(n) m32<-(new.x-mean(x))ˆ2/(a[2]ˆ2*sz) m1+m2*sqrt(m31+m32) m1-m2*sqrt(m31+m32) p.42/81
43 Z ( ) Z > hat.z Z 95% > m1+m2*sqrt(m31+m32) > m1-m2*sqrt(m31+m32) Z p.43/81
44 AUC AUC(Area Under the bood - level Curve) concentrations concentrations concentrations time time time Subject 1 Subject 2 Subject 3 p.44/81
45 SAS NLMIXED Example (Pinheiro and Bates, 1995) time( ) conc( ) dose( ) AUC R PK AUC p.45/81
46 R (AUC ) data<-read.table("auc_data.txt", header=true) library(pk) auc<-matrix(0, 12, 3) for(i in 1:12) {auc[i,]<- AUC(conc=data$CONC[data$SUBJECT==i], time=data$time[data$subject==i])$auc} colnames(auc) <- c("obs","inter","inf") auc<-data.frame(auc) p.46/81
47 log(auc) = α + β log( ) + ε AUC = e α ( ) β e ε { β 1 = AUC β = 1 = AUC p.47/81
48 H 0 : β = 1 log(auc) log( ) log(auc) log( ) = α + β log( ) + ε β H 0 : β = 0 p.48/81
49 R ( ) dose<-numeric(0) for(i in 1:12) {dose[i]<-data$dose[data$subject==i]} ones<-rep(1, length(dose)) predictor<-rbind(ones, log(dose)) plot(log(dose), log(auc$inf), xlab="log(dose)",ylab="log(auc)",ylim=c(4.4, 5.4)) points(log(dose), lm(log(auc$inf) log(dose))$coe%*%predictor,type="l") p.49/81
50 log(auc) log(dose) log(auc) = log( ) p.50/81
51 R (H 0 : β = 1 ) coefficients(summary( lm((log(auc$inf)-log(dose)) log(dose)))) Estimate Std. Error t value Pr(> t ) (Intercept) <0.001 log(dose) p.51/81
52 R (β ) confint(lm((log(auc$inf)) log(dose))) 2.5 % 97.5 % (Intercept) log(dose) p.52/81
53 R ( ) plot(lm(log(auc$inf) log(dose))) Q-Q Cook p.53/81
54 Scale-Location plot Standardized residuals Fitted values 1 Cook s distance plot Obs. number p.54/81 Cook s distance
55 ( ) log(auc) log(dose) log(auc) = log( ) p.55/81
56 H 0 : β = 1 ( ) coefficients(summary( lm((log(auc$inf)[-1]-log(dose)[-1]) log(dose)[-1]))) Estimate Std. Error t value Pr(> t ) (Intercept) <0.001 log(dose)[-1] p.56/81
57 β ( ) confint( lm((log(auc$inf)[-1]) log(dose)[-1])) 2.5 % 97.5 % (Intercept) log(dose)[-1] p.57/81
58 log(auc) = log( ) H 0 : β = β 1.52 AUC (Subject 1 ) log(auc) = log( ) H 0 : β = β 1.44 AUC p.58/81
59 (Subject1 ) Scale-Location plot Cook s distance plot Standardized residuals Cook s distance Fitted values Obs. number p.59/81
60 X: Z: D Z i = log 2 ( /3.5) (Z i ) n i Xi s i 1 3.5(0) (1) (2) s i : X p.60/81
61 Z 2 0 Z 0 p.61/81
62 X i : Z i X (i = 1, 2,...,g) H 0 : 2 F = ni ( X i X i) 2 (g 3)s 2 F > F g 3,ν,α/3 = H 0 reject p.62/81
63 X Z X = α + βz + γz 2 + ε ( ) s s 2 = (ni 1)s 2 i (ni 1) p.63/81
64 a b c a ni Xi b = M 1 ni Xi Z i c ni Xi Zi 2 ni ni Z i ni Zi 2 M = ni Z i ni Zi 2 ni Zi 3 ni Zi 2 ni Zi 3 ni Zi 4 p.64/81
65 R ( ) z<-c(0, 1, 2) n<-c(10, 8, 13) x<-c(1.80, 3.31, 3.42) M<-c(sum(n), sum(n*z), sum(n*zˆ2), sum(n*z), sum(n*zˆ2), sum(n*zˆ3), sum(n*zˆ2), sum(n*zˆ3), sum(n*zˆ4)) M<-matrix(M, ncol=3) M2<-c(sum(n*x), sum(n*x*z), sum(n*x*zˆ2)) a<-solve(m)%*%m2 p.65/81
66 R ( : ) > a [,1] [1,] 1.80 [2,] 2.21 [3,] a = 1.80 b = 2.21 c = 0.70 p.66/81
67 2 H 0 : Z 2 γ = 0 (α/2%) L c = c se(c) se(c) = s m (3,3) m (3,3) M L c > t n 3,α/4 = H 0 reject p.67/81
68 R (2 ) s2<-((n-1)%*%sˆ2)/sum(n-1) se.c<-sqrt(s2*solve(m)[3,3]) L.c<-a[3]/se.c p.c<-1-pt(abs(l.c), 28, )# > p.c H 0 : γ = % p.68/81
69 (1) X Z : Z a X Z = a + bz + cz 2 = Z b c Z = (1,Z,Z 2 ) p.69/81
70 (2) 2 Working-Hotelling ( 100(1 α)%) X Z ± 3F 3,n. g,α se(x z) n. = n i se(x Z) = s Z M 1 Z p.70/81
71 R ( ) new.z<-seq(0, 3, 0.2) ones<-rep(1, length(new.z)) new.z<-cbind(ones, new.z, new.zˆ2) se.x<-sqrt(s2*diag(new.z%*%solve(m)%*%t(new.z))) plot(new.z, new.z%*%a, ylim=c(0,6), type="l", xlab="z", ylab="x") U<-new.Z%*%a+sqrt(3*qf(0.95, 3, sum(n)-3))*se.x L<-new.Z%*%a-sqrt(3*qf(0.95, 3, sum(n)-3))*se.x points(new.z, U, type="l") points(new.z, L, type="l") points(z, x) p.71/81
