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AM216StochasticDifferentialEquationsLecture06
CopyrightbyHongyunWang,UCSC
Listoftopicsinthislecture
• LongroadtoconcludingdW/dtisawhitenoise:Energyspectrumdensity(ESD),powerspectrumdensity(PSD);
Stationarystochasticprocess,auto-correlationfunctionR(t);Wiener-Khinchintheorem(PSDisFouriertransformofR(t));
dW/dthasauniformPSD(definitionofwhitenoise).
• ConstrainedWienerprocess,BayesTheorem
RecapTheshortstoryofwhitenoise:
1)Z(t)≡ dW
dtisnotaregularfunction.
2) E Z(t)Z(s)( ) = δ(t − s) 3) exp(−i2πξt)E Z(t)Z(0)( )dt∫ =1 4) Z(t)isawhitenoise(wewillclarifywhatthismeans).
Planforthelongstory
Wewillfirstaddressthedefinitionofwhitenoiseinitem4).Wediscussageneralstationarystochasticprocessandinthatcontextdefinewhitenoiseinstepslistedbelow
• Energyspectrumdensity(ESD)
• Powerspectrumdensity(PSD)
• AgeneralstationarystochasticprocessanditsPSD
• RelationbetweenPSDandauto-correlationfunction
• DefinitionofwhitenoisebasedonPSD
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Beforeweproceedwiththeplan,wefinishthepropertiesofFouriertransform.
PropertiesofFouriertransform
1)F ρ
N(0,σ2 )(t)⎡⎣⎤⎦ = F
12πσ2
exp −t2
2σ2⎛
⎝⎜⎞
⎠⎟⎡
⎣⎢⎢
⎤
⎦⎥⎥= exp −2π2σ2ξ2( )
2) F[δ(x)]=1
3) F[1]=δ(ξ)4) Parseval’stheorem
y(t)2dt∫ = ŷ(ξ)
2dξ∫
Proof:
ŷ(ξ)2dξ∫ = ŷ(ξ) ŷ(ξ)dξ∫
= exp(−i2πξt)y(t)dt∫ exp(i2πξ s)y(s)ds∫
⎛
⎝⎜
⎞
⎠⎟ dξ∫
= exp −i2πξ(t − s)( ) y(t)y(s)dtds∫∫
⎛
⎝⎜
⎞
⎠⎟ dξ∫
Changetheorderofintegration
= y(t)y(s) exp −i2πξ(t − s)( )dξ∫
F[1]=δ(t−s)! "#### $####
⎛
⎝⎜
⎞
⎠⎟dtds∫∫
= y(t)y(s)δ(t − s)dtds∫∫
= y(s)y(s)ds∫ = y(s)
2ds∫
Thelongstoryofwhitenoise
Energyspectrumdensity(ESD)
Inphysicsproblems,
Energy∝ y(t)2dt∫ = ŷ(ξ)
2dξ∫
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Note: Here“energy”referstotheenergydissipated.
Examples:y(t)=electriccurrent
Energy = R ⋅ y(t)2dt∫ , R=electricalresistance
y(t)=velocity
Energy = b ⋅ y(t)2dt∫ , b=viscousdragcoefficient
Formathematicalconvenience,wescaletheenergytodefine
Energy = y(t)2dt∫ = ŷ(ξ)
2dξ∫
Weliketoknowhowtheenergyisdistributedinthefrequencydimension.
Definitionofenergyspectrumdensity(ESD)
ESD≡ ŷ(ξ)2 = exp(−i2πξt)y(t)dt∫
2
Caution: ŷ(ξ)2isanunnormalizeddensity.
ŷ(ξ)2dξ∫ = y(t)
2dt∫ =Energy ≠1
Otherexamplesofunnormalizeddensity:
Populationdensity: Xnumberofpersonspersquaremile
Pollutiondensity: XamountofchemicalsperunitvolumeofairorwaterCardensity: Xnumberofcarsperthousandpersons
Xnumberofcarspersquaremile
Caution: (differentdefinitionsofenergyspectrumdensity)
Inelectricalengineering(EE),energyspectrumdensityisdefinedas
ESD≡Φ(ω)= 1
2πexp(−iωt)y(t)dt∫
2
Φ(ω)and ŷ(ξ)2arerelatedby
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Φ(ω)= 12π ŷ(ξ)
2 , ξ = ω2π
PowerspectrumdensityEnergyspectrumdensityismeaningfulonlywhen
Energy = y(t)2dt∫ = finite
Example:
y(t)=electriccurrent=y0, constantintime
Energydissipated = R ⋅ y02dt∫ =∞
Whenthetotalenergyisnotfinite,welookattheenergyperunittime.
Power = Energytime = finite
Definitionofpowerspectrumdensity(PSD)
PSD≡ lim
T→∞
exp(−i2πξt)y(t)dt−T
T
∫2
2T
Expressionofpowerspectrumdensity(PSD)
WewritePSDintoamoreworkableexpression.
PSD= lim
T→∞
exp(−i2πξt)y(t)dt−T
T
∫ exp(i2πξ s)y(s)ds−TT
∫2T
= limT→∞
exp(−i2πξ(t − s))y(t)y(s)dt−T
T
∫ ds−TT
∫2T
changeofvariableτ=t–s
= limT→∞
exp(−i2πξτ)y(τ+ s)y(s)dτ−T−s
T−s
∫ ds−TT
∫2T
Drawtheintegrationregionins-τplane.Foreachs,therangeforτis[–T–s,T–s].
Foreachτ,therangeforsis[a(τ),b(τ)]
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where
a(τ)= −T − τ, τ∈[−2T , 0]
−T , τ∈[0, 2T ]⎧⎨⎪
⎩⎪
b(τ)= T , τ∈[−2T , 0]
T − τ, τ∈[0, 2T ]⎧⎨⎪
⎩⎪
Changetheorderofintegration
PSD= lim
T→∞
exp(−i2πξτ) y(τ+ s)y(s)dsa(τ)
b(τ)∫ dτ−2T
2T∫
2T (PSD01)
Sofar,weworkedwithdeterministicprocessy(t).Nextweintroducestochasticprocessandstationarystochasticprocess.
StationarystochasticprocessDefinitionofstochasticprocess
Astochasticprocessisafunctionoftimethatvarieswiththerandomoutcomeofanexperiment.
y(t)
Shortnotation! = y(t ,ω)
Fullnotation"#$ %$ ω=randomoutcomeofanexperiment
DefinitionofstationarystochasticprocessLety(t)beastochasticprocess.Wesayy(t)isstationaryifforanysetoftimeinstances(t1,t2,…,tk),thejointdistributionof(y(t+t1),y(t+t2),…,y(t+tk))isindependentoft.
Example:
• W(t)isastochasticprocesses.
• Z(t)= dW(t)
dtisastochasticprocess.
Note: Forfinitedt,dW/dtiswelldefined,withnocomplicationatall.
Example:
• W(t)isnotstationary.E W(t)2( ) = t varieswitht.
• Z(t)= dW(t)
dtisstationary
Note: Thejointdistributionisinvariantunderashift.
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PropertiesofstationarystochasticprocessForastationarystochasticprocess,wehave
• E(y(t))=E(y(0))• E y(s + τ)y(s)( ) = E y(τ)y(0)( )
Caution:
Thesearenecessaryconditionsforastationarystochasticprocess.Theyarenotsufficientconditions.
Auto-correlationfunctionDefinitionofauto-correlationfunction
Forastationarystochasticprocess,
R(τ)≡ E y(s + τ)y(s)( ) = E y(τ)y(0)( ) iscalledtheauto-correlationfunction.
Note: R(τ)isafunctionofτonly,independentofs.Caution: becarefulwiththeterm“auto-correlation”
Auto-correlationcoefficientisdefinedas
ρ(τ)≡
E y(τ)−E( y(0))⎡⎣ ⎤⎦ y(0)−E( y(0))⎡⎣ ⎤⎦( )var( y(0))
Auto-correlationfunctionisdefinedas
R(τ)≡ E y(τ)y(0)( )
Wiener-Khinchintheorem(relationbetweenPSDandauto-correlationfunction)
Forastationarystochasticprocess,thepowerspectrumdensity(PSD)is
PSD≡ s(ξ)NewnotationforPSD
!"# = limT→∞E exp(−i2πξt)y(t)dt
−T
T
∫2⎛
⎝⎜⎞⎠⎟
2T
Weuse(PSD01)obtainedabovetorewrites(ξ)as
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s(ξ)= lim
T→∞
E exp(−i2πξτ) y(τ+ s)y(s)dsa(τ)
b(τ)∫ dτ−2T
2T∫⎛⎝
⎞⎠
2T
Changetheorderofintegrationandtakingaverage
= limT→∞
exp(−i2πξτ) E y(τ+ s)y(s)( )dsa(τ)b(τ)∫ dτ−2T2T∫2T
= limT→∞
exp(−i2πξτ)R(τ)(b(τ)−a(τ))dτ−2T
2T∫
2T
Theterm(b(τ)–a(τ))hastheexpression:
b(τ)−a(τ)= 2T + τ , τ∈[−2T , 0]2T − τ , τ∈[0, 2T ]
⎧⎨⎪
⎩⎪=2T − τ
Substitutingitintotheexpressionofs(ξ)yields
s(ξ)= lim
T→∞exp(−i2πξτ)R(τ) 1− τ2T
⎛⎝⎜
⎞⎠⎟dτ
−2T
2T∫
TakingthelimitasT→∞,wearriveat
s(ξ)= exp(−i2πξτ)R(τ)dτ−∞+∞
∫ WejustderivedtheWiener-Khinchintheorem.
Wiener-Khinchintheorem:Forastationarystochasticprocessy(t),thepowerspectrumdensity,s(ξ),andtheauto-correlationfunction,R(t),arerelatedby
s(ξ)= exp(−i2πξt)R(t)dt−∞+∞
∫ Inotherwords,thePSDisFouriertransformoftheauto-correlationfunction.
DefinitionofwhitenoiseLety(t)beastationarystochasticprocess.Wesayy(t)isawhitenoiseif
s(ξ)= const Inotherwords,thepowerofawhitenoiseisuniformlydistributedinthefrequencydimension.
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TheWiener-Khinchintheoremestablishedabovetellsusthatawhitenoisehastwoequivalentdefiningcharacters.
s(ξ)= const ⇐⇒ R(t)= E y(t)y(0)( )∝δ(t)
WorkingoutitemsintheshortstoryWere-writetheshortstoryintermsoftheauto-correlationfunvtionR(τ)andpowerspectrumdensitys(ξ).
1)Z(t)≡ dW
dtisnotaregularfunction.
2) R(τ)= E Z(s + τ)Z(s)( ) = δ(τ) 3) s(ξ)= exp(−i2πξt)R(t)dt∫ =1 4) Z(t)isawhitenoise.
• ToshowZ(t)isawhitenoise(item4),weonlyneedtoshows(ξ)=const(item3).• Toshows(ξ)=1(item3),weonlyneedtoshowR(t)=δ(t)(item2)
Thus,theremainingtaskistoshowitem2,whichwedonow.
DerivationofR(t)=δ(t) (a“formal”derivation”)
WefirstcalculateE(W(t)W(s))fort≥s.
E W(t)W(s)( ) = E (W(t)−W(s)+W(s))W(s)( )
= E (W(t)−W(s))W(s)( )+E W(s)2( ) =0+ s = s
SinceE(W(t)W(s))=E(W(s)W(t)),weobtain
E W(t)W(s)( ) =min(t ,s) Next,inthecalculationofE(Z(t)Z(s)),we“formally”exchangetheorderoftakingderivativesandtakingaverage.
E Z(t)Z(s)( ) = E ∂∂s
∂∂t
W(t)W(s)( )⎛⎝⎜
⎞⎠⎟
= ∂∂s
∂∂tE W(t)W(s)( ) = ∂∂s
∂∂tmin(t ,s)
Asafunctionoft,wehave
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min(t ,s)= t , t < s
s , t > s⎧⎨⎪
⎩⎪
Differentiatingwithrespecttot,andthenwritingitasafunctionofs,weget
∂∂tmin(t ,s)= 1, t < s
0, t > s⎧⎨⎪
⎩⎪ (asafunctionoft)
=
0, s < t1, s > t
⎧⎨⎪
⎩⎪ (asafunctionofs)
Differentiatingwithrespecttos,wearriveat
∂∂s
∂∂tmin(t ,s)= δ(s −t)
Therefore,weconclude
E Z(t)Z(s)( ) = δ(t − s) ==> R(τ)= E Z(s + τ)Z(s)( ) = δ(τ)
ExpressionsofR(t)ands(ξ)forfinitedt
(Justificationofthe“formal”derivationsabove)
Toemphasizethefinitetimestep,letΔt≡dt.Wehave
Z(t)=W(t +Δt)−W(t)
Δt awelldefinedstationarystochasticprocess
E Z(t)Z(s)( ) = E W(t +Δt)−W(t)Δt ⋅
W(s +Δt)−W(s)Δt
⎛⎝⎜
⎞⎠⎟
=0 , |t − s |> ΔtΔt−|t − s |(Δt)2 , |t − s |≤ Δt
⎧
⎨⎪
⎩⎪
(derivationnotincluded)
R(τ)= E Z(s + τ)Z(s)( ) =0 , |τ|> ΔtΔt−|τ|(Δt)2 , |τ|≤ Δt
⎧
⎨⎪
⎩⎪
TakingtheFouriertransformofR(t),weobtain
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s(ξ)= exp(−i2πξt)R(t)dt∫ = exp(−i2πξt)
Δt−|t |(Δt)2 dt−Δt
Δt
∫
=2cosh(i2πξΔt)−1(i2πξΔt)2
(derivationnotincluded)
Now,afterweobtains(ξ)forfiniteΔt,wetakethelimitasΔt→0.
Atanyfixedξ,asΔt→0,wehave
limΔt→0
s(ξ)= limΔt→0
2cosh(i2πξΔt)−1(i2πξΔt)2 =1
Observation:
• Mathematically,workingwithfinitedtuntiltakingthelimitattheendisarigorousapproachinwhicheverystepisproperlyjustified.Butderivingexpressionswithfinitedtisalsomathematicallymuchmoreelaborated.
• “Formal”derivationsaremuchsimpler.Buttheyarenotrigorous.
Aclassofcolorednoise:InthesubsequentdiscussionofOrnstein-Uhlenbeckprocess(OU),wewillseethatitsauto-correlationhastheform:
R(t)= E y(t)y(0)( )∝exp(−β|t |) Thecorrespondingpowerspectrumdensityis
s(ξ)= exp(−i2πξt)R(t)dt∫ ∝ exp(−i2πξt)exp(−β|t |)dt∫= 2ββ2 +4π2ξ2
Endofdiscussionofwhitenoise
ConstrainedWienerprocess
ForanunconstrainedWienerprocess,wehave
W(0)=0 and W(t1)~N(0,t1)
WhathappensifitisconstrainedbyW(t1+t2)=y?
W(t1)isstillrandom.
Weliketoknowtheconditionaldistribution(W(t1)|W(t1+t2)=y).
Forthatdiscussion,weneedtointroduceBayestheorem.
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BayesTheorem
ConsidertwoeventsAandB.WewritePr(AandB)intwoways.Pr(AandB)=Pr(A|B)Pr(B)
Pr(AandB)=Pr(B|A)Pr(A)Equatingthetwo,weget
Pr(A|B)Pr(B)=Pr(B|A)Pr(A)
ExpressPr(A|B)intermsofPr(B|A),wearriveatBayesTheoremforevents:
Pr(A B)=
Pr(B A)Pr(A)Pr(B)
ThisisBayestheoremforevents.
ToderiveBayestheoremfordensities,weconsider
A=“x≤X<x+ΔxB=“y≤Y<y+Δy
Wewriteprobabilitiesintermsofdensities
Pr(A B) ≈ ρ(X = x Y = y)Δx
Pr(B A) ≈ ρ(Y = y X = x)Δy
Pr(A) ≈ ρ(X = x)Δx
Pr(B) ≈ ρ(Y = y)Δy SubstitutingthesetermsintoBayestheorem,weobtainBayestheoremfordensities.
Bayestheoremfordensities
ρ(X = x Y = y) =
ρ(Y = y X = x)⋅ρ(X = x)ρ(Y = y)
Ausefultrick:
Indensityρ(X=x|Y=y),xistheindependentvariableandyisaparameter.ρ(Y=y)ontheRHSisafunctionofyonly,independentofx.ItsimplyservesasanormalizingfactortomaketheRHSintegrateto1.Thus,wedon’tneedtoexplicitlykeeptrackofρ(Y=y).WecanwriteBayestheoremconvenientlyas
ρ(X = x Y = y) ∝ ρ(Y = y X = x)⋅ρ(X = x)
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wheretheRHSneedsapropernormalizingfactortomakeitintegrateto1.
Thistrickisespeciallyconvenientfornormaldistributions.Oncewefind
ρ(X = x) ∝ exp −(x −µ)
2
2σ2⎛
⎝⎜⎞
⎠⎟,
wecanconcludeX~N(μ,σ2).
Conditionaldistribution(W(t1)|W(t1+t2)=y)
ThetargetisaprobabilityconditionedonWatalatertime.WeuseBayestheoremtowriteitintermsofaprobabilityconditionedonWatanearliertime.
LetX=W(t1)andY=W(t1+t2).Wehave
W(t1)~N(0,t1)
==>ρ W(t1)= x( )~N(0,t1)∝exp −x
2
2t1⎛
⎝⎜⎞
⎠⎟
W(t1 +t2) = W(t1)+ W(t1 +t2)−W(t1)( )
~N(0,t2)! "### $###
==> W(t1 +t2)W(t1)= x( ) ~ x +N(0,t2)
==>ρ W(t1 +t2)= y W(t1)= x( ) ∝ exp −( y − x)
2
2t2⎛
⎝⎜⎞
⎠⎟
TheBayestheoremgivesus
ρ W(t1)= x W(t1 +t2)= y( ) ∝ ρ W(t1 +t2)= y W(t1)= x( )⋅ρ W(t1)= x( )
∝exp −( y − x)
2
2t2⎛
⎝⎜⎞
⎠⎟exp −x
2
2t1⎛
⎝⎜⎞
⎠⎟
(Wedon’tneedtokeeptrackoffactorsthatareindependentofx!)
∝exp − 12t1
+ 12t2⎛
⎝⎜⎞
⎠⎟x2 −2 y2t2
x⎛
⎝⎜
⎞
⎠⎟
⎛
⎝⎜
⎞
⎠⎟
(Completingthesquare)
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∝exp− x −
t1 yt1 +t2
⎛
⎝⎜⎞
⎠⎟
2
2 t1t2t1 +t2
⎛
⎝
⎜⎜⎜⎜⎜
⎞
⎠
⎟⎟⎟⎟⎟
~ N t1 yt1 +t2
, t1t2t1 +t2
⎛
⎝⎜⎞
⎠⎟
Weconclude
ρ W(t1)= x W(t1 +t2)= y( ) ~ N t1 yt1 +t2 ,
t1t2t1 +t2
⎛
⎝⎜⎞
⎠⎟
Forthegeneralcase,wehave
ρ W(a+t1)= x W(a)= ya andW(a+t1 +t2)= yb( ) ~ N t1 yb +t2 yat1 +t2 ,
t1t2t1 +t2
⎛
⎝⎜⎞
⎠⎟
Aspecialcase: t1=t2=h
ρ W(a+h)= x W(a)= ya andW(a+2h)= yb( ) ~ N ya + yb2 ,
h2
⎛
⎝⎜⎞
⎠⎟