Re eived:date/A epted:date
Abstra t Lu y-Ri hardson(LR)isa lassi aliterativeregularizationmethod
largelyusedfortherestorationofnonnegativesolutions.LRndsappli ations
inmanyphysi alproblems,su hasfortheinversionoflights atteringdata.In
theseproblems,thereisoftenadditionalinformationonthetruesolutionthat
isusuallyignoredbymanyrestorationmethodsbe ausetherelatedmeasurable
quantitiesarelikelyto beae tedbynon-negligiblenoise.
In this arti le we propose a novel Weakly Constrained Lu y-Ri hardson
(WCLR)method whi hadds aweak onstraintto the lassi alLR by
intro-du ing apenalization term, whose strength an be varied over avery large
A.Bu ini
DepartmentofMathemati alS ien es,
KentStateUniversity,
233MSB,1300LeftonEsplanade,
44242Kent,Ohio,
Tel.:+13306721481
E-mail:abu inikent.edu
M.Donatelli
DipartimentodiS ienzaeAltaTe nologia,
UniversitàdegliStudidell'Insubria,
ViaValleggio11, 22100Como,Italy, Tel.:+39-031-2386378 Fax:+39-031-2386209 E-mail:mar o.donatelliuninsubria.it F.Ferri
DipartimentodiS ienzaeAltaTe nologia,
To.S a.Lab,
UniversitàdegliStudidell'Insubria,
ViaValleggio11, 22100Como,Italy, Tel.:+39-031-2386251 Tel.:+39-031-2386294 Fax:+39-031-2386250 E-mail:fabio.ferriuninsubria.it
range.The WCLR method is simpleandrobustasthestandardLR, but
of-fersthegreatadvantageofwidelystret hingthedomainrangeoverwhi hthe
solution an be reliably re overed.Some sele ted numeri al examples prove
theperforman esoftheproposed algorithm.
Keywords Lu y-Ri hardsonAlgorithm
·
LightS attering·
Parti leSizing Mathemati sSubje t Classi ation (2000) 65R32·
78A46·
78A101Introdu tion
Inthisworkwe onsider the aseof aFredholmintegralequationoftherst
kind
I(θ) =
ˆ
K(θ, R) N (R)dR.
(1)where
I(θ)
representsthedataevaluatedattheindependentvariableθ
,N (R)
is the unknown fun tion that depends on the variableR
, andK(θ, R)
is a knownintegralkernelwith ompa tsupport.Thelatter onditionimpliesthatequation(1)isill-posed,meaningthatthesolutionisnotuniqueanddoesnot
depend ontinuouslyonthedata, i.e., smallperturbationsin
I
greatlyae t thesolutionN
.Wearegoingto onsiderinverseproblemsoftheform(1) omingfromlight
s attering methods in opti s [2,6,1518℄, where the main goalof theopti al
te hnique is to re over the parti le-size distribution
N (R)
whi h hara ter-izes thesampleunder investigation.Thusthe solutionN (R)
isdened to be positive(N > 0
)withapositivesupport(R > 0
).Amongthevarious s atter-ing te hniques, themost popular ones are Dynami LightS attering(DLS),Stati orElasti LightS attering(ELS) andMultiWavelengthTurbidimetry
(MWT). All of them an be easily implementedby using simple
experimen-tal setups(seeforexample[7℄andreferen estherein),with thepossibilityof
hara terizingsimultaneouslyaverylargenumberofparti les,the
hara ter-izationbeing arriedoutinsitu and almostreal time.Re entappli ationsof
these methods to parti le sizing an be found in Refs. [25,28℄ for the DLS
te hnique,in Refs.[21,30℄forELS,andRefs.[14,31℄forMWT.
Thegoalofane ient,wellperforminginversionalgorithmisthea urate
andfastre overyofthesampleparti le-sizedistributionoverthelargest
pos-siblerangeofparti leradii.Indeed,inversionalgorithmsareexpe tedtowork
prettywellonlywhentheparti lesizestobere overedliewithinagivenrange
[R
min
, R
max
]
,whi hdependsontherangeofthe[θ
min
, θ
max
]
independent vari-ablebeingprobed.Althoughwhat followsisof generalvalidity,in thispaperwewillfo usontheELSte hnique,where
I(θ)
representstheintensityofthe light s attered by the sample at various s attering anglesθ
. In the past we haveshown[12℄ thatthedynami alextensionof theR
−
range(i.e.,theratio[R
max
/R
min
]
)whi h an be probed,s alesproportionallyto[θ
max
/θ
min
]
and, therefore anberatherlimitedifthelatterratioisnotsu ientlylarge.avoidthepresen eofnoisein thedata,thedire tinversionof
A
,forinstan e be the MoorePenrose pseudoinverse, leads to very poor approximations oftheoriginaldesired
N
.Tore overameaningfulapproximationofthetrue so-lution, a ommon approa his to resortto regularization,i.e., use numeri almethodsthat omputeasolutionofanearbywell-posedproblem,see[3,9℄for
lassi alregularizationmethodsforinverseproblems.