72 x z p.72/81
73 X = α + βz + ε ˆβ = ni (Z i Z)(X i X) ni (Z i Z) 2 ˆα = ni Xi ˆβ n i Z i ni p.73/81
74 beta<-((sum(n)*sum(n*x*z)-(sum(n*x))*(sum(n*z))) /(sum(n)*sum(n*zˆ2)-sum(n*z)ˆ2)) alpha<-((sum(n*x)-beta*sum(n*z))/(sum(n))) > beta [1] > alpha [1] ˆβ = 0.786, ˆα = p.74/81
75 H 0 : β = 0 ( α/2%) Lˆβ = ˆβ se(ˆβ) se(ˆβ) = s ni ni (Z i Z) 2 Lˆβ > t n 3,α/4 = H 0 reject p.75/81
76 R ( ) se.beta<-(sqrt((s2*sum(n))/ (sum(n)*sum(n*zˆ2)-sum(n*z)ˆ2))) L.beta<-beta/se.beta p.beta<-1-pt(l.beta, 28, ) p.76/81
77 : > L.beta > p.beta H 0 : β = % p.77/81
78 R ( ) a1<-coefficients(lm(x z, weight=n)) ones<-rep(1, length(new.z)) new.z1<-cbind(ones, new.z) points(new.z, new.z1%*%a1, type="l") p.78/81
79 x z p.79/81
80 4.6 Z 2 0 Z 0 Z D p.80/81
81 J.L. (KR ) (2004). RjpWiki Pinheiro, J.C. and Bates, D.M. (1995), "Approximations to the Log-likelihood Function in the Nonlinear Mixed-effects Model," Journal of Computational and Graphical Statistics, 4, p.81/81
(lm) lm AIC 2 / 1
W707 s-taiji@is.titech.ac.jp 1 / 1 (lm) lm AIC 2 / 1 : y = β 1 x 1 + β 2 x 2 + + β d x d + β d+1 + ϵ (ϵ N(0, σ 2 )) y R: x R d : β i (i = 1,..., d):, β d+1 : ( ) (d = 1) y = β 1 x 1 + β 2 + ϵ (d > 1) y
More informationDAA09
> summary(dat.lm1) Call: lm(formula = sales ~ price, data = dat) Residuals: Min 1Q Median 3Q Max -55.719-19.270 4.212 16.143 73.454 Coefficients: Estimate Std. Error t value Pr(> t ) (Intercept) 237.1326
More informationk2 ( :35 ) ( k2) (GLM) web web 1 :
2012 11 01 k2 (2012-10-26 16:35 ) 1 6 2 (2012 11 01 k2) (GLM) kubo@ees.hokudai.ac.jp web http://goo.gl/wijx2 web http://goo.gl/ufq2 1 : 2 2 4 3 7 4 9 5 : 11 5.1................... 13 6 14 6.1......................
More informationH22 BioS t (i) treat1 treat2 data d1; input patno treat1 treat2; cards; ; run; 1 (i) treat = 1 treat =
H BioS t (i) treat treat data d; input patno treat treat; cards; 3 8 7 4 8 8 5 5 6 3 ; run; (i) treat treat data d; input group patno period treat y; label group patno period ; cards; 3 8 3 7 4 8 4 8 5
More information1 15 R Part : website:
1 15 R Part 4 2017 7 24 4 : website: email: http://www3.u-toyama.ac.jp/kkarato/ kkarato@eco.u-toyama.ac.jp 1 2 2 3 2.1............................... 3 2.2 2................................. 4 2.3................................
More information講義のーと : データ解析のための統計モデリング. 第3回
Title 講義のーと : データ解析のための統計モデリング Author(s) 久保, 拓弥 Issue Date 2008 Doc URL http://hdl.handle.net/2115/49477 Type learningobject Note この講義資料は, 著者のホームページ http://hosho.ees.hokudai.ac.jp/~kub ードできます Note(URL)http://hosho.ees.hokudai.ac.jp/~kubo/ce/EesLecture20
More information最小2乗法
2 2012 4 ( ) 2 2012 4 1 / 42 X Y Y = f (X ; Z) linear regression model X Y slope X 1 Y (X, Y ) 1 (X, Y ) ( ) 2 2012 4 2 / 42 1 β = β = β (4.2) = β 0 + β (4.3) ( ) 2 2012 4 3 / 42 = β 0 + β + (4.4) ( )
More information1 Tokyo Daily Rainfall (mm) Days (mm)
( ) r-taka@maritime.kobe-u.ac.jp 1 Tokyo Daily Rainfall (mm) 0 100 200 300 0 10000 20000 30000 40000 50000 Days (mm) 1876 1 1 2013 12 31 Tokyo, 1876 Daily Rainfall (mm) 0 50 100 150 0 100 200 300 Tokyo,
More information: (EQS) /EQUATIONS V1 = 30*V F1 + E1; V2 = 25*V *F1 + E2; V3 = 16*V *F1 + E3; V4 = 10*V F2 + E4; V5 = 19*V99
218 6 219 6.11: (EQS) /EQUATIONS V1 = 30*V999 + 1F1 + E1; V2 = 25*V999 +.54*F1 + E2; V3 = 16*V999 + 1.46*F1 + E3; V4 = 10*V999 + 1F2 + E4; V5 = 19*V999 + 1.29*F2 + E5; V6 = 17*V999 + 2.22*F2 + E6; CALIS.
More informationuntitled
2011/6/22 M2 1*1+2*2 79 2F Y YY 0.0 0.2 0.4 0.6 0.8 0.000 0.002 0.004 0.006 0.008 0.010 0.012 1.0 1.5 2.0 2.5 3.0 3.5 4.0 Y 0 50 100 150 200 250 YY A (Y = X + e A ) B (YY = X + e B ) X 0.00 0.05 0.10
More informationH22 BioS (i) I treat1 II treat2 data d1; input group patno treat1 treat2; cards; ; run; I
H BioS (i) I treat II treat data d; input group patno treat treat; cards; 8 7 4 8 8 5 5 6 ; run; I II sum data d; set d; sum treat + treat; run; sum proc gplot data d; plot sum * group ; symbol c black
More informationt sex N y y y Diff (1-2)
Armitage 1 1.1 2 t 1.2 SAS Proc GLM 2 2.1 1 1 2.1.1 50 1 1 t sex N y 50 116.45 119.6 122.75 11.071 1.5657 93.906 154.32 y 50 127.27 130.7 134.13 12.072 1.7073 102.68 163.37 y Diff (1-2) -15.7-11.1-6.504
More informationy = x x R = 0. 9, R = σ $ = y x w = x y x x w = x y α ε = + β + x x x y α ε = + β + γ x + x x x x' = / x y' = y/ x y' =
y x = α + β + ε =,, ε V( ε) = E( ε ) = σ α $ $ β w ( 0) σ = w σ σ y α x ε = + β + w w w w ε / w ( w y x α β ) = α$ $ W = yw βwxw $β = W ( W) ( W)( W) w x x w x x y y = = x W y W x y x y xw = y W = w w
More information研修コーナー
l l l l l l l l l l l α α β l µ l l l l l l l l l l l l l l l l l l l l l l l l l l l l l l l l l l l l l l l l l l l l l l l l l l l l l l l l l l l l l l l l l l l l l l l l l l l l l l
More informationrenshumondai-kaito.dvi
3 1 13 14 1.1 1 44.5 39.5 49.5 2 0.10 2 0.10 54.5 49.5 59.5 5 0.25 7 0.35 64.5 59.5 69.5 8 0.40 15 0.75 74.5 69.5 79.5 3 0.15 18 0.90 84.5 79.5 89.5 2 0.10 20 1.00 20 1.00 2 1.2 1 16.5 20.5 12.5 2 0.10
More informationI A A441 : April 15, 2013 Version : 1.1 I Kawahira, Tomoki TA (Shigehiro, Yoshida )
I013 00-1 : April 15, 013 Version : 1.1 I Kawahira, Tomoki TA (Shigehiro, Yoshida) http://www.math.nagoya-u.ac.jp/~kawahira/courses/13s-tenbou.html pdf * 4 15 4 5 13 e πi = 1 5 0 5 7 3 4 6 3 6 10 6 17
More information(τ τ ) τ, σ ( ) w = τ iσ, w = τ + iσ (w ) w, w ( ) τ, σ τ = (w + w), σ = i (w w) w, w w = τ w τ + σ w σ = τ + i σ w = τ w τ + σ w σ = τ i σ g ab w, w
S = 4π dτ dσ gg ij i X µ j X ν η µν η µν g ij g ij = g ij = ( 0 0 ) τ, σ (+, +) τ τ = iτ ds ds = dτ + dσ ds = dτ + dσ δ ij ( ) a =, a = τ b = σ g ij δ ab g g ( +, +,... ) S = 4π S = 4π ( i) = i 4π dτ dσ
More information2 H23 BioS (i) data d1; input group patno t sex censor; cards;
H BioS (i) data d1; input group patno t sex censor; cards; 0 1 0 0 0 0 1 0 1 1 0 4 4 0 1 0 5 5 1 1 0 6 5 1 1 0 7 10 1 0 0 8 15 0 1 0 9 15 0 1 0 10 4 1 0 0 11 4 1 0 1 1 5 1 0 1 1 7 0 1 1 14 8 1 0 1 15 8
More information第11回:線形回帰モデルのOLS推定
11 OLS 2018 7 13 1 / 45 1. 2. 3. 2 / 45 n 2 ((y 1, x 1 ), (y 2, x 2 ),, (y n, x n )) linear regression model y i = β 0 + β 1 x i + u i, E(u i x i ) = 0, E(u i u j x i ) = 0 (i j), V(u i x i ) = σ 2, i
More informationuntitled
WinLD R (16) WinLD https://www.biostat.wisc.edu/content/lan-demets-method-statistical-programs-clinical-trials WinLD.zip 2 2 1 α = 5% Type I error rate 1 5.0 % 2 9.8 % 3 14.3 % 5 22.6 % 10 40.1 % 3 Type
More informationGLM PROC GLM y = Xβ + ε y X β ε ε σ 2 E[ε] = 0 var[ε] = σ 2 I σ 2 0 σ 2 =... 0 σ 2 σ 2 I ε σ 2 y E[y] =Xβ var[y] =σ 2 I PROC GLM
PROC MIXED ( ) An Introdunction to PROC MIXED Junji Kishimoto SAS Institute Japan / Keio Univ. SFC / Univ. of Tokyo e-mail address: jpnjak@jpn.sas.com PROC MIXED PROC GLM PROC MIXED,,,, 1 1.1 PROC MIXED
More information,, Poisson 3 3. t t y,, y n Nµ, σ 2 y i µ + ɛ i ɛ i N0, σ 2 E[y i ] µ * i y i x i y i α + βx i + ɛ i ɛ i N0, σ 2, α, β *3 y i E[y i ] α + βx i
Armitage.? SAS.2 µ, µ 2, µ 3 a, a 2, a 3 a µ + a 2 µ 2 + a 3 µ 3 µ, µ 2, µ 3 µ, µ 2, µ 3 log a, a 2, a 3 a µ + a 2 µ 2 + a 3 µ 3 µ, µ 2, µ 3 * 2 2. y t y y y Poisson y * ,, Poisson 3 3. t t y,, y n Nµ,
More informationIsogai, T., Building a dynamic correlation network for fat-tailed financial asset returns, Applied Network Science (7):-24, 206,
H28. (TMU) 206 8 29 / 34 2 3 4 5 6 Isogai, T., Building a dynamic correlation network for fat-tailed financial asset returns, Applied Network Science (7):-24, 206, http://link.springer.com/article/0.007/s409-06-0008-x
More informationchap9.dvi
