Peyton pop Std T parameter santa parameter€¦ · Peyton: pep = population mean, 6 = pop. Std....
Transcript of Peyton pop Std T parameter santa parameter€¦ · Peyton: pep = population mean, 6 = pop. Std....
1
STAT 400 UIUC 6.4 - Maximum Likelihood Estimation,
Method of Moments Stepanov
Dalpiaz Nguyen
p.m.f. or p.d.f. f ( x ; q ), q Î W. W – parameter space. Example 1: Suppose W = { 1, 2, 3 } and the p.d.f. f ( x ; q ) is q = 1: f ( 1 ; 1 ) = 0.6, f ( 2 ; 1 ) = 0.1, f ( 3 ; 1 ) = 0.1, f ( 4 ; 1 ) = 0.2.
q = 2: f ( 1 ; 2 ) = 0.2, f ( 2 ; 2 ) = 0.3, f ( 3 ; 2 ) = 0.3, f ( 4 ; 2 ) = 0.2.
q = 3: f ( 1 ; 3 ) = 0.3, f ( 2 ; 3 ) = 0.4, f ( 3 ; 3 ) = 0.2, f ( 4 ; 3 ) = 0.1. What is the maximum likelihood estimate of q ( based on only one observation of X ) if … a) X = 1; b) X = 2; c) X = 3; d) X = 4.
Peyton : pep= population mean , 6 = pop .
Std.
T
parameter parameter
(santa. '¥÷:* mean,
"
iii.us.#> Iopredation is normally distributed .
N ( µ , 6)T t
⇒ Use sample data to estimate pi, 6. parameters of thea-what we want to estimate distribution
if -0=1 , then
I@tweeps's hat
x-- 4 is 0.2.
probabilityto estimate
of(x -- l; f =D = O.G ← I = I f (x- 2 ; -0=1) -- O. I
f (x - l ; 0=2) = 0.2 # f ( x=L; 0=2) = 0.3
f ( x- l ; 0=3) = 0.3 f- ( x=L; f -- 3) = O. y ← I =3
f (x=3; ⑦ =D = O.I
-
f (x -- 4; f -- l) = 0.2f (x=3; 0=2) - O. 3 ← I = 2 } ← I = I or 2f ( x=3; 8=3) = O. 2
f ( x = 4; f -- 2) = 0.2
f- ( x = 4; f =3) = O. I
* Note Maximum likelihood estimate may not be unique .
( ML E)
2
Likelihood function:
L ( q ) = L ( q ; x 1 , x 2 , … , x n ) = f ( x i ; q ) = f ( x 1 ; q ) × … × f ( x n ; q )
It is often easier to consider ln L ( q ) = ln f ( x i ; q ).
Maximum Likelihood Estimator: = arg max L ( q ) = arg max ln L ( q ). Method of Moments: E ( X ) = g ( q ). Set = g ( ). Solve for . Example 0: Consider a single observation X of a Binomial random variable with n trials and probability of “success” p. That is,
, k = 0, 1, … , n. a) Obtain the method of moments estimator of p, . b) Obtain the maximum likelihood estimator of p, .
Õ=
n
i 1
å=
n
i 1
θ̂
X θ~ θ~
knk ppkCnk --== 1 XP )(
)(
p~
p̂
( MLE)sample data ( n observations)-
Tparameter to be estimated
Tnatural log
estimates .P Idea: E (X) = I( Mom) t -
g CE) = I
population moment = sample moment
X - Binom ( n, p) astfwme n is known
Population moment Sample momentF- CX) = np I = X
so, rip = x ⇒F
Likelihood function :L ( p) = L ( p ; X) -- f ( X; p) = nc×p× ( I- p )
"-X
Elp) = In L ( p ) = lnlncxltxlnlpt In- X) ln ( I - p)
optdecp) = Ip - np = X-XP-nptXP-axp-n.PE Etop CI
-
p)
⇒p-.
d.a
check 2nd derivative:#
dpz-llp7-inplt-PJ-npllll-p7-pygopr.CI-
p)'
3
Example 2: Let X1 , X2 , … , X n be a random sample of size n from a Poisson distribution with mean l, l > 0. That is,
P ( X = k ) = , k = 0, 1, 2, 3, … .
a) Obtain the method of moments estimator of l, .
b) Obtain the maximum likelihood estimator of l, .
!λ
λ
kek -
λ~
l̂
-
unknown=
known f=
①← pmf of Poisson partmeter of
Poisson
Population:sampleth-ment.EC/7--④ I = E. Xi
⇒ I -- I ⇒=
does not have id
LCH -
- iitfcxisi)=T*e"
e-in .IT ÷
ICX -- Xi ;D)i'¥
=
lnlab) -- blnla) t=axle- X XX - e- d
. . . .
Ine- d-- -
incl) = O Poisson Cd) X , !'
Xz ! Xn !
lnfab) - lnlaltlnlb)= e-dndh.E.xi.nlIn (F) = Inca) - lncb) TIX ; !
Ince) = I i -- i
Nd)=lnLCN= - inkle) t.E.pl/ilnd-lniIIXi ! )= - in t Ii
,
Xi Ind - II. In ( Xi ! )
¥ecN= - nt ?÷ Eto ⇒ I=iEfi
4
Example 3: Let X 1 , X 2 , … , X n be a random sample of size n from a Geometric distribution with probability of “success” p, 0 < p < 1. That is, P ( X = k ) = ( 1 – p ) k – 1 p, k = 1, 2, 3, … . a) Obtain the method of moments estimator of p, .
b) Obtain the maximum likelihood estimator of p, .
p~
p̂
:ftp.Mor-nent : S#t :
Efx) = IF I = III⇒ feet I ⇒
"
Llp) = IT f ( Xi sp) = ¥1 ( i - p)"- ' pIC X -- Xi )r
= ( I - p )" - l
p. ( I - p)"- '
p. . . ( I -p)×n
- '
pGeom (p)
= ph ( i - p ) Ei, Xi-
n
f. ( p) = In Llp) = nlnlp) t ( FE,Xi - n) ln
#elp) -- F t C -D= F - E;YipI=nCtp)-tExinp ( I - p)
n - PEIXi - O= to
⇒ n - ri E. xi=o⇒p=Exi
5
Example 4: Let X 1 , X 2 , … , X n be a random sample of size n from the distribution with probability density function
f ( x ; q ) =
0 < q < ¥.
a) Obtain the method of moments estimator of q, .
Method of Moments: E ( X ) = g ( q ). Set = g ( ). Solve for . b) Obtain the maximum likelihood estimator of q, .
Likelihood function:
L ( q ) = L ( q ; x 1 , x 2 , … , x n ) = f ( x i ; q ) = f ( x 1 ; q ) × … × f ( x n ; q )
Maximum Likelihood Estimator: = arg max L ( q ) = arg max ln L ( q ).
ïïî
ïïí
ì -
££×
otherwise0
10θ1
θ θ1
xx
θ~
X θ~ θ~
θ̂
Õ=
n
i 1
θ̂
continuous
ftp.#ent : E (x) -- f! x - tf x'
dx -- tf fo"
x't
d× = to fix % dx=¥l÷÷÷l : I ⇐ ÷.S#ment : F ⇒ If = I ⇒ E=¥-i=t x
Lee ) = II fix is e) = II. et Xi'
= Ix ,'¥
. I x.'
. . . ¥xn¥= In I÷Xi¥ - ' inch - uh =
- in Co)
eco) = in Hot = nln (to) t in ( II Xi't ') = -nonce) t.E.in ( Xi't
'
)= - nine I - I ) ln (Xi ) = -mln E t ( to - I) Ezln (Xi)
#eco- I ⇐ -F -Eihf Eto ⇒ E=-IiEw x
6
c) Suppose n = 3, and x 1 = 0.2, x 2 = 0.3, x 3 = 0.5. Compute the values of the method of moments estimate and the maximum likelihood estimate for q. Example 5: Let X 1 , X 2 , … , X n be a random sample of size n from N ( q 1 , q 2 ), where
W = { ( q 1 , q 2 ) : – ¥ < q 1 < ¥, 0 < q 2 < ¥ }. That is, here we let q1 = µ and q2 = s2 . a) Obtain the maximum likelihood estimator of q 1 , , and of q 2 , .
b) Obtain the method of moments estimator of q 1 , , and of q 2 , .
1 θ̂ 2 θ̂
1 θ~
2 θ~
X = XltXzgtX3 = 0.2+0.33+-0.5 = ÷I.
'
I= - I[ ln (O. 2) t Cn (O. 3) t In (0.5)) €1.16890
% a"
Likelihood function :Pdf of Normal Co , .az ,
HG . a) = II. this G. ed = exp f-H]tex -- expend =f!⇒ )!It expf-lxijo.FI)
h
=H⇒) e-'
e
-¥¥". . . .
e-":*
.
→
=÷.sn#.e.E.-cxiiEiI=q.o..jnh.e-Eo.Eicxi-a5ICE.. Ez) = In L CQ . Ez) = -Z ln (2nA) -2¥77, ( Xi - G)
-
ln (e)
= - Eln (2nA) - If.
IF, ( Xi - fi )'
¥,
elf.. a) = - Izz ¥,
2 ( Xi - G) C- D=# II. ( Xi - fi)
⇐ eco-i.az) = - 2¥,
Ldn) t# ÷zCxi - ED'n
= -
Iot # Ei, Hi - -0,5set # eco
. .= o ⇒ i¥¥=o⇒÷icxi -G) - o
⇐ II. Xi - no , -- o ⇐o*
set # eco , .es -
- o ⇒ - Io.
+E7o⇒I¥¥iIo205 2-05
⇒- n + Eat:O ⇒ oI=÷E"→ this is not
the samplevariance
(b) Mom Xi . . . . . Xn N CQ , QD
Population :samplemo-ment.ECX) = f ,← first I ← first sample moment
2nd → ECX'
) = Var ( x) t# (XD- XT = ht Eax:
= Gz t -0T
⇒ s :÷÷: ⇐ *⇒H÷÷÷÷÷i*