Forlargeproblems,a ommonapproa histoadoptiterativemethodsthat
require only matrix ve tor-produ ts. Among these iterative pro edures, one
ofthemostpopularonesis undoubtedlythe lassi alLu y-Ri hardson(LR),
known also as Ri hardson-Lu y method [26,29℄, whi h has the remarkable
feature ofensuring nonnegativity ofthesolutions.LR is alsoquite simpleto
implement,robustagainstnoiseand, providedthat theiterativepro edureis
stoppedafteraproperly hosennumberofsteps,doesnotrequireany
parame-tertobeoptimized.Furthermore,itisthespe i natureofourproblemthat
suggests the usage of the LR method, mainly be ause the noise present on
thedataisnotadditive,but multipli ativewhiteGaussiannoiseasdes ribed
in Se tion4.5,and theoperator
A
isseverelyill- onditionedand underdeter-mined. These features suggest that methods relying on the minimization ofthe Eu lidean norm of the residual would not perform well on this spe i
problem. Moreover,in the onsidered setting, the knowledge of the norm of
thenoiseisnotavailableandonlysomestatisti alinformationonit anbe
re-trieved,implyingthatthe lassi aldis repan yprin iple annotbeemployed.
Thus,amethodlikeLRseemstobemoreee tivethanothermethods based
ontheminimization oftheEu lideannorm.
Ontheother side,theLRmethod isknownforbeingrelativelyslowand,
as mentioned above and reported in [12℄ 1
, for being not so e ient when
when therangeof re overableradiiis toolarge.Thelatterlimitation o urs
be ause,foranygivenangularrange
[θ
min
, θ
max
]
,asparti lesbe omesmaller andsmaller(R
≪ λ/θ
min
),theangulardistributionofthes atteredlighttends tobemoreandmoreuniform[I(θ
min
)/I(θ
max
)
∼ 1
℄,thus arryinglessandless informationon parti lesize.Conversely,forlargerand largerparti les(R
≫
λ/θ
max
), the angular distribution varies widely with a high signal dynami range [I(θ
min
)/I(θ
max
)
≫ 1
℄, but theshapeofI(θ)
tendsto beindependent onparti lesize[23℄.1
Afterthepubli ationof[12℄,itwasrealizedthatthemethod alledmodi ationofthe
Inthis paperweproposeanewmethod alled WeaklyConstrained
Lu y-Ri hardson (WCLR), whi h improves the lassi al LR method by adding a
weak onstraint to the true solution asso iated to a physi al property (the
parti levolumefra tion on entration)thatisknownor anbemeasuredwith
ratherhigha ura y.Theintrodu tionofthisadditionalknowledgea elerates
remarkablythe onvergen erateofthemethodand,atthesametime,largely
improvesthe qualityof therestoration.In parti ularit allowstoenlargethe
R
−
rangebymorethanoneorder ofmagnitude,apropertythat is ru ial in manyrealappli ations.Thepri etopayforaddingthe onstraintistheintrodu tionofadamping
parameter,
γ
, whi h has to be properly adjusted. However, this task is not riti alatallbe ausethestrengthofγ
an bevariedoveraverybroadrange and its optimal value an be easily found by exploiting a se ond physi alproperty(the parti le number on entration),whi hneedsto beknownonly
veryroughly.Notethatusingaweak ratherthananexa t onstraintisavital
feature of the WCLR method. Indeed, while imposing an exa t onstraint
has the advantage of requiring no damping parameter, its implementation
(by using lassi aloptimization algorithms for linear onstrained problems)
mightstillneedthetuningofotherparametersand,duetounavoidableerrors
alwayspresentintheestimateofthe onstraint,itdoesnotprovidene essarily
an improvement in the quality of the restoration. Conversely, our WCLR is
quite simple to implement, it is exible and robust against small (
.
±2%
) un ertaintiesasso iated tothe onstraintand, ex eptforγ
, doesnotrequire anyotherparametertobeset inthesamespiritofthe lassi alLR.This work is stru tured as follows. In Se tion 2 we give some physi al
details abouttheproblem weare goingtoanalyze. Inparti ular,Se tion 2.1
des ribesthedis retizationpro ess,whileSe tion2.2 onsidersthe onstrains
wearegoingtouse.Se tion3isdevotedtotheformulationofthemathemati al
modelandtothedenitionofournumeri almethod.Thelatteroneistested
and omparedwithLRonsomenumeri alexamplesin Se tion4.Se tion5is
devotedto on ludingremarksandfuturework.
2Physi al details
Inthisse tionwegivesomeinsightintothephysi alproblemwearegoingto
onsider,i.e.,theproblemasso iatedtotheinversionofelasti lights attering
(ELS) data, where the main goal is to re over the size distribution of the
parti lespresentinthesample.
A ordingto ELStheory[23℄,whenasamplemadeofpolydisperse
parti- les hara terizedbyarefra tionindexdierentfromthatofthesurrounding
mediumisilluminatedbyalaserlightofwavelength
λ
,partoftheradiationis goingtobes atteredatanglesdierentfromthein identdire tion.Ifthepar-ti les arehomogeneouslydispersed in themedium andtheir on entrationis
solowthatthey anbe onsideredasnon-intera ting,theangulardistribution
Fig.1 (a):normalizedbehaviorofthekernel
K(θ, R)
appearingin(1)asafun tionofthe s attering angleθ
for veparti les withdiametersd = 2R
ranging fromd = 0.01 µm
tod = 100 µm
;the normalizationissu hthatK(θ = 0, R) = 1
.(b):behavior ofthe kernel amplitudeK(θ = 0, R)
asafun tionoftheratioR/λ
.Thestraightlineswithslopes6
and4
indi atethatK(θ = 0, R)
growthsas∼ R
6
or
∼ R
4
,the rossovero urringat
R ∼ λ
.s attered bythesingleparti les [23℄.Thusthe systemis linearand
I(θ)
an bewritten as(1) whereθ
is the s attering angle (the angle between the in- identlaserbeamand thedire tionat whi hthes atteredlightisdete ted),N (R)
istheunknownnumber- on entrationdensity[cm
−3
µm
−1
℄ofparti les
ofradius
R
,andK(θ, R)
isthe(known)kernelofthesystem,representingthe intensitys atteredbyasingleparti leofradiusR
atangleθ
.Typi ally,I(θ)
is dete tedatanitenumberofanglesθ
i
(i = 1, .., n)
withinaboundedinterval[θ
min
, θ
max
]
.If the parti les are spheres, the kernel
K(θ, R)
is provided by the Mie theory [22℄,a ordingto whi h the angulardistribution ofI(θ)
s atteredby aparti le ofradiusR
ismostly onnedto thedira tion lobeθ
diff
∼ λ/2R
andI(θ)
amplitudestronglyin reaseswithparti leradiusasI
∼ R
6
forsmall
parti les(
R
≪ λ
)andI
∼ R
4
forlargeparti les(
R
≫ λ
).Figure1(a)reports anexampleof thebehaviorsofI(θ)/I(0) = K(θ, R)/K(0, R)
versusθ
overa rangeof[2
− 180 deg]
forparti lesofdierentdiametersd = 2R
fromd = 0.01
to100 µm
.Asone annoti e, forsmallparti lesI(θ)
tendsto beratherat, whereasforlargeparti lesI(θ)
exhibitsmanyos illationsandde aysbymany orderofmagnitudeoverthereportedθ
range.Atthesametimethezero-angle amplitudeI(0)
varies widely, passing fromI(0)
∼ 10
−11
atR/λ = 10
−2
toI(0)
∼ 10
8
atR/λ = 10
2
,seeFigure 1(b).Thus, itis learthattheinversion
of (1) might be ome an unbearable task when the parti le size distribution
N (R)
tobere overed ontainsparti leswithverydierentradii.2.1Dis retizationoftheFredholmIntegralEquation
We now des ribethe dis retization of (1). Let us onsider that only anite
numberof
θ
i
(i = 1, ..., n
) anbea essedexperimentallyandwithinalimited range[θ
1
, θ
n
]
. Thus, if the parti le size distributionN (R)
is approximated by ahistogram onstituted bym
bins(or lasses)delimited by theradiir
j
,j = 0, 1, ..., m
,theequation(1)be omesI(θ
i
) =
m
X
j=1
A
i,j
N
j
,
i = 1, 2, . . . , n,
(3)where
N
j
is the number on entration density[cm
−3
µm
−1
℄ of the parti les
belongingtothe
j
-th lassofwidth∆r
j
= r
j
− r
j−1
andA
i,j
=
ˆ
r
j
r
j−1
K(θ
i
, r) dr.
(4)Whenthe lassesarenarrowenough,we anpinpointthem intermsoftheir
averageradius
R
j
= (r
j
+ r
j−1
)/2
and width∆R
j
:=∆r
j
, where∆r
j
= r
j
−
r
j−1
.ThusN
j
∆R
j
representsthenumber on entrationofparti lesbelonging tothej
− th
lassandthetermA
i,j
/∆r
j
istheaverageintensitys atteredat angleθ
i
byasingleparti le withaverageradiusR
j
. Notethat (3)is aset ofn
linearequationsin whi h theleft-handsideI(θ
i
)
arethedataprovidedby theexperiment,thematrix entriesA
i,j
are known andN
j
aretheunknowns tobere overed.Although somewhatarbitrary,itisoften onvenientto hoosethe
r
j
grid points sothat, within the range[r
0
, r
m
]
, all them
lassesare hara terized bythesamerelativewidthα = ∆R
j
/R
j
.This anbea omplishedbys alingr
j
a ordingto thegeometri alprogressionr
j
= r
0
a
j
,
where
a = (R
m
/R
1
)
1/(m−1)
and
r
0
= 2R
1
/(1 + a)
. In this way theaverage radiusandthewidthofea h lasss aleasR
j
= R
1
a
j−1
,
∆R
j
= ∆R
1
a
j−1
,
j = 1, ..., m,
(5) thusα = 2[(a
− 1)/(a + 1)]
and fora & 1
,α
≈ a − 1
. A sket h layoutand dis retizations hemeofthe lassesisreportedinFigure2.Typi allyifwewantto overthree ordersof magnitudein size,i.e.
R
m
/R
1
= 10
3
with
α = 0.02
, approximatelym = 350
lassesarene essary.2.2Constraints
Theveryrst onstraintwe animposeisthat
N
j
> 0,
j = 1, . . . , m,
(6) This omesfromthesimpleobservationthatthenumberofparti le annotbenegative.
Amoreinteresting onstraintisrelatedtotheintegralof
N (R)
obtainingc
N
=
m
X
j=1
Fig.2 Dis retizations hemeofequation(1)
where
c
N
represents the parti le number on entration [cm
−3
℄, i.e., the
to-tal number of parti les ontained in the sample divided by the sample
vol-ume.This onstraint anbeappliedwheneverthenumberofparti les anbe
ounted, a somewhatdi ult task that an be arried outonly under some
experimental onditions.
Thelast onstraintisrelatedtotheparti levolumefra tion on entration
c
V
, whi h is given by the totalvolume o upied by the parti les dividedby thesamplevolumec
V
=
m
X
j=1
N
j
v
j
∆R
j
,
(8) wherev
j
=
1
∆R
j
ˆ
R
j
+∆R
j
/2
R
j
−∆R
j
/2
(4/3)πR
3
dR
(9)is the averagevolume of oneparti le belonging to the
j
th
lass. Clearly, for
verynarrow lasses(
∆R
j
/R
j
≪ 1
),v
j
≈ (4/3)πR
3
j
.Remark1 The onstraint(8)on
c
V
isofparti ularsigni an ebe auseinmost experimentsthevolume on entrationisaquantitythat anbemeasuredquiteeasilyandwithhigh a ura y.
Inourmethodwewouldliketoexploit both on entration onstraints(7)
and(8)(the positiveness onstraint,(6) ,beingfullledautomati ally,see
be-low),buttheyarenotequivalentfromaphysi alpointofview.Asmentioned
out above, whereas an a urate value of
c
V
an be easily obtained experi-mentally,theestimateofc
N
mightbesomewhattroublesomeandae tedby largeerrors. Thus, we propose aweakly onstrainedversionof theLRalgo-rithm basedon the
c
V
onstraintalone, and wewill use theestimate ofc
N
onlyfor ross- he kingtheself- onsisten yoftheinversionpro edure,i.e.,for3The Weakly Constrained Lu y-Ri hardson method
We now des ribe how the physi al model translates into the linear algebra
language.Thelinearsystem(3)is ompa tlyrewrittenas
AN = I
(10) whereA
∈ R
n×m
,N
∈ R
m
andI
∈ R
n
.Similarly,thethree onstraintsofSe tion2.2 anberewrittenas:
(i) From(6)
N
> 0
,meaningthat
N
j
> 0
,forj = 1, . . . , m
; (ii) From(7)c
N
= N
t
∆R,
(11) where0 < ∆R
∈ R
m
,with(∆R)
j
= ∆R
j
denedin(5)forj = 1, . . . , m
; (iii) From(8)c
V
= N
t
V
=
m
X
j=1
V
j
N
j
.
(12) where0 < V
∈ R
m
and
V
j
= v
j
∆R
j
,beingv
j
denedin (9).Thisinformationwillbeusedin thefollowingtodeneasimpleandee tive
iterativepro edureto omputeasolutionof(10),where,ex eptfromthe
pos-itiveness(i) ,the onstraints(ii)-(iii)arenotallstri tlysatised,butareused
toimprovethe omputedapproximationortoestimatepossibleparameters.
Notethatequations(11)and(12) anbeseenasweighted
ℓ
1
normbe ause bothV
and∆R
arenonnegative,sowe an denekNk
1,V
= N
t
V
,
kNk
1,∆R
= N
t
∆R.
AsstatedattheendofSe tion2.2,wearegoingtousedire tlyonlyaweighted
versionofthe onstraint(iii) .
Inordertoinsertthe onstraint(iii)weopportunelypadthematrix
A
and theright-handsideI
.Letγ > 0
beaxed realnumberanddeneϕ =
hA
i,j
i
hV
j
i
,
(13) wherehA
i,j
i =
1
N M
P
i,j
A
i,j
andhV
j
i =
1
N
P
j
V
j
arethearithmeti averagesoftheentries ofthematrix
A
andtheve torV
,respe tively.Wedene˜
A =
A
γϕV
t
and˜I =
I
γϕc
V
.
(14)Notethat,sin ethefa tor
γϕV
j
= γ < A
i,j
> (V
j
/ < V
j
>)
appearingin(14), musthavethesamedimensionalunitsas< A
i,j
>
,γ
is orre tlya dimension-lessparameter.Asa onsequen e,itsee tof (14)isindependentontheunitstheinitialguess
N
0
> 0
,the
k + 1
approximatedsolutionofequation(15) an bere ursivelywrittenin termofthek
−
iterateasN
k+1
=
N
k
a
◦
A
˜
t
·
˜I
˜I
k
!
,
k = 0, 1, . . .
where•
•
and• ◦ •
are respe tivelytheentry-wisedivision andmultipli ation and• · •
is the usual matrix-ve tor multipli ation. The ve tora
∈ R
m
is denedasa
j
=
n+1
X
i=1
˜
A
t
j,i
=
n
X
i=1
A
i,j
+ γϕV
j
,
j = 1, . . . , m,
(16) and˜I
k
is˜I
k
= ˜
AN
k
=
AN
k
γϕ
N
k
1,V
.
Letus onsiderthe
j
− th
omponentofN
k+1
:N
j
k+1
=
N
k
j
a
j
"
˜
A
t
·
˜I
˜I
k
#
j
=
N
k
j
a
j
ξ
j
,
(17) thefa torξ
j
isξ
j
=
n+1
X
i=1
˜
A
t
j,i
˜I
i
˜I
k
i
=
n+1
X
i=1
˜
A
i,j
˜I
i
˜I
k
i
=
n
X
i=1
A
i,j
I
i
I
k
i
+ γϕV
j
c
V
c
k
V
,
(18) withc
k
V
=
N
k
1,V
.Combining(16)and(18)with(17),weobtainN
j
k+1
= N
j
k
P
n
i=1
A
i,j
I
I
k
i
i
+ γ
hA
i,j
i
hV
V
j
j
i
c
c
V
k
V
P
n
i=1
A
i,j
+ γ
hA
i,j
i
V
j
hV
j
i
V
j
,
j = 1, . . . , m.
(19)where wehaveexpli itlyreportedthe expressionfor
ϕ
givenin(13). We an seethat onstraint(iii)isnotblendedwiththeotherterm,itisde oupledfromthedatattingpartandisweightedby
γ
.Moreover,thenonnegativityofN
k
issimplypreservedstartingwith
N
0
> 0
,e.g.,
N
0
= 1
,where
1
representsthe ve torwithentries allequalsto1
.3.1Heuristi interpretation
We now want to givean heuristi interpretation of theformulation of (15).
A standardapproa h forpassingfrom a onstrainedleast squareproblem to
anun onstrainedproblemisthewell-knownquadrati penalizationte hnique
[5℄. In our ase, onsidering the onstraint (iii) , we obtain the minimization
problem
min
N
kAN − Ik
2
2
+ (γϕ)
2
kNk
1,V
− c
V
2
,
(20)where
k · k
2
denotes the Eu lidean norm and(γϕ)
2
is the penalization
pa-rameter.This anbeseenasaregularizedversionof theproblem(2), where
theparameter
(γϕ)
2
balan esthe trade o betweenthedata tting andthe
penalizationterm. Dene
Ψ (N) =
kAN − Ik
2
2
+ (γϕ)
2
kNk
1,V
− c
V
2
= N
t
A
t
AN
− 2N
t
A
t
I
+ I
t
I
+ (γϕ)
2
N
t
VV
t
N
− 2c
V
N
t
V
+ c
2
V
.
ThegradientofΨ (N)
is∇Ψ(N) = 2[A
t
AN
− A
t
I
+ (γϕ)
2
(VV
t
N
− c
V
V
)].
Assumethat
V
j
6= 0
forallj
.ThenΨ (N)
is oer ive.Infa tΨ (N)
≥ γϕ
min
j
{V
j
}N
t
1− c
V
2
→ ∞
askNk
2
→ ∞.
Thustheminimumof
Ψ
exists,byWeierstrass theorem,andsatises∇Ψ(N) = 0.
(21)Thefun tional
Ψ
is onvex,butnotstri tly onvex,sin e,ingeneral,N (A) ∩
N (
Vt
)
6= {0}
,wherebyN (A)
wedenotethenullspa eofA
.Thus, ondition (21) is only ne essary and the minimum is not unique. However, sin e thefun tionalis oer ive,wehavethattheminimum
N
∗
of
Ψ
satiseskN
∗
k
2
<
∞
. InotherwordswehaveproventhefollowingProposition 1 Thefun tional
Ψ
denedabove admitsaglobalminimizerN
∗
su hthat (a)kN
∗
k
2
<
∞
; (b)∇Ψ(N
∗
) = 0
.Condition(21) anberewrittenequivalentlyas
A
t
γϕV
A
γϕV
t
N
= A
t
γϕV
I
γϕc
V
,
(22)Re allingthedenitionsof
A
˜
and˜I
,we anseethat(22)issimplythenormal equations of (15). This, oupled with (i) , leadsto the idea of looking for aLet us all
N
γ
the nonnegativesolution of (22)obtained with a ertain
hoi e of
γ
and suppose to know exa tlyc
N
. Thus, we expe t that the best hoi e forγ
istheonethat,besideprovidingthebestre onstru tion forN
γ
, minimizesalsotheerroronc
N
.Therefore,we hooseγ = γ
opt
su hthatγ
opt
= arg min
γ
{|c
N
− kN
γ
k
1,∆R
|}.
(23)
In pra ti e, as we will see in Se tion 4, the hoi e rule (23) is not so stri t
be ausethere is alargerange of
γ
-valuesaroundγ
opt
where the re onstru -tion is equallygood and even avalue ofγ
veryfar fromγ
opt
would provide a urateresults.Thisfeatureisoffundamentalimportan ebe ause,wheneverthe onstraint
c
N
isnotknownand anbeonlyroughlyestimated(asitmight happen experimentally),γ
opt
annot bedetermined with high a ura y and the ondition(23)would beinappli able.Toobtainanestimationof
γ
opt
we omputeN
γ
forasmallsetofpossible
γ
andsele ttheonethat minimizes|c
N
− kN
γ
k
1,∆R
|
.Summarizing,ourweakly onstrainedLR(WCLR)algorithmisthe
follow-ing:
1. x
N
0
= 1
andasmallsetofpossiblevaluesfor
γ
; 2. omputeN
γ
foreveryγ
;3. hoosethesolution
N
γ
opt
orrespondingtoγ
opt
dened in(23).4Numeri al Examples
Inthisse tionwereportsomenumeri alexamplesaimedatas ertaininghow
our algorithm performs against the lassi al LR method, i.e., when
γ = 0
. Wewillalso showhowto ndtheoptimalvalueγ
opt
, onsistentlywith what des ribedabove.4.1GenerationofmatrixA
The
n
×m
matrixA
was omputedbynumeri allyintegratingequation(4)with thekernelK
providedbytheMietheory[22℄andillustratedinFigure1.The numberofangleswasn = 100
,s aled a ordingto ageometri alprogressionwith
θ
min
= 2 deg
andθ
max
= 180 deg
.Thebinsforthere overeddistribution were also hosen a ordingly to a geometri al progression (see Se tion 2.1)with
R
min
= 10
−3
µm
and
R
max
= 10
3
µm
andtheirnumberwas
m = 600
.In thiswayallthebinswere hara terizedbythesamerelativewidth∆R
j
/R
j
≈
0.023
.4.2Generationofarti ialtestdata
Thegenerationofarti ialtest datawas arriedoutbysupposingtoknowa
truesolutionforthesystem
N
true
and omputingthenoise-freedataasI
true
= AN
true
.
Then the real data were obtained by adding to
I
true
a (fra tional) random whiteGaussiannoise,sothatthenoiselevelisproportionaltoI
true
and inde-pendent from point to point. If we indi ate withǫ
the fra tional noiselevel, thenoisyI
be omesI
= I
true
◦ (1 + ǫe) ,
(24) wheree
is ave torwhose entries are realizationsof a randomvariable su h that(e)
j
∼ N (0, 1)
.Typi alvaluesforǫ
arein theinterval[10
−3
, 10
−2
]
.
4.3Inversionpro edure andstopping riteria
Thearti ialtestdatain(24)wereinvertedbyxingavalueoftheparameter
γ
andusingtheiterativealgorithmgivenby(19).Theiterativepro edurewas stoppeda ordingto thefollowing riteria:(1) Firstofallweimposeaminimumnumberofiterations
k
min
= 10
5
,whi his
ne essaryfortheWCLR(ortheLR)algorithmtoworkproperly.The
min-imumnumberofiterations
k
min
wasestimatedbyinvertingnoiselessdata and he king that10
5
iterations are enough for retrieving the expe ted
distributionwith high a ura y (
RRE . 10
−2
, see below, Se tion 4.4).
Wealso he kedthat fornoisydata withnoiselevelstypi alof our
prob-lem (
∼ 1%
) when the pro edure would prefer to stop at a number of iterationsk < k
min
(seebelowpoints3.and 4.),for ingit to ontinue up tok
min
= 10
5
doesnotspoilsigni antlythequalityofthedistribution.
(2) Wealso imposea maximumnumberof iterations
k
max
= 10
6
, whi h
en-suresthat the inversionstops evenwhen the riteria belowreported are
notmet.
(3) Forany
k
min
< k < k
max
thepro edureisstoppeda ordinglytoarelative dis repan y prin iple,whi hisamodiedversionofthe lassi aldis rep-an yprin iple, largelyusedwith iterative regularizationmethods [9℄.As
relativedis repan yparameterwedenethequantity
ǫ
k
=
1
√
n
I
k
− I
I
2
,
(25)unknownandhen ethe lassi aldis repan yprin iple annotbeused.
A ordingto (25),thealgorithm wasthereforestoppedafter
k = k
∗
iter-ationssothat
ǫ
k
∗
≤ ǫ,
(26)where
ǫ
isthefra tionalnoiselevelintrodu edin(24).(4) Finallywhenever,for
k
min
< k < k
max
, ondition(26) isnotmet butǫ
k
attains aminimum and begins to in rease (the sequen e{ǫ
k
}
de reases forsmallvaluesofk
,butisnotalwaysmonotoni de reasingforlargek
), thepro edureisstoppedin orresponden eoftheminimum.Sin ethevalueof
ǫ
k
anos illate,wesaythatwehaverea hedaminimum forǫ
k
ifǫ
k
< ǫ
k+1
< ǫ
k+2
< . . . < ǫ
k+10
, i.e., ifǫ
k
has in reasedfor10
onse utiveiterations.Whensu h a minimumis rea hedbefore
k
min
, the pro edure is stopped atk = k
min
.Inthefollowingwewilldenotewith
K
it
thenumberofiterationsatwhi hthe pro edureisa tuallystoppedand the orrespondingǫ
K
it
willbe alledMean RelativeStandardDeviation(MRSD).4.4Evaluationparameters
Thea ura y ofthe inversionalgorithm wasevaluatedby omparingthe
re-trieveddistributionwiththetrueone.However,sin efromaphysi alpointof
view,volume (ormass)distributions aremu hmoresigni antthan number
distributions, we ompared retrieved and true distributions on the basis of
volume-fra tiondensitydistributions,denedas
φ(R) = N (R)v(R),
here
φ(R)
hasthedimensionsof[µm
−1
℄.
Forassessingthea ura yoftheinversionpro edure,wedenea
γ
-dependent RelativeRestorationError(RRE)asRRE(γ) =
kφ
γ
− φ
true
k
2
kφ
true
k
2
whi h orrespondstotherelativeaveragerootmeansquare(
r.m.s.
)deviations betweentheretrievedandtruemassdistributions.Similarly,for assessingthea ura y onthe re onstru tionof the two
pa-rameters
c
N
andc
V
that hara terize the true distribution, we dene the quantitiesD
N
(γ) =
k
N
γ
k
1,∆R
− c
N
c
N
andD
V
(γ) =
k
N
γ
k
1,V
− c
V
c
V
,
whi hrepresenttherelativeerrorsbetween
c
N
andc
V
andthe orresponding re overedparameters.4.5Numeri alresults
Inthefollowingnumeri altests,theWCLRandLRalgorithmswere ompared
forseveralvaluesof
γ
inagivenrangeofre overableradii.Thelatteronewas hosento beasubset oftheoriginalrangedened in Subse tion4.1, so thatR
max
/R
min
= 100
.Forea hγ
,thetestswererepeated30
times,withdierent noiserealizations(ofthesameǫ
level).Test1 Inthersttestweshowthat,whenthedistributiontobere overedis
hara terizedbyparti lesthatprodu esignalswhosefeaturesare:(a)
asymp-toti ally onstantatlowanglesand(b)exhibitadynami rangebetweenrst
and lastangle of severalorder of magnitudes(see
d = 0.1 µm
ord = 1.0 µm
urves in Figure 1(a)),the original LR andour WCLR algorithms arequiteequivalent.Tothisaim,wesele tedastruenumberdistribution
N
true
a Gaus-sian enteredinthemiddleofthere overablerange[R
min
, R
max
]
,i.e.,withan averagevaluehRi = 1 µm
andstandarddeviationσ
R
= 0.1 µm
.Theparti le number on entrationwas(arbitrarily) hosentobec
N
= 10
16
cm
−3
andthe
r.m.s.
noiseleveladded to thedata wasǫ = 0.01
.Theinversionwas arried outbytrimmingthere overableparti leradii intherange[0.1 µm
− 10 µm]
, so that number of bins wasm = 200
. Correspondingly, the matrix used in thistestwasobtainedbysele tingapropersubset(100
× 200)
oftheoriginal(100
× 600)
matrix omputedat se tion4.1.Thevalueofγ
rangesfromzero (originalLR)toγ = 10
6
and
K
it
= 10
6
.
Thendingsofthistestshowthatouralgorithmperformsequallywell
in-dependentlyofthe
γ
−
value(0
− 10
4
)anditsperforman eswerequitesimilar
totheones providedbytheoriginalLR algorithm.ThisisshowninFigure 3
wheredatare onstru tionsandaveragere overeddistributionsarehighly
a - urate and, asmatter of fa t, indistinguishable between our algorithm (run
with
γ = 1
)andthe lassi alLRalgorithm(γ = 0
).Test 2 Theee tive dieren ebetweenthe two algorithmsbe omes evident
onlywhentheparti lesare losetotheboundariesofthe
[R
min
, R
max
]
range. Forthisse ondtestwesele tedaGaussiandistribution hara terizedbylargeFig.3 Test1:ComparisonbetweentheoriginalLR(bluesymbols)andourWCLRalgorithm
(redsymbols)runwith
γ = 1
foraGaussiandistributionwithanaveragevaluehRi = 1 µm
andstandarddeviationσ
R
= 0.1 µm
.(a)Re onstru ted(symbols)andtrue(line)signals. (b) Re onstru ted (symbols)and true (line) distributions. The two algorithmsperformsequallywelland,asmatteroffa t,bothresults(a)and(b)arealmostindistinguishable.
parti les,i.e., with
hRi = 100 µm
andσ
R
= 10 µm
.Thenoiseleveladded to the data wasǫ = 0.01
, the inversion was arriedout in the range[10 µm
−
1000 µm]
(sothatm = 200
),andγ
wasvariedin therange[10
−2
− 10
7
]
.
Dierently from the rst test, the ee t of hanging
γ
is quite relevant, as shown in Figure 4 where the behaviors of the parametersK
it
, whi h we re all that denotes the numberof iterations, (a), MRSD (b), RRE ( ),D
N
(d), andD
V
(e) arereported asafun tion ofγ
.First of allweobservethat thereisabroadrangeofγ
∼ [10
−1
− 10
5
]
wheretheinversionpro edurewas
stoppedatanumberofiterations
K
it
≤ 10
6
(seeFigure4(a)).Correspondingly,
withinthisrange,there onstru tionparameter
M RSD
(seeFigure4(b))was omparablewiththenoiseleveladdedtothedata,meaningthattheiterativepro edurewasmu hfasterandstoppeda ordinglytotherelativedis repan y
prin iple(26).
Then,whereas
D
V
(seeFigure4(d))de reasesmonotoni allywith in reas-ingγ
(whi h is onsistentwith thefa t that thestrongerthe onstraint,the higherthea ura yofitsre overedvalue),theparametersdes ribingthea u-ra yoftheretrieveddistribution,
RRE
(seeFigure4( ))andthea ura yon there overednumber on entration,D
N
(seeFigure4(e)),exhibitverybroad valleys whose at regions over almost the same range ofγ
∼ [10
1
− 10
5
]
.
Thus,the hoi eofanoptimalvaluefor
γ
isnot riti alat allandanyvalue hoseninthe entralpartofthisinterval(forexampleγ
opt
∼ [10
2
−10
4
]
)leads
bothto small errors in the re overyof
c
N
and to verya urate distribution re onstru tions,as shownin Figure 5(e-f-g). Conversely,for valuesofγ
out-sidethisrange,there overyofc
N
be omesin reasinglylessandlessa urate and,atthesametime,thedistributionsaremoreandmorepoorlyre overed,asshownin all theotherpanelsof thegure.Inparti ular, wewould liketo
pointouttheremarkablemismat hingbetweenthetruedistribution andthe
onere overedinFigure5(a),showingthat the lassi alLR algorithm(
γ = 0
) istotallyunabletoperformsu hatask.Fig. 4 Test 2: Behavior as a fun tion of
γ
of the average parametersK
it
(number of iterations)(a),MRSD(b),RRE ( ),D
N
(d),andD
V
(e)foraGaussiandistributionwithhRi = 100 µm
andσ
R
= 10 µm
.Theerror bars arethe standard deviationsasso iatedto the various parametersderivingfromthe noise(ǫ = 0.01
)presentonthedata (error bars largerthanthedatapointsarenotdisplayed).Finally,wewouldliketopointoutthattherathersimilarbehaviorsbetween
RRE
andD
N
guaranteesthat,inarealexperimentwheretheparameterRRE
annotbemeasuredbe auseφ
true
(R)
isnotknown,theoptimalrangeforγ
opt
anbeinferredbylookingatthebehaviorofD
N
(Figure4(d)).Thefa tthat su harangeisremarkablybroad(∼ 2 − 3
ordersofmagnitude)ensuresthat evenahugeun ertaintyonthevalueofc
N
wouldnotae t signi antlythe a ura ywithwhi hφ
true
(R)
willbere onstru ted.Test3 Inthistestwesele tedadistribution losetotheleftsideoftherange,
namely aGaussian with
hRi = 0.05 µm
andσ
R
= 0.005 µm
.In this ase, as shown inFigure1,theI(θ)
dataareratherat;therefore,fornot orrupting ompletelytheirbehavior,thenoiseleveladdedtothedatawasǫ = 0.001
.The inversionwas arriedoutintherange[0.005 µm
− 0.5 µm]
(sothatm = 200
), andγ
wasvariedintherange[10
−7
− 10
2
]
.
Figure6showsthebehavioroftheparameters
K
it
(Numberofiterations) (a), MRSD (b),RRE ( ),D
N
(d), andD
V
(e), whereasthe omparison be-tweenthere overeddistributionandφ
true
(R)
isshown inFigure 7varyingγ
in therange[10
−6
− 10
3
]
. As for the large parti les, there is an even larger
optimalrange
γ
opt
∼ [10
−3
− 10
1
]
,where onvergen erateisfasterand both
distributionre onstru tionand
c
N
re overyareverya urate.Were allthatγ
opt
an be safely identied by the riterion (23) thanks to the very broad andshallowminimumregionof the urveofD
N
inFigure 6(d).Finally,noteFig.5 Test2:Comparisonbetween theaveragere overeddistributions(redsymbols)
ob-tainedwithouralgorithmatvarious
γ
-values(γ = 0
isLR)andatrueGaussiandistributionφ
true
(R)
withwithhRi = 100 µm
andσ
R
= 10 µm
.Theerrorbarsarethestandard devia-tionsasso iatedtothebinsofthere overedhistogramduetothenoise(ǫ = 0.01
)presents inthedata.that,also in this ase, theoriginal LR algorithmis totallyunable to re over
thetruedistribution(seeFigure7(a)).
4.6Errorsonthe
c
V
onstraintInthis se tionwereportanexampleof theee ts ofsmallsystemati errors
onthe onstraint
c
V
withrespe ttothequalityofthere overeddistributions. We investigated the spe i ase of the true distribution used in Figure 7,i.e., aGaussian distributionwith
hRi = 0.05 µm
andσ
R
= 0.005 µm
,andwe supposedtohaveerrorsδc
V
varyingwithinarangeof±10%
.Thenforanyxed valueofγ
andweinvestigatedhowthere overeddistributions deterioratesasδc
V
isin reased. Thisanalysis was arried outfollowingthe samepro edure des ribed forthe previoustests, andwasrepeated for8
dierent valuesofγ
spanningtherangeγ
∼ [10
−5
− 10
2
]
(
1
pointperorderofmagnitude). Themain result is summarized in the rst panel of Figure 8, where thebehaviorof the parameter RRE is reported as a fun tion of the per entage
error
δc
V
. As expe ted, within the optimal rangeγ
opt
∼ [10
−3
− 10
1
]
, the
minimum of RRE o urs at zero error and in reasesas
δc
V
be omes larger andlarger,butas longasδc
V
.
±2%
,itsvalueremains.
2
− 3 × 10
−2
.
This
trendis learlynotfollowedbyvaluesof
γ
thatareoutsidethisoptimalrange be ause,evenat zero errorasshown in Figure 6(a), theinversionalgorithmFig. 6 Test 3: Behavior as a fun tion of
γ
of the average parametersK
it
(a), MRSD (b), RRE ( ),D
N
(d), andD
V
(e) fora Gaussian distributionwithhRi = 0.05 µm
andσ
R
= 0.005 µm
.withhRi = