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non-classical pdfs
Remi Abgrall, Pietro Marco Congedo, Gianluca Geraci, Gianluca Iaccarino
To cite this version:
Remi Abgrall, Pietro Marco Congedo, Gianluca Geraci, Gianluca Iaccarino. Non-polynomial ex- pansion for stochastic problems with non-classical pdfs. [Research Report] RR-8191, INRIA. 2012.
�hal-00766760�
0 2 4 9 -6 3 9 9 IS R N IN R IA /R R -- 8 1 9 1 -- F R + E N G
RESEARCH REPORT N° 8191
December 18, 2012
Non-polynomial
expansion for stochastic problems with
non-classical pdfs
Remi Abgrall, Pietro Marco Congedo, Gianluca Geraci, Gianluca
Iaccarino
RESEARCH CENTRE BORDEAUX – SUD-OUEST 351, Cours de la Libération
RemiAbgrall,Pietro Maro Congedo, GianluaGerai,
GianluaIaarino
Projet-TeamBahus
ResearhReport n°8191Deember18,201223pages
Abstrat: Inthisstudy, somepreliminary resultsaboutthepossibilitytoextendthelassial
polynomialChaos(PC) theorytostohastiproblemswithnon-lassialprobabilitydistributions
ofthevariables,i.e. outsidetheframeworkofthelassialWiener-Askeysheme[1℄,arepresented.
Theproposedstrategyallowstoobtainananalytialrepresentationofthesolutioninordertobuild
a metamodel or to ompure onditional statistis. Various numerial results obtained on some
analytialproblemsarethenprovidedtodemonstratetheorretnessofthepresentedapproah.
Key-words: PolynomialChaos,Colloation,Unertainty Quantiation,ANOVA,Conditional
statistis
non-lassiques
Résumé : Dans ette étude, on présente des résultats préliminaires sur la
possibilité d'utiliser la théorie lassique du Chaos Polynomial pour des prob-
lèmesstohastiquesavedesfontionsdensitédeprobabiliténon-lassiques. La
stratégie proposéepermet de aluler une représentation analytique de laso-
lution pour onstruire un metamodèle ou aluler les statistiques. Plusieurs
résultatsnumériquessontprésentés pourillustrerlavaliditédel'approhepro-
posée.
Mots-lés : ChaosPolynomial,Colloation,Quantiationdesinertitudes,
ANOVA
Contents
1 Introdution 5
2 Mathematialand problem setting 5
2.1 ANOVAdeompositionandsensitivityindexes . . . 7
2.1.1 Sobolsensitivityindies . . . 7
3 ClassialPolynomial Chaosapproah 8
3.1 SensitivityomputationfromPCexpansion . . . 9
4 Anon polynomialapproahfor highorder statistis 10
4.1 PolynomialVsNon-Polynomialapproah. . . 12
4.2 ComputationoftheonditionalstatistisbythenPC. . . 14
5 Numerialresults 16
6 Conlusionsand perspetive 20
7 Aknowledgements 22
List of Figures
1 ExtratermswiththenPCapproah . . . 14
2 ColloaltionvsnPCforthemonodimensionalproblem . . . 17
3 ColloaltionvsnPCfor
f pol
withpdfp 1
(d = 2
). . . . . . . . . . 184 ColloaltionvsnPCfor
f pol
withpdfp 2
(d = 2
). . . . . . . . . . 185 ColloaltionvsnPCfor
f pol
withpdfp 3
(d = 2
). . . . . . . . . . 196 ColloaltionvsnPCfor
f pol
withpdfp 1
(d = 3
). . . . . . . . . . 197 ColloaltionvsnPCfor
f pol
withpdfp 2
(d = 3
). . . . . . . . . . 208 ColloaltionvsnPCfor
f np
withpdfp 1
(d = 2
) . . . . . . . . . . 209 ColloaltionvsnPCfor
f np
withpdfp 2
(d = 2
) . . . . . . . . . . 2110 ColloaltionvsnPCfor
f np
withpdfp 3
(d = 2
) . . . . . . . . . . 211 Introdution
Inreentyearsthe growinginterestin UnertaintyQuantiation (UQ)in the
numerial eld has leadto manydierent numerialmethods or strategiesto
quantify the statistisin preseneof stohasti inputs. Oneof the mostpop-
ular method is the Polynomial Chaos (PC) both in its version intrusive or
non-intrusive [2℄. This lass of methods has bee shown to be very eient,
omparedto MonteCarloorolloationstrategies,ifthemodeltorepresentis
smoothenough. Morereentlywiththeaim toextendthelassialPCtheory
to realappliation asesthesoalled multi-elementPC(me-PC)has beenin-
troduedbyKarniadakisetal. (seeforinstane[3℄)allowingtherepresentation
ofprobabilitydistributionsthatfalloutsidetheso-alledWiener-Askeysheme.
Thisopenthewaytotherepresentationofinputsharaterizedbyprobability
distributions that anbeextratedfrom experiments. Howevertheimplemen-
tation of a me-PC ode ould be not so straightforward even if aPC ode is
already at disposal and, until this moment, the eetiveness of this approah
to obtainstatistial momentshigherthanthe varianehasnotbeen doneyet.
In partiular a simple extension of the simple link between the ANOVA rep-
resentation andthe PCexpansion(seefor instane [4℄) isstill missing. Inthe
presentworkwewouldliketoreinterprettheproblemtoextendthePCtonon
lassial pdf in a more diret way reovering all the ommon features of the
lassial PC, as for instane the link between theexpansion and theANOVA
deomposition to omputeonditional statistis. Weproposeastrategybased
onamappingoftheoriginalproblemonanequivalentuniformstohastispae
on whih applying the PC analysis. This strategy leads to a non orthogonal
andnonpolynomial(inthegeneralase)representationthatreetsinaloseof
eienyifomparedtothePCintheaseoflassialpdfs. Howeveraswillbe
learlatertheloseoforthogonalitydoesnotaettheomputationoftheoef-
ientoftherepresentationbutonlythestatistial momentsomputation. We
expet anywayto improvethese preliminary resultswith some simple further
steps, as aoupling with aSparse Grid algorithm anda parallel implementa-
tion,inashortterm. Theremainingpartoftheworkisorganizedasfollows. In
thesetion 2 themathematialsetting is presentedand thehigher statistial
moments are dened. An analytial denition of the ANOVA expansion and
howitsreetin theomputationofonditional statistisisalsoprovided. An
introdutiononthelassialPCisfurnishedwiththeaimtomaketheworkas
possibleself-ontainedinseetion3. Thehearthoftheworkisthesetion4in
whihourstrategy(nPC)isproposed.SomeresultsonthelinkbetweenthePC
and nPCare thenpresentedand thelink betweenthenPC expansionandthe
ANOVA deompositionisdesribedfortherstordertermsoftheonditional
varianes. Finallysomenumerialresultsarepresentedforanalytialproblems
indimensionuptothreefordierentkindofustomdened pdfsinsetion5.
Conludingremarksandfutureperspetiveworksarereportedaslosurein 6.
2 Mathematial and problem setting
Considerthefollowingproblem foranoutputofinterest
u(x, t, ξ(ω))
:L(x, t, ξ(ω); u(x, t, ξ(ω))) = S(x, t, ξ(ω)),
(1)wheretheoperator
L
anbeeitheranalgebraioradierentialoperator(inthisaseweneedappropriateinitialandboundaryonditions). Theoperator
L
andthesoureterm
S
aredenedonthedomainD × T × Ξ
, wherex ∈ D ⊂ R n d
,with
n d ∈ {1, 2, 3}
,andt ∈ T
are the spatialand temporal dimensions. Ran- domnessisintroduedin(1)anditsinitialandboundaryonditionsintermofd
seondorder randomparameters
ξ(ω) = {ξ 1 (ω 1 ), . . . , ξ d (ω d )} ∈ Ξ
withparam-eterspae
Ξ ⊂ R d
. Thesymbolω = {ω 1 , . . . , ω d } ∈ Ω ⊂ R
denotesrealizations inaompleteprobabilityspae(Ω, F , P )
. HereΩ
isthesetofoutomes,F ⊂ 2 Ω
isthe
σ
-algebraofeventsandP : F → [0, 1]
isaprobabilitymeasure. Random parametersξ(ω)
an haveany arbitraryprobability density funtionp(ξ(ω))
,in thisway
p(ξ(ω)) > 0
forallξ(ω) ∈ Ξ
andp(ξ(ω)) = 0
forallξ(ω) ∈ / Ξ
; weannowdroptheargument
ω
forbrevity. Theprobabilitydensityfuntionp(ξ)
is dened as ajointprobability density funtion from the independentproba-
bilityfuntion of eahvariable:
p(ξ) = Q d
i=1 p i (ξ i )
. Thisassumption allowstoanindependentpolynomialrepresentationforeverydiretionintheprobabilis-
tispaewiththepossibilitytoreoverthemultidimensionalrepresentationby
tensorization. Inthepresentworkthetestasesarealgebrai,steadyequations
withnophysialspaedependene(weandropthespatialargument
x
),soweanwrite
L(ξ; f (ξ)) = 0
(2)thentheaimistondthestatistialmomentsofthesolution
f (ξ)
.The(entered)statistial momentsofdegree
n
tharedenedasµ n (f ) =
Z
Ξ
(f (ξ) − E(f )) n p(ξ)dξ,
(3)where
E(f )
representstheexpetedvalueofthesolutionf (ξ) E(f ) =
Z
Ξ
f (ξ)p(ξ)dξ.
(4)Inthis work moments upto thedegree four areonsidered and in the fol-
lowing we refer to the variane
Var
, skewnesss
and kurtosisk
to indiate,respetively,theseond,thirdandfourthorder statistialmoments.
Higherorder statistis(fromordertwo)anbeomputedknowingonlyex-
petanies of the model funtion
f
and its values raised to the desired orderVar = E(f 2 ) − E(f ) 2
s = E(f 3 ) − 3E(f )Var − E(f ) 3
k = E(f 4 ) − 4E(f 3 )E(f ) + 6E(f 2 )E(f ) 2 − 3E(f ) 4 .
(5)
This representation of the higher moments will be employed to ompare the
strategywithaolloationapproah. Thekeyidea,leadingtothislastapproah,
is to ompute the expetany for the funtions
f
,f 2
,f 3
andf 4
, obtaineddiretlyfrom thevaluesof themodel
f
andthenombinethese expetanytoobtainhigh order statistis. Adiret, brutal-fore,olloationapproah ould
betoomputediretlyalltheintegralsontainedintheequations(5)evaluating
eahtermbythepreedentstatistialmoment. Theproblemreduetoompute
only four integral. This an be done eiently if the number of quadrature
points is high enough. Anyway this approah annot provide ametamodel of
the funtion and an expansionof the solution on whih onditional statistis
anbeomputed(seeforinstane[5℄). Thetheoretialframeworkonwhihthe
onditionalstatistisanbeobtainedbasedonanANOVArepresentationisthe
subjetofthefollowingsetion.
2.1 ANOVA deomposition and sensitivity indexes
Let us onsider to havea given equation, or asystems of equations, to solve
and to have an output of interest
f = f (ξ)
. The output of the system isdependentby
d
unertaintiesparametersξ i
assumedsothatξ = {ξ 1 , . . . , ξ d } ∈ Ξ ⊂ R d
. In this work we assume independent distributed random variablesξ i ∈ Ξ i
and,onsequently,thespaeΞ
anbeobtainedbytensorizationoftheir monodimensional spaes,i.e.Ξ i ⊂ R
,Ξ = Ξ 1 × · · · × Ξ d
.From the independene of the random variables follows diretly
p(ξ) = Q
i p(ξ i )
. Assumingf (ξ) ∈ L 2 (ξ, p(ξ))
thenaSobolunique funtionaldeom-positionexists:
f (ξ) = X
u ⊆{1,...,d}
f u (ξ u )
(6)where
u
is aset of integerswith ardinalityv = |u|
andξ u = {ξ u 1 , . . . , ξ u v }
.Eahfuntion
f u
isomputedbytherelation[4℄:f u (ξ u ) = Z
Ξ u ¯
f (ξ)p(ξ u ¯ )dξ u ¯ − X
w ⊂ u
f w (ξ w )
(7)where
Ξ u ¯
is thespaeΞ
withoutthedimensionsontainedinu
andξ u ¯
isthevetor
ξ
withoutthevariablesinu
.Bydenition
f 0 = Z
Ξ
f (ξ)p(ξ)dξ
(8)is the mean of the funtion
f (ξ)
. This funtional deomposition is alled ANOVA if eah of the2 d
elements of the deomposition, exeptf 0
, veriesforevery
ξ i
:Z
Ξ i
f u (ξ u )p(ξ i )dξ i = 0, ∀i ∈ u
(9)Diretlyfromeq. 9followstheorthogonality:
Z
Ξ
f u (ξ u )f w (ξ w )p(ξ)dξ = 0, u 6= w
(10)2.1.1 Sobolsensitivity indies
EmployingtheANOVAdeompositionitispossibleto deomposethevariane
of
f = f (ξ)
:Var(f ) = X
u ⊆{1,...,d}
u 6=0
D u (f u )
(11)where
D u (f u ) = Z
Ξ u
f u 2 (ξ u )p(ξ u )dξ u
(12)and
Ξ u = Ξ u 1 × · · · × Ξ u v
.TheSobolsensitivityindies(SI),aredenedas:
S u = D u
Var
(13)measuringthesensitivityofthevarianeduetothe
v
-order(v = |u|
)interationbetweenthevariablesin
ξ u
. Itisevidentthatthesummationofthe2 d −1
Sobolindiesisequaltoone.
3 Classial Polynomial Chaos approah
In this setion we refer briey to the main results relative to the high order
statis omputation by the lassial PC approah with further extensions for
higherstatistialmomentsprovidedbythesameauthors;forexhaustivedetails
referto[5℄.
Thesolutionisexpandedas
f (ξ) =
P
X
k=0
β k Ψ k (ξ),
(14)where
Ψ k
is thepolynomialbasisorthogonal to theprobabilitydensity distri- butionp(ξ)
.Eahofthe
P + 1 = (n 0 + d)!/(n 0 !d!)
oeientsoftheexpansion(oftotaldegree
n 0
)anbeomputedasprojetionofthemodelfuntionf (ξ)
withthepolynomial basis exploiting the orthogonality onditions, i.e. the polynomial
basisis hosen in aordto the Wiener-Askeysheme to be orthogonalto the
probabilitydistribution
p(ξ) β k =
R
Ξ f (ξ)Ψ k (ξ)p(ξ)dξ R
Ξ Ψ k (ξ)Ψ(ξ)p(ξ)dξ .
(15)Theproblemistoomputetheintegralatnumeratorwhileforthedenominator
thevalueouldbeknownanalytially.
Assumingto know the oeients
β k
of the expansionthe four statistialmomentsare[5℄
E(f ) = β 0
Var =
P
X
i=1
β 2 i hΨ 2 i (ξ)i
s =
P
X
k=1
β 3 k hΨ 3 k (ξ)i + 3
P
X
i=1
β i 2
P
X
j=1 j6=i
β j hΨ 2 i (ξ), Ψ j (ξ)i
+ 6
P
X
i=1 P
X
j=i+1 P
X
k=j+1
β i β j β k hΨ i (ξ), Ψ j (ξ)Ψ k (ξ)i
k =
P
X
i=1
β 4 i hΨ 4 i i + 4
P
X
i=1
β i 3
P
X
j=1 j6=i
β j hΨ 3 i , Ψ j i + 3
P
X
i=1
β 2 i
P
X
j=1 j6=i
β j 2 hΨ 2 i , Ψ 2 j i
+ 12
P
X
i=1
β i 2
P
X
j=1 j6=i
β j P
X
k=j+1 k6=i
β k hΨ 2 i , Ψ j Ψ k i
+ 24
P
X
i=1 P
X
j=i+1 P
X
k=j+1 P
X
h=k+1
β i β j β k β h hΨ i Ψ j , Ψ k Ψ h i
(16)
Theexpressionreportedin(16)areobtainedthankstotheorthogonalityof
thepolynomialbasis,i.e.
Z
Ξ
Ψ i (ξ)Ψ j (ξ)p(ξ)dξ = δ ij hΨ 2 i i.
(17)3.1 Sensitivity omputation from PC expansion
TheomputationoftheSobolindiesis possibleusingeverysamplestohasti
method (Monte Carlo, quasi-Monte Carlo)but anbedone in averyeient
waywhenapolynomialexpansionofthesolutionisadopted. Theideaistoom-
pute theexpansionof thesolution(trunated) andompute theSobolindies
fromtheexpansioninsteadofomputingthemontherealfuntion. Remember
thepolynomialexpansion:
f (ξ) = ˜ f (ξ) + O T =
P
X
k=0
β k Ψ k (ξ) + O T ,
(18)withanumberoftermsrelatedtothemaximumdegreeofthepolynomialreon-
strution
n o
andthedimensionofthesystemd
:P + 1 = (n n o o +d)! !d!
. Eahelementf u
ofthefuntionaldeompositionoff (ξ)
isapproximatedbytherelativetermf ˜ u
:f u (ξ u ) ≈ f ˜ u (ξ u ) = X
k∈K u
β k Ψ k (ξ u ),
(19)wheretheset ofindies
K u
isgivenbyK u =
k ∈ {1, . . . , P }|Ψ k (ξ u ) =
| u |
Y
i=1
φ α k i (ξ u i ), α k i > 0
(20)
and
φ α k i (ξ u i )
are the monodimensional polynomials for every diretionξ i
ofdegree
k
hosenwithrespettotheso-alledWiener-Askeysheme[1℄.Thanks to the orthogonality it is possible to obtain diretly the variane
Var(f ˜ ) = Var( ˜ f ) ≈ Var(f )
and the onditional varianeD ˜ u (f u ) = D u ( ˜ f u ) ≈ D u (f u )
from thefollowingrelations:Var(f ˜ ) =
P
X
k=1
β k 2 hΨ k , Ψ k i
(21)D ˜ u (f u ) = X
k∈K u
β k 2 hΨ k , Ψ k i.
Sobolsensitivityindiesfollowsdiretly fromeq. 21:
S u ≈ S ˜ u = D ˜ u (f u ) Var(f ˜ ) =
P
k∈K u β 2 k hΨ k , Ψ k i P P
k=1 β k 2 hΨ k , Ψ k i .
(22)If ustom dened probability distribution funtion are employed the or-
thonality properties of thebasisannot beexploited anymore to omputethe
oeientsofthepolynomialexpansion. Inthefollowingsetionwedesribea
strategytoreoverasolutionexpansionwithrespetanonpolynomialbasis,in
the generalase,in whih theortoghonalityof asupport basisis employedto
omputetheoeientsoftheexpansion.
4 Handling whatever form of pdf for the ompu-
tation of higher order statistis
Thestate-of-the-artto omputestatistismomentsfornon lassialpdf isthe
so-alledmulti-elementmethodme-PC[3℄. This familyof tehniques allowsto
eiently ompute, thanks to a partition of the stohasti spae, the (piee-
wise) polynomial approximationsof the model funtion
f (ξ)
. Despite to thepossibilitytoomputeexpetanyandvarianeeiently toomputehigh or-
der statistis this method enounter the same problems of the lassial PC
approah: high number ofintegralsto omputeasin the diret approah (see
equations (16))orsampling onvergene issues asametamodel approah. At
thesametimeaverystrongomputationaleortmustbedevotedto adaptan
existingPCodetoamulti-elementapableone. Anywaytheeetivepossibil-
ityto linkthe me-PCmethod tothe ANOVAdeomposition hasnotbeenyet
providedtoomputeonditionalstatistis.
Totaklethisproblemweproposedamapping proedurethatallowstoob-
tain apolynomialrepresentation ofafuntion depending onaustomdened
distributed randomvetor. Thisproedure allowsastraightforwardimplemen-
tationstartingfromanexistingPCode.
Theproedure is thesameof thelassial PCapproah, i.e. a polynomial
approximation ofthe model is omputed andthen all thestatistial moments
are omputed diretlyfrom this polynomialexpansion. Obviously onditional
statistisanbeomputedtoo.
First of all the
P + 1
oeients must be omputed. If the probability distributionfalloutsidetheso-alledWiener-Askeyshemeaproperorthogonalbasisannotbeemployedasin thegeneralized-PCmethod.
Letus assumetoreasttheprobabilitydensityfuntion
p(ξ)
asp(ξ) = p(ξ)¯ p
¯
p ,
(23)where
p ¯
isanequivalentuniformdistributiononthespaeΞ
¯ p = 1
R
Ξ dξ .
(24)All theintegralofthekind
R f (ξ)p(ξ)dξ
anbere-interpretedasstatistis ofafuntionf ¯ (ξ)
denedbyf ¯ (ξ) = f (ξ)p(ξ)
¯
p ,
(25)withanuniformdistribution
p ¯
onΞ
oftheparametervetor.At this stage a polynomial representation of the funtion
f ¯ (ξ)
an be ob-tainedemployingaLegendrebasisorthogonalonastohastispaeembedded
withanuniformdistribution.
The
P + 1
oeientsoftheseriesanbeomputedasβ k =
R
Ξ f ¯ (ξ)Ψ k (ξ)¯ pdξ R
Ξ Ψ k (ξ)Ψ(ξ)¯ pdξ ,
(26)wheretheorthogonalityofthepolynomialbasisallowstoavoidtoomputethe
mixed terms,i.e. termsofthekind
R
Ξ Ψ i Ψ j pdξ ¯
.The
P + 1
terms of the polynomial approximation of the funtionf ¯ (ξ)
,obtainedontheLegendrebasis,ouldbeemployedeasilytoobtainapolynomial
expansionof
f (ξ)
onasetofP +1
(nonorthogonal)termonthestohastispae withdistributionp
. Theproedureisthefollowingf ¯ (ξ) = f (ξ) p(ξ)
¯
p =
P
X
i=0
β k Ψ k (ξ) → f (ξ) =
P
X
i=0
β k Ψ k
¯ p p(ξ) =
P
X
i=0
β k Ψ ¯ k ,
(27)
this is made possible if, as is the ase, no holes in the domain are present,
p(ξ) > 0
. WeremarkthatthebasisΨ ¯ i P
i=0
isnotpolynomialiftheprobability distributionp(ξ)
is notpolynomialand, in the general aseR
Ξ Ψ ¯ i Ψ ¯ j p(ξ)dξ 6=
δ ij
R
Ξ Ψ ¯ 2 i p(ξ)dξ
.Howeverthisexpansionallowstoomputestatistis(eventuallyonditional)
and also the metamodel for the funtion
f (ξ)
. Even in the ase of time de-pendent pdf the points on whih evaluate the model are always the zeros of
theLegendre polynomialassoiatedto thespae. Despiteto thepossibilityto
ompute the expansion even for a known distribution as for instane a Beta
distribution,thistehniqueisexpetedtoperformworstinthisaseinwhiha
properoptimalbasis,intermofonvergene,anbehosen. Adisussiononthe
relationofthelassialgPCmethodwiththisnonpolynomialhaosexpansion
isreportedin thenextsetion.
4.1 On the relation between polynomial and non polyno-
mial haos approah
In the previous setion a novel tehnique has beenpresented to ompute the
expansionofthesolutionforawhateverformofpdf.
Letassumetohaveapolynomialfuntion
f (ξ) ∈ P r
withadistributionofthe vetorparameterξ ∼ Beta(α, β)
. WereallherethataBeta(α, β)
distribution isdesribedasp(ξ) = (ξ + 1) α−1 (1 − ξ) β−1
B(α, β)2 α+β−1 ,
(28)wherethefuntion
B(α, β)
isB(α, β) = Γ(α)Γ(β)
Γ(α + β)
(29)andthegammafuntion is
Γ(n) = (n − 1)!
Inthegeneralized-PCasetheJaobibaseanbeemployedandthenumber
ofpoints
n
neededtoomputetheintegraloforder2r
(produtofthefuntionand the Jaobipolynomialof degree
r
th) is2r = 2n − 1
, thenn = r + 1
(foreahdimension). Ifthenonpolynomialhaosisemployedtheintegrandshould
beof theorder
2r + α + β
. Ofoursethe regularityof theintegrandbeomesthe sameof the PC asein aseof uniform distribution (
α = β = 0
). In thegeneralaseanhighernumberofpointsisneededtosolveorretlytheintegrals
withrespetthegeneralase. Howeverin ageneralasethemodelfuntion is
notpolynomialandthentheadvantageofaGaussianquadraturebasedonthe
polynomial orthogonal basis is less evident. Of ourse this tehniques make
sense in the ase of non standard (eventually time dependent) pdfs in whih
ase thePC tehniquesannot beapplied without amulti-elementtehnique.
Weremarkherethat intheaseofdisontinuouspdfthisproedure ouldstill
be applied even if the onvergene ould be slower or even prevented in the
worstases.
Theother dierene with respet a standardPC tehnique is in the om-
putation of the statistial moments. The basis
Ψ ¯ i P
i=0
is not orthogonal onthespae
Ξ
withrespetthedistributionp(ξ)
andthenthemixed termsoftheexpansion must be onsidered. When theexpansion for
f (ξ)
is obtained (seeequation(27))thestatistisanbeomputedas(see[5℄fortheorthogonalase)
E(f ) = β 0
Var = β 0 2 (h Ψ ¯ 2 0 − 1i) +
P
X
k=1
β k 2 h Ψ ¯ 2 k i + 2
P
X
i=0 P
X
j=i+1
β i β j h Ψ ¯ i , Ψ ¯ j i
s =
P
X
k=0
β k 3 h Ψ ¯ 3 k (ξ)i + 3
P
X
i=0
β i 2
P
X
j=0 j6=i
β j h Ψ ¯ 2 i (ξ), Ψ ¯ j (ξ)i
+ 6
P
X
i=0 P
X
j=i+1 P
X
k=j+1
β i β j β k h Ψ ¯ i (ξ), Ψ ¯ j (ξ) ¯ Ψ k (ξ)i
k =
P
X
k=0
β k 4 h Ψ ¯ 4 k (ξ)i + 4
P
X
i=0
β i 3
P
X
j=0 j6=i
β j h Ψ ¯ 3 i , Ψ ¯ j i + 3
P
X
i=0
β i 2
P
X
j=0 j6=i
β 2 j h Ψ ¯ 2 i , Ψ ¯ 2 j i
+ 12
P
X
i=0 P
X
j=0 j6=i
P
X
k=j+1 k6=i
β i 2 β j β k h Ψ ¯ i (ξ) 2 , Ψ ¯ j (ξ) ¯ Ψ k (ξ)i
+ 24
P
X
i=0 P
X
j=i+1 P
X
k=j+1 P
X
h=k+1
β i β j β k β h h Ψ ¯ i (ξ), Ψ ¯ j (ξ) ¯ Ψ k (ξ) ¯ Ψ h (ξ)i.
(30)
Obviously the number of integral to ompute depends diretly form the
numberofoeientsthatisdiretlyrelatedtothedimension
d
oftheproblemand the total degreeof approximation
n 0
. The numberof termsfor the nonpolynomialapproahanbeevaluatedas
T ¯ Var = P + 1 + P
2
T ¯ s = P + 1 + P (P + 1) +
P + 1 3
T ¯ k = P + 1 + P (P + 1) + P (P + 1) + (P + 1) P
2
+
P + 1 4
,
(31)
wherethesymbols
T ¯ Var
,T ¯ s
andT ¯ k
indiaterespetivelythenumberofintegral toomputeforvariane,skewnessandkurtosisforthenonpolynomialapproah.The number of the mixed term to ompute, whih is equal to the dier-
ene between thenumber ofintegralto omputein thelassialPC ase (see
equations(16)),anbeshowntobyequalto
∆ Var = P
2
+ 1
∆ s = 2P + 1 +
P + 1 3
− P
3
∆ k = P 2 + 3P + 1 + (P + 1) P
2
+
P + 1 4
− P
2
− P P − 1
2
− P
4
,
(32)
where
P
dependsfromboththestohastidimensiond
andthetotaldegreeoftheapproximation(ofthefuntion
f ¯ (ξ)
).Theevolutionofthe numberof theextratermsto omputeisreported for
theasewith
n 0 = 2
anddimensionbetween2and 10in gure1.d
∆ T
2 4 6 8 10
10 1 10 2 10 3 10 4
∆T Var
∆T s
∆T k
Figure 1: Evolution ofthe extratermsto omputein thenon polynomialap-
proahwith respetthe standardgPC method. Theasereported isobtained
with
n 0 = 2
andadimensiond
between2and10.4.2 Computation of the onditional statistis by the nPC
The approah presented in this work allowsto reprodue thestruture of the
solution
f (ξ)
intermofomponentseveniftheseomponentsarenotorthogonaleah other. For this reason the funtional ANOVA deomposition annot be
derivedin astraightforwardwayasshowed in setion3.1 identifyingdiretly
thesubsetofindexes
K u
asshowedintheequation(20). HowevertheorthogonalbasisofLegendreunderlinedabovetheseriesexpansionofthesolutionallowsto
obtaininarelativesimplewayeahrstordertermoftheANOVAexpansion,
i.e. termsassoiated to thesubset
u
with ardinalityequal to one. Reallingthedenitionofthese
d
termsoftheANOVAexpansion,theequation(7)herereportedonlyforonveniene
f u (ξ u ) = Z
Ξ u ¯
f (ξ)p(ξ u ¯ )dξ u ¯ − X
w ⊂ u
f w (ξ w ),
intheaseoftherstorderterms,i.e. termswith
card(u) = 1
,anbereduedin
f u (ξ u ) = Z
Ξ u ¯
f (ξ)p(ξ u ¯ )dξ u ¯ − f 0 .
(33)Inatingtheexpansion(27)into(33)oneobtains
f u (ξ u ) =
P
X
k=0
β k
Z
Ξ u ¯
Ψ ¯ k (ξ)p(ξ u ¯ )dξ u ¯ − f 0
=
P
X
k=0
β k
Z
Ξ u ¯
Ψ k (ξ) p(ξ u ¯ )
p(ξ) pdξ ¯ u ¯ − f 0 .
(34)
Theratiobetweenthetwoprobabilitydensity
p(ξ u ¯ )
andp(ξ)
anbeomputedas
p(ξ u ¯ )
p(ξ) = p(ξ u ¯ )
p(ξ u )p(ξ u ¯ ) = 1
p(ξ u ) ,
(35)where
p(ξ u )
istheprobabilitydensityrelativeto thesubsetu
. Theequivalentuniform distribution
p ¯
, in the same way, an be deomposed in the produtbetweentheequivalentuniformdistribution relativetotheset
u
andtheothervariablesas
¯
p = ¯ p u p ¯ u ¯ .
(36)Theselast twoequationallowtoreasttherstorderANOVAtermas
f u (ξ u ) =
P
X
k=0
β k
¯ p u
p(ξ u ¯ ) Z
Ξ u ¯
Ψ k (ξ)¯ p u ¯ dξ u ¯ − f 0 .
(37)Thevalueoftheintegralin thelastequationdepends ontheset assoiated
totheindex
k
. Wean writeZ
Ξ u ¯
Ψ k (ξ)¯ p u ¯ dξ u ¯ =
Ψ k (ξ) if k ∈ K u 0
0 if k / ∈ K u 0 ,
(38)where theset
K u 0
isobtainedasunionof thesetK u
and thenullmulti-index element(k = 0
).Fortherstorderterms,i.e. if
card(u) = 1
, weanwritef u (ξ u ) = X
k∈K u 0
β k
¯ p u
p(ξ u ¯ ) Ψ k (ξ) − f 0 ,
(39)obviouslystillholds
f 0 = β 0
.To omputethe onditional varianerelative to eah funtion
f u
the rststepis to raise to theseond powertheequation (39)and thenintegrate over
thespae
Ξ u ⊂ Ξ
withtheweightfuntionp(ξ u )
.Theequation(39)raisedtotheseondpoweris
f u 2 (ξ u ) = X
k∈K u 0
β k 2 p ¯ 2 u
p 2 (ξ u ) Ψ 2 k (ξ) + 2 X
i∈K 0 u
X
j≥i+1 j∈K u 0
β i β j
¯ p 2 u
p 2 (ξ u ) Ψ i (ξ)Ψ j (ξ)
− 2β 0
X
k∈K u 0
β k
¯ p u
p(ξ u ) Ψ k (ξ) + β 0 2
(40)
Thelast equationneedtobeintegratedandthen, in thefollowing,weanalyze
termbytermtheintegrationoftherighthandsideofthe(40) . Therstterm
oftherighthandsideintegratedanbewritten as
X
k∈K u 0
β 2 k Z
Ξ u
¯ p 2 u
p 2 (ξ u ) Ψ 2 k (ξ) p(ξ u )dξ u = X
k∈K 0 u
β 2 k Z
Ξ u
¯ p 2 u
p(ξ u ) Ψ 2 k (ξ) dξ u .
(41)Theseondtermanbetreatedin ananalogueway
2 X
i∈K u 0
X
j≥i+1 j∈K 0 u
β i β j
Z
Ξ u
¯ p 2 u
p 2 (ξ u ) Ψ i (ξ)Ψ j (ξ) p(ξ u )dξ u =
2 X
i∈K u 0
X
j≥i+1 j∈K 0 u
β i β j
Z
Ξ u
¯ p 2 u
p(ξ u ) Ψ i (ξ)Ψ j (ξ) dξ u .