9 AR (i) (ii) MA (iii) (iv) (v) 9.1 2 1 AR 1 9.1.1 S S y j = (α i + β i j) D ij + η j, η j = ρ S η j S + ε j (j =1,,T) (1) i=1 {ε j } i.i.d(,σ 2 ) η j (j ) D ij j i S 1 S =1 D ij =1 S>1 S =4 (1) y j =
More information5 Armitage x 1,, x n y i = 10x i + 3 y i = log x i {x i } {y i } 1.2 n i i x ij i j y ij, z ij i j 2 1 y = a x + b ( cm) x ij (i j )
5 Armitage. x,, x n y i = 0x i + 3 y i = log x i x i y i.2 n i i x ij i j y ij, z ij i j 2 y = a x + b 2 2. ( cm) x ij (i j ) (i) x, x 2 σ 2 x,, σ 2 x,2 σ x,, σ x,2 t t x * (ii) (i) m y ij = x ij /00 y
More information.3 ˆβ1 = S, S ˆβ0 = ȳ ˆβ1 S = (β0 + β1i i) β0 β1 S = (i β0 β1i) = 0 β0 S = (i β0 β1i)i = 0 β1 β0, β1 ȳ β0 β1 = 0, (i ȳ β1(i ))i = 0 {(i ȳ)(i ) β1(i ))
Copright (c) 004,005 Hidetoshi Shimodaira 1.. 3. 4. 004-10-01 16:15:07 shimo cat(" 1: "); c(mea(), mea()) cat(" : "); mmea
More informationII 2 II
II 2 II 2005 yugami@cc.utsunomiya-u.ac.jp 2005 4 1 1 2 5 2.1.................................... 5 2.2................................. 6 2.3............................. 6 2.4.................................
More information4.9 Hausman Test Time Fixed Effects Model vs Time Random Effects Model Two-way Fixed Effects Model
1 EViews 5 2007 7 11 2010 5 17 1 ( ) 3 1.1........................................... 4 1.2................................... 9 2 11 3 14 3.1 Pooled OLS.............................................. 14
More informations = 1.15 (s = 1.07), R = 0.786, R = 0.679, DW =.03 5 Y = 0.3 (0.095) (.708) X, R = 0.786, R = 0.679, s = 1.07, DW =.03, t û Y = 0.3 (3.163) + 0
7 DW 7.1 DW u 1, u,, u (DW ) u u 1 = u 1, u,, u + + + - - - - + + - - - + + u 1, u,, u + - + - + - + - + u 1, u,, u u 1, u,, u u +1 = u 1, u,, u Y = α + βx + u, u = ρu 1 + ɛ, H 0 : ρ = 0, H 1 : ρ 0 ɛ 1,
More informationkubostat2018d p.2 :? bod size x and fertilization f change seed number? : a statistical model for this example? i response variable seed number : { i
kubostat2018d p.1 I 2018 (d) model selection and kubo@ees.hokudai.ac.jp http://goo.gl/76c4i 2018 06 25 : 2018 06 21 17:45 1 2 3 4 :? AIC : deviance model selection misunderstanding kubostat2018d (http://goo.gl/76c4i)
More information第13回:交差項を含む回帰・弾力性の推定
13 2018 7 27 1 / 31 1. 2. 2 / 31 y i = β 0 + β X x i + β Z z i + β XZ x i z i + u i, E(u i x i, z i ) = 0, E(u i u j x i, z i ) = 0 (i j), V(u i x i, z i ) = σ 2, i = 1, 2,, n x i z i 1 3 / 31 y i = β
More informationインターネットを活用した経済分析 - フリーソフト Rを使おう
R 1 1 1 2017 2 15 2017 2 15 1/64 2 R 3 R R RESAS 2017 2 15 2/64 2 R 3 R R RESAS 2017 2 15 3/64 2-4 ( ) ( (80%) (20%) 2017 2 15 4/64 PC LAN R 2017 2 15 5/64 R R 2017 2 15 6/64 3-4 R 15 + 2017 2 15 7/64
More informationkubostat2015e p.2 how to specify Poisson regression model, a GLM GLM how to specify model, a GLM GLM logistic probability distribution Poisson distrib
kubostat2015e p.1 I 2015 (e) GLM kubo@ees.hokudai.ac.jp http://goo.gl/76c4i 2015 07 22 2015 07 21 16:26 kubostat2015e (http://goo.gl/76c4i) 2015 (e) 2015 07 22 1 / 42 1 N k 2 binomial distribution logit
More informationα β *2 α α β β α = α 1 β = 1 β 2.2 α 0 β *3 2.3 * *2 *3 *4 (µ A ) (µ P ) (µ A > µ P ) 10 (µ A = µ P + 10) 15 (µ A = µ P +
Armitage 1 1.1 2 t *1 α β 1.2 µ x µ 2 2 2 α β 2.1 1 α β α ( ) β *1 t t 1 α β *2 α α β β α = α 1 β = 1 β 2.2 α 0 β 1 0 0 1 1 5 2.5 *3 2.3 *4 3 3.1 1 1 1 *2 *3 *4 (µ A ) (µ P ) (µ A > µ P ) 10 (µ A = µ P
More informationkubostat2017e p.1 I 2017 (e) GLM logistic regression : : :02 1 N y count data or
kubostat207e p. I 207 (e) GLM kubo@ees.hokudai.ac.jp https://goo.gl/z9ycjy 207 4 207 6:02 N y 2 binomial distribution logit link function 3 4! offset kubostat207e (https://goo.gl/z9ycjy) 207 (e) 207 4
More informationJMP V4 による生存時間分析
V4 1 SAS 2000.11.18 4 ( ) (Survival Time) 1 (Event) Start of Study Start of Observation Died Died Died Lost End Time Censor Died Died Censor Died Time Start of Study End Start of Observation Censor
More information一般化線形 (混合) モデル (2) - ロジスティック回帰と GLMM
.. ( ) (2) GLMM kubo@ees.hokudai.ac.jp I http://goo.gl/rrhzey 2013 08 27 : 2013 08 27 08:29 kubostat2013ou2 (http://goo.gl/rrhzey) ( ) (2) 2013 08 27 1 / 74 I.1 N k.2 binomial distribution logit link function.3.4!
More informationUse R
Use R! 2008/05/23( ) Index Introduction (GLM) ( ) R. Introduction R,, PLS,,, etc. 2. Correlation coefficient (Pearson s product moment correlation) r = Sxy Sxx Syy :, Sxy, Sxx= X, Syy Y 1.96 95% R cor(x,
More informationσ t σ t σt nikkei HP nikkei4csv H R nikkei4<-readcsv("h:=y=ynikkei4csv",header=t) (1) nikkei header=t nikkei4csv 4 4 nikkei nikkei4<-dataframe(n
R 1 R R R tseries fseries 1 tseries fseries R Japan(Tokyo) R library(tseries) library(fseries) 2 t r t t 1 Ω t 1 E[r t Ω t 1 ] ɛ t r t = E[r t Ω t 1 ] + ɛ t ɛ t 2 iid (independently, identically distributed)
More informationst.dvi
9 3 5................................... 5............................. 5....................................... 5.................................. 7.........................................................................
More information2 / 39
W707 s-taiji@is.titech.ac.jp 1 / 39 2 / 39 1 2 3 3 / 39 q f (x; α) = α j B j (x). j=1 min α R n+2 n ( d (Y i f (X i ; α)) 2 2 ) 2 f (x; α) + λ dx 2 dx. i=1 f B j 4 / 39 : q f (x) = α j B j (x). j=1 : x
More information10
z c j = N 1 N t= j1 [ ( z t z ) ( )] z t j z q 2 1 2 r j /N j=1 1/ N J Q = N(N 2) 1 N j j=1 r j 2 2 χ J B d z t = z t d (1 B) 2 z t = (z t z t 1 ) (z t 1 z t 2 ) (1 B s )z t = z t z t s _ARIMA CONSUME
More information4 Mindlin -Reissner 4 δ T T T εσdω= δ ubdω+ δ utd Γ Ω Ω Γ T εσ (1.1) ε σ u b t 3 σ ε. u T T T = = = { σx σ y σ z τxy τ yz τzx} { εx εy εz γ xy γ yz γ
Mindlin -Rissnr δ εσd δ ubd+ δ utd Γ Γ εσ (.) ε σ u b t σ ε. u { σ σ σ z τ τ z τz} { ε ε εz γ γ z γ z} { u u uz} { b b bz} b t { t t tz}. ε u u u u z u u u z u u z ε + + + (.) z z z (.) u u NU (.) N U
More information変 位 変位とは 物体中のある点が変形後に 別の点に異動したときの位置の変化で あり ベクトル量である 変位には 物体の変形の他に剛体運動 剛体変位 が含まれている 剛体変位 P(x, y, z) 平行移動と回転 P! (x + u, y + v, z + w) Q(x + d x, y + dy,
変 位 変位とは 物体中のある点が変形後に 別の点に異動したときの位置の変化で あり ベクトル量である 変位には 物体の変形の他に剛体運動 剛体変位 が含まれている 剛体変位 P(x, y, z) 平行移動と回転 P! (x + u, y + v, z + w) Q(x + d x, y + dy, z + dz) Q! (x + d x + u + du, y + dy + v + dv, z +
More information基礎数学I
I & II ii ii........... 22................. 25 12............... 28.................. 28.................... 31............. 32.................. 34 3 1 9.................... 1....................... 1............
More informationkubostat2017c p (c) Poisson regression, a generalized linear model (GLM) : :
kubostat2017c p.1 2017 (c), a generalized linear model (GLM) : kubo@ees.hokudai.ac.jp http://goo.gl/76c4i 2017 11 14 : 2017 11 07 15:43 kubostat2017c (http://goo.gl/76c4i) 2017 (c) 2017 11 14 1 / 47 agenda
More informationO1-1 O1-2 O1-3 O1-4 O1-5 O1-6
O1-1 O1-2 O1-3 O1-4 O1-5 O1-6 O1-7 O1-8 O1-9 O1-10 O1-11 O1-12 O1-13 O1-14 O1-15 O1-16 O1-17 O1-18 O1-19 O1-20 O1-21 O1-22 O1-23 O1-24 O1-25 O1-26 O1-27 O1-28 O1-29 O1-30 O1-31 O1-32 O1-33 O1-34 O1-35
More information1 911 9001030 9:00 A B C D E F G H I J K L M 1A0900 1B0900 1C0900 1D0900 1E0900 1F0900 1G0900 1H0900 1I0900 1J0900 1K0900 1L0900 1M0900 9:15 1A0915 1B0915 1C0915 1D0915 1E0915 1F0915 1G0915 1H0915 1I0915
More information,,..,. 1
016 9 3 6 0 016 1 0 1 10 1 1 17 1..,,..,. 1 1 c = h = G = ε 0 = 1. 1.1 L L T V 1.1. T, V. d dt L q i L q i = 0 1.. q i t L q i, q i, t L ϕ, ϕ, x µ x µ 1.3. ϕ x µ, L. S, L, L S = Ld 4 x 1.4 = Ld 3 xdt 1.5
More information1 (1) () (3) I 0 3 I I d θ = L () dt θ L L θ I d θ = L = κθ (3) dt κ T I T = π κ (4) T I κ κ κ L l a θ L r δr δl L θ ϕ ϕ = rθ (5) l
1 1 ϕ ϕ ϕ S F F = ϕ (1) S 1: F 1 1 (1) () (3) I 0 3 I I d θ = L () dt θ L L θ I d θ = L = κθ (3) dt κ T I T = π κ (4) T I κ κ κ L l a θ L r δr δl L θ ϕ ϕ = rθ (5) l : l r δr θ πrδr δf (1) (5) δf = ϕ πrδr
More information通信容量制約を考慮したフィードバック制御 - 電子情報通信学会 情報理論研究会(IT) 若手研究者のための講演会
IT 1 2 1 2 27 11 24 15:20 16:05 ( ) 27 11 24 1 / 49 1 1940 Witsenhausen 2 3 ( ) 27 11 24 2 / 49 1940 2 gun director Warren Weaver, NDRC (National Defence Research Committee) Final report D-2 project #2,
More informationchap10.dvi
. q {y j } I( ( L y j =Δy j = u j = C l ε j l = C(L ε j, {ε j } i.i.d.(,i q ( l= y O p ( {u j } q {C l } A l C l
More information第86回日本感染症学会総会学術集会後抄録(I)
κ κ κ κ κ κ μ μ β β β γ α α β β γ α β α α α γ α β β γ μ β β μ μ α ββ β β β β β β β β β β β β β β β β β β γ β μ μ μ μμ μ μ μ μ β β μ μ μ μ μ μ μ μ μ μ μ μ μ μ β
More informationarxiv: v1(astro-ph.co)
arxiv:1311.0281v1(astro-ph.co) R µν 1 2 Rg µν + Λg µν = 8πG c 4 T µν Λ f(r) R f(r) Galileon φ(t) Massive Gravity etc... Action S = d 4 x g (L GG + L m ) L GG = K(φ,X) G 3 (φ,x)φ + G 4 (φ,x)r + G 4X (φ)
More information% 10%, 35%( 1029 ) p (a) 1 p 95% (b) 1 Std. Err. (c) p 40% 5% (d) p 1: STATA (1). prtesti One-sample test of pr
1 1. 2014 6 2014 6 10 10% 10%, 35%( 1029 ) p (a) 1 p 95% (b) 1 Std. Err. (c) p 40% 5% (d) p 1: STATA (1). prtesti 1029 0.35 0.40 One-sample test of proportion x: Number of obs = 1029 Variable Mean Std.
More informationuntitled
17 5 13 1 2 1.1... 2 1.2... 2 1.3... 3 2 3 2.1... 3 2.2... 5 3 6 3.1... 6 3.2... 7 3.3 t... 7 3.4 BC a... 9 3.5... 10 4 11 1 1 θ n ˆθ. ˆθ, ˆθ, ˆθ.,, ˆθ.,.,,,. 1.1 ˆθ σ 2 = E(ˆθ E ˆθ) 2 b = E(ˆθ θ). Y 1,,Y
More information『共形場理論』
T (z) SL(2, C) T (z) SU(2) S 1 /Z 2 SU(2) (ŜU(2) k ŜU(2) 1)/ŜU(2) k+1 ŜU(2)/Û(1) G H N =1 N =1 N =1 N =1 N =2 N =2 N =2 N =2 ĉ>1 N =2 N =2 N =4 N =4 1 2 2 z=x 1 +ix 2 z f(z) f(z) 1 1 4 4 N =4 1 = = 1.3
More information「スウェーデン企業におけるワーク・ライフ・バランス調査 」報告書
1 2004 12 2005 4 5 100 25 3 1 76 2 Demoskop 2 2004 11 24 30 7 2 10 1 2005 1 31 2 4 5 2 3-1-1 3-1-1 Micromediabanken 2005 1 507 1000 55.0 2 77 50 50 /CEO 36.3 37.4 18.1 3-2-1 43.0 34.4 / 17.6 3-2-2 78 79.4
More information80 X 1, X 2,, X n ( λ ) λ P(X = x) = f (x; λ) = λx e λ, x = 0, 1, 2, x! l(λ) = n f (x i ; λ) = i=1 i=1 n λ x i e λ i=1 x i! = λ n i=1 x i e nλ n i=1 x
80 X 1, X 2,, X n ( λ ) λ P(X = x) = f (x; λ) = λx e λ, x = 0, 1, 2, x! l(λ) = n f (x i ; λ) = n λ x i e λ x i! = λ n x i e nλ n x i! n n log l(λ) = log(λ) x i nλ log( x i!) log l(λ) λ = 1 λ n x i n =
More information医系の統計入門第 2 版 サンプルページ この本の定価 判型などは, 以下の URL からご覧いただけます. このサンプルページの内容は, 第 2 版 1 刷発行時のものです.
医系の統計入門第 2 版 サンプルページ この本の定価 判型などは, 以下の URL からご覧いただけます. http://www.morikita.co.jp/books/mid/009192 このサンプルページの内容は, 第 2 版 1 刷発行時のものです. i 2 t 1. 2. 3 2 3. 6 4. 7 5. n 2 ν 6. 2 7. 2003 ii 2 2013 10 iii 1987
More information研究シリーズ第40号
165 PEN WPI CPI WAGE IIP Feige and Pearce 166 167 168 169 Vector Autoregression n (z) z z p p p zt = φ1zt 1 + φ2zt 2 + + φ pzt p + t Cov( 0 ε t, ε t j )= Σ for for j 0 j = 0 Cov( ε t, zt j ) = 0 j = >
More informationMicrosoft Word - 表紙.docx
黒住英司 [ 著 ] サピエンティア 計量経済学 訂正および練習問題解答 (206/2/2 版 ) 訂正 練習問題解答 3 .69, 3.8 4 (X i X)U i i i (X i μ x )U i ( X μx ) U i. i E [ ] (X i μ x )U i i E[(X i μ x )]E[U i ]0. i V [ ] (X i μ x )U i i 2 i j E [(X i
More informationR R 16 ( 3 )
(017 ) 9 4 7 ( ) ( 3 ) ( 010 ) 1 (P3) 1 11 (P4) 1 1 (P4) 1 (P15) 1 (P16) (P0) 3 (P18) 3 4 (P3) 4 3 4 31 1 5 3 5 4 6 5 9 51 9 5 9 6 9 61 9 6 α β 9 63 û 11 64 R 1 65 13 66 14 7 14 71 15 7 R R 16 http://wwwecoosaka-uacjp/~tazak/class/017
More informationV(x) m e V 0 cos x π x π V(x) = x < π, x > π V 0 (i) x = 0 (V(x) V 0 (1 x 2 /2)) n n d 2 f dξ 2ξ d f 2 dξ + 2n f = 0 H n (ξ) (ii) H
199 1 1 199 1 1. Vx) m e V cos x π x π Vx) = x < π, x > π V i) x = Vx) V 1 x /)) n n d f dξ ξ d f dξ + n f = H n ξ) ii) H n ξ) = 1) n expξ ) dn dξ n exp ξ )) H n ξ)h m ξ) exp ξ )dξ = π n n!δ n,m x = Vx)
More information総合薬学講座 生物統計の基礎
2013 10 22 ( ) 2013 10 22 1 / 40 p.682 1. 2. 3 2 t Mann Whitney U ). 4 χ 2. 5. 6 Dunnett Tukey. 7. 8 Kaplan Meier.. U. ( ) 2013 10 22 2 / 40 1 93 ( 20 ) 230. a t b c χ 2 d 1.0 +1.0 e, b ( ) e ( ) ( ) 2013
More information10:30 12:00 P.G. vs vs vs 2
1 10:30 12:00 P.G. vs vs vs 2 LOGIT PROBIT TOBIT mean median mode CV 3 4 5 0.5 1000 6 45 7 P(A B) = P(A) + P(B) - P(A B) P(B A)=P(A B)/P(A) P(A B)=P(B A) P(A) P(A B) P(A) P(B A) P(B) P(A B) P(A) P(B) P(B
More information( 30 ) 30 4 5 1 4 1.1............................................... 4 1.............................................. 4 1..1.................................. 4 1.......................................
More informationVol. 36, Special Issue, S 3 S 18 (2015) PK Phase I Introduction to Pharmacokinetic Analysis Focus on Phase I Study 1 2 Kazuro Ikawa 1 and Jun Tanaka 2
Vol. 36, Special Issue, S 3 S 18 (2015) PK Phase I Introduction to Pharmacokinetic Analysis Focus on Phase I Study 1 2 Kazuro Ikawa 1 and Jun Tanaka 2 1 2 1 Department of Clinical Pharmacotherapy, Hiroshima
More informationStata11 whitepapers mwp-037 regress - regress regress. regress mpg weight foreign Source SS df MS Number of obs = 74 F(
mwp-037 regress - regress 1. 1.1 1.2 1.3 2. 3. 4. 5. 1. regress. regress mpg weight foreign Source SS df MS Number of obs = 74 F( 2, 71) = 69.75 Model 1619.2877 2 809.643849 Prob > F = 0.0000 Residual
More information1.2 R R Windows, Macintosh, Linux(Unix) Windows Mac R Linux redhat, debian, vinelinux ( ) RjpWiki ( RjpWiki Wiki
R 2005 9 12 ( ) 1 R 1.1 R R R S-PLUS( ) S version 4( ) S (AT&T Richard A. Becker, John M. Chambers, and Allan R. Wilks ) S S R R S ( ) S GUI( ) ( ) R R R R http://stat.sm.u-tokai.ac.jp/ yama/r/ R yamamoto@sm.u-tokai.ac.jp
More informationsolutionJIS.dvi
May 0, 006 6 morimune@econ.kyoto-u.ac.jp /9/005 (7 0/5/006 1 1.1 (a) (b) (c) c + c + + c = nc (x 1 x)+(x x)+ +(x n x) =(x 1 + x + + x n ) nx = nx nx =0 c(x 1 x)+c(x x)+ + c(x n x) =c (x i x) =0 y i (x
More informationohpmain.dvi
fujisawa@ism.ac.jp 1 Contents 1. 2. 3. 4. γ- 2 1. 3 10 5.6, 5.7, 5.4, 5.5, 5.8, 5.5, 5.3, 5.6, 5.4, 5.2. 5.5 5.6 +5.7 +5.4 +5.5 +5.8 +5.5 +5.3 +5.6 +5.4 +5.2 =5.5. 10 outlier 5 5.6, 5.7, 5.4, 5.5, 5.8,
More informationDVIOUT-ar
1 4 μ=0, σ=1 5 μ=2, σ=1 5 μ=0, σ=2 3 2 1 0-1 -2-3 0 10 20 30 40 50 60 70 80 90 4 3 2 1 0-1 0 10 20 30 40 50 60 70 80 90 4 3 2 1 0-1 -2-3 -4-5 0 10 20 30 40 50 60 70 80 90 8 μ=2, σ=2 5 μ=1, θ 1 =0.5, σ=1
More informationPart () () Γ Part ,
Contents a 6 6 6 6 6 6 6 7 7. 8.. 8.. 8.3. 8 Part. 9. 9.. 9.. 3. 3.. 3.. 3 4. 5 4.. 5 4.. 9 4.3. 3 Part. 6 5. () 6 5.. () 7 5.. 9 5.3. Γ 3 6. 3 6.. 3 6.. 3 6.3. 33 Part 3. 34 7. 34 7.. 34 7.. 34 8. 35
More informationN cos s s cos ψ e e e e 3 3 e e 3 e 3 e
3 3 5 5 5 3 3 7 5 33 5 33 9 5 8 > e > f U f U u u > u ue u e u ue u ue u e u e u u e u u e u N cos s s cos ψ e e e e 3 3 e e 3 e 3 e 3 > A A > A E A f A A f A [ ] f A A e > > A e[ ] > f A E A < < f ; >
More information( ) Note (e ) (µ ) (τ ) ( (ν e,e ) e- (ν µ, µ ) µ- (ν τ,τ ) τ- ) ( ) ( ) (SU(2) ) (W +,Z 0,W ) * 1) 3 * 2) [ ] [ ] [ ] ν e ν µ ν τ e
( ) Note 3 19 12 13 8 8.1 (e ) (µ ) (τ ) ( (ν e,e ) e- (ν µ, µ ) µ- (ν τ,τ ) τ- ) ( ) ( ) (SU(2) ) (W +,Z 0,W ) * 1) 3 * 2) [ ] [ ] [ ] ν e ν µ ν τ e µ τ, e R, µ R, τ R (1a) L ( ) ) * 3) W Z 1/2 ( - )
More information鉄鋼協会プレゼン
NN :~:, 8 Nov., Adaptive H Control for Linear Slider with Friction Compensation positioning mechanism moving table stand manipulator Point to Point Control [G] Continuous Path Control ground Fig. Positoining
More informationuntitled
IT (1, horiike@ml.me.titech.ac.jp) (1, jun-jun@ms.kagu.tus.ac.jp) 1. 1-1 19802000 2000ITIT IT IT TOPIX (%) 1TOPIX 2 1-2. 80 80 ( ) 2004/11/26 S-PLUS 2 1-3. IT IT IT IT 2. 2-1. a. b. (Size) c. B/M(Book
More informationO x y z O ( O ) O (O ) 3 x y z O O x v t = t = 0 ( 1 ) O t = 0 c t r = ct P (x, y, z) r 2 = x 2 + y 2 + z 2 (t, x, y, z) (ct) 2 x 2 y 2 z 2 = 0
9 O y O ( O ) O (O ) 3 y O O v t = t = 0 ( ) O t = 0 t r = t P (, y, ) r = + y + (t,, y, ) (t) y = 0 () ( )O O t (t ) y = 0 () (t) y = (t ) y = 0 (3) O O v O O v O O O y y O O v P(, y,, t) t (, y,, t )
More information2 1 1 α = a + bi(a, b R) α (conjugate) α = a bi α (absolute value) α = a 2 + b 2 α (norm) N(α) = a 2 + b 2 = αα = α 2 α (spure) (trace) 1 1. a R aα =
1 1 α = a + bi(a, b R) α (conjugate) α = a bi α (absolute value) α = a + b α (norm) N(α) = a + b = αα = α α (spure) (trace) 1 1. a R aα = aα. α = α 3. α + β = α + β 4. αβ = αβ 5. β 0 6. α = α ( ) α = α
More information2 G(k) e ikx = (ik) n x n n! n=0 (k ) ( ) X n = ( i) n n k n G(k) k=0 F (k) ln G(k) = ln e ikx n κ n F (k) = F (k) (ik) n n= n! κ n κ n = ( i) n n k n
. X {x, x 2, x 3,... x n } X X {, 2, 3, 4, 5, 6} X x i P i. 0 P i 2. n P i = 3. P (i ω) = i ω P i P 3 {x, x 2, x 3,... x n } ω P i = 6 X f(x) f(x) X n n f(x i )P i n x n i P i X n 2 G(k) e ikx = (ik) n
More informationI L01( Wed) : Time-stamp: Wed 07:38 JST hig e, ( ) L01 I(2017) 1 / 19
I L01(2017-09-20 Wed) : Time-stamp: 2017-09-20 Wed 07:38 JST hig e, http://hig3.net ( ) L01 I(2017) 1 / 19 ? 1? 2? ( ) L01 I(2017) 2 / 19 ?,,.,., 1..,. 1,2,.,.,. ( ) L01 I(2017) 3 / 19 ? I. M (3 ) II,
More informationR = Ar l B r l. A, B A, B.. r 2 R r = r2 [lar r l B r l2 ]=larl l B r l.2 r 2 R = [lar l l Br ] r r r = ll Ar l ll B = ll R rl.3 sin θ Θ = ll.4 Θsinθ
.3.2 3.3.2 Spherical Coorinates.5: Laplace 2 V = r 2 r 2 x = r cos φ sin θ, y = r sin φ sin θ, z = r cos θ.93 r 2 sin θ sin θ θ θ r 2 sin 2 θ 2 V =.94 2.94 z V φ Laplace r 2 r 2 r 2 sin θ.96.95 V r 2 R
More information