(42)
Thethirdtermanbedramatiallysimpliedas
2β 0
X
k∈K u 0
β k
Z
Ξ u
¯ p u
p(ξ u ) Ψ k (ξ) p(ξ u )dξ u = 2β 0 2
Z
Ξ u
¯ p u
p(ξ u ) p(ξ u )dξ u + 2β 0
X
k∈K u
β k
Z
Ξ u
¯ p u
p(ξ u ) Ψ k (ξ) p(ξ u )dξ u = 2β 2 0
(43)
Thenal formof theonditionalvariane,fortherstorderterms,is then
obtaineddiretlybysummingupthese simpliedterms
D u = X
k∈K u 0
β k 2 Z
Ξ u
¯ p 2 u
p(ξ u ) Ψ 2 k (ξ) dξ u +
2 X
i∈K u 0
X
j≥i+1 j∈K u
β i β j
Z
Ξ u
¯ p 2 u
p(ξ u ) Ψ i (ξ)Ψ j (ξ) dξ u − β 0 2 .
(44)
5 Numerial results
In this setion some numerial results are reported for model problems with
ustom dened pdfs. All theresults are provided with aomparison between
thenPCandtheolloationapproah. Weremarkherethatweexpetabetter
behaviorin termofonvergenefrom theolloationapproah,buttheimpor-
tane of the present nPC approah is to provide ametamodel of thesolution
andaframeworktoomputehighordermomentsonditionalstatistis. Exam-
pleswith dimensionsuptothree areherereportedandtheeetiveness ofthe
strategyisveriedwithrespettotheanalytialsolution.
Threedierentkindofustompdfsareemployedinthiswork(forastohas-
tiparameterdened in
[−1, 1]
): alinearpdf
p 1 (ξ) = 1/2 + 1/3ξ
aquadratipdf
p 2 (ξ) = ξ 2 + 1/2ξ + 1/6
anonpolynomialpdf
p 3 (ξ) = 1/2 + 1/3 sin (πξ)
.Intheaseofmultidimensionalproblemsthepdfisobtainedbytensorization
ofequalpdfsforeah diretionofthestohastispae.
Therstmodelproblemisamonodimensionalfuntion
f (ξ) = sin (πξ) +e ξ 2
dened on
Ξ = [−1, 1]
withaprobabilitydistributionequaltop 1 (ξ)
.Theresultsobtainedfortherstmodelproblemintermofperentageerror
with respet the analytial results are reported in gure 2. The olloation
approahandthenonpolynomialapproahshowthesamerateofonvergene.
As evidentalowererrorisreahedbytheolloationapproahevenif,in this
ase,afullyonvergedsolutionanbeobtainedfortheproblemin bothases.
N
s ta ti s ti c s p e rc e n ta g e e rr o rs
10 20 30 40 50
10 -8 10 -6 10 -4 10 -2 10 0
10 2 err_mean (PC)
err_var (PC) err_var (Collocation) err_skew (PC) err_skew (Collocation) err_kurt (PC) err_kurt (Collocation)
Figure2: Comparisonbetweentheolloationapproahandthenonpolynomial
approahforthemonodimensionalproblem.
Inthefollowingsomemultidimensionalasesarereported withdimensions
uptothree. Twokindoffuntion areemployed
apolynomialfuntion
f pol (ξ) = Q d
i=1 (ξ i /2 + 1)
anonpolynomialfuntion
f np (ξ) = Q d
i=1 sin(πξ i )
.Inpartiular theresultsfor thepolynomialfuntion
f pol
in dimensiontwowith distributions (for eah dimension)
p 1 (ξ)
,p 2 (ξ)
andp 3 (ξ)
are reported,respetively,ingures3,4and5.
The results for the polynomial funtion
f pol
in dimension three with dis-tributions (for eah dimension)
p 1 (ξ)
andp 2 (ξ)
are reported, respetively, in gures6and7.For the non polynomial funtion only the ase with stohasti dimension
equal to twois analyzed. In this asethe three probability funtions are em-
ployed and the perentage errorsare reported respetively in thegures 8, 9
and10.
Theresultsobtainedareinaordtoourpreditions: thesolutiononverges
slowlyforhighermomentswithrespetto themeanandvarianeandtheon-
N
s ta ti s ti c s p e rc e n ta g e e rr o rs
0 100 200 300 400
10 -8 10 -6 10 -4 10 -2 10 0 10 2
10 4 err_mean (PC)
err_var (PC) err_var (Collocation) err_skew (PC) err_skew (Collocation) err_kurt (PC) err_kurt (Collocation)
Figure3: Comparisonbetweentheolloationapproahandthenonpolynomial
forthepolynomialfuntion
f pol
withprobabilitydistributionp 1
(d = 2
).N
s ta ti s ti c s p e rc e n ta g e e rr o rs
0 100 200 300 400
10 -7 10 -5 10 -3 10 -1 10 1 10 3 10 5
err_mean (PC) err_var (PC) err_var (Collocation) err_skew (PC) err_skew (Collocation) err_kurt (PC) err_kurt (Collocation)
Figure4: Comparisonbetweentheolloationapproahandthenonpolynomial
forthepolynomialfuntion
f pol
withprobabilitydistributionp 2
(d = 2
).vergene ismore sti for problemswith higher stohasti dimension and with
nonpolynomialfuntion orpdf.
Atually thehomemade ode we employedis asequential oneand is very
time demanding to obtain a fully onverged solution for more sti problems,
but we aspet to improvethe present resultswith a parallel implementation.
N
s ta ti s ti c s p e rc e n ta g e e rr o rs
0 100 200 300 400
10 -8 10 -6 10 -4 10 -2 10 0 10 2 10 4 10 6
err_mean (PC) err_var (PC) err_var (Collocation) err_skew (PC) err_skew (Collocation) err_kurt (PC) err_kurt (Collocation)
Figure5: Comparisonbetweentheolloationapproahandthenonpolynomial
forthepolynomialfuntion
f pol
withprobabilitydistributionp 3
(d = 2
).N
s ta ti s ti c s p e rc e n ta g e e rr o rs
0 500 1000 1500
10 -9 10 -7 10 -5 10 -3 10 -1 10 1 10 3 10 5
err_mean (PC) err_var (PC) err_var (Collocation) err_skew (PC) err_skew (Collocation) err_kurt (PC) err_kurt (Collocation)
Figure6: Comparisonbetweentheolloationapproahandthenonpolynomial
forthepolynomialfuntion
f pol
withprobabilitydistributionp 1
(d = 3
).Howeverasageneralruleweannotify,thatasweexpeted,asimpleolloation
ismoreeientintermofsimulationsinpratiallyalltheases. Howeverthe
presentapproahretainitsinterestinthepossibilityto obtainametamodelof
thesolutionandanestimationoftheonditionalstatistis.
N
s ta ti s ti c s p e rc e n ta g e e rr o rs
0 500 1000 1500
10 -8 10 -6 10 -4 10 -2 10 0 10 2 10 4 10 6
err_mean (PC) err_var (PC) err_var (Collocation) err_skew (PC) err_skew (Collocation) err_kurt (PC) err_kurt (Collocation)
Figure7: Comparisonbetweentheolloationapproahandthenonpolynomial
forthepolynomialfuntion
f pol
withprobabilitydistributionp 2
(d = 3
).N
s ta ti s ti c s p e rc e n ta g e e rr o rs
0 100 200 300 400
10 -8 10 -6 10 -4 10 -2 10 0 10 2 10 4
err_mean (PC) err_var (PC) err_var (Collocation) err_skew (PC) err_skew (Collocation) err_kurt (PC) err_kurt (Collocation)
Figure8: Comparisonbetweentheolloationapproahandthenonpolynomial
forthepolynomialfuntion
f np
withprobabilitydistributionp 1
(d = 2
).6 Conlusions and perspetive
Inthepresentworkanovelapproahhasbeenpresentedtoextendthepolyno-
mialhaosexpansiontotheaseofnonlassialdenedpdfs,i.e. pdfsthatfall
outsidetheso-alledWiener-Askeysheme. Thestrategyis basedonthelas-
N
s ta ti s ti c s p e rc e n ta g e e rr o rs
0 100 200 300 400
10 -9 10 -7 10 -5 10 -3 10 -1 10 1 10 3 10 5
err_mean (PC) err_var (PC) err_var (Collocation) err_skew (PC) err_skew (Collocation) err_kurt (PC) err_kurt (Collocation)
Figure9: Comparisonbetweentheolloationapproahandthenonpolynomial
forthepolynomialfuntion
f np
withprobabilitydistributionp 2
(d = 2
).N
s ta ti s ti c s p e rc e n ta g e e rr o rs
0 100 200 300 400
10 -8 10 -6 10 -4 10 -2 10 0 10 2
10 4 err_mean (PC)
err_var (PC) err_var (Collocation) err_skew (PC) err_skew (Collocation) err_kurt (PC) err_kurt (Collocation)
Figure 10: Comparison betweentheolloationapproahandthenon polyno-
mialforthepolynomialfuntion
f np
withprobabilitydistributionp 3
(d = 2
).sialPCapproahbutuniformequivalentdistributionsareemployedtore-map
the originalproblem in anuniform oneirrespetiveless of thetrueprobability
distribution. Thisapproaheventuallydegradestheonvergeneofthelassial
approah,in termofnumberofsimulationsrequiredtoestimatethestatistis,
ifalassialpdfisemployed. Thisisdue toaquadratureruleoptimalonlyin
theaseofpolynomialfuntionswithuniformdistribution. Howeverthisdraw-
bakisnotmuhinuentin realappliationsasesbeausethemodelfuntion
is,often, notpolynomial. Anotherdrawbaksouldemergeifoneomparethe
presentstrategytoabrutalforeolloationstrategyin whiheverystatistial
moments is deomposed in expetanies of thefuntion and all the funtions
itselfraisedto apowerequaltothedegreeofthemaximumstatistialmoment
required. Thislastapproahallowsto reduedramatiallythenumberofinte-
grals to beomputed. Anywaythe present strategy is motivated beausethe
advantagedespite to thehigheromputational ostis to provide, at thesame
time,aompletemetamodelofthemodelfuntionandaknownstrutureofthe
funtiononwhihispossibletoomputeonditionalstatistis. Thispossiblyis
notompletely explored in thisworkand onlythe rstorder onditionalvari-
anesare expliitlyshown. Atthepresenttime onlyanhomemadesequential
ode is at our disposal and this limits the possibility to ompute high order
statistis formore omplexproblems in higher dimension thantwo. Toallow
more real appliation ases, in whih thesingle ost of eah omputation an
be muh more expensive, we expet to really inrease the eieny oupling
the present strategywith aSmolyak algorithmto omputethe set ofquadra-
turepointsonwhihthesimulationsmustbeperformed. Intheaseofsmooth
modelfuntionsandprobabilitydistribution,forhighdimensionproblems,the
ouplingbetweenournovelnPCapproahandthesparsegridisstraightforward.
7 Aknowledgements
Remi Abgrallhas been partially supportedby theERC Advaned GrantAD-
DECCON.226316,whileGianluaGeraihasbeenfullysupportedbytheERC
AdvanedGrantADDECCON.226316. GianluaGeraialsoaknowledgethe
supportoftheAssoiatedTeam'AQUARIUS'whihprovidedthenanialsup-
portforafruitfulvisitattheStanfordUniversityattheendof2011.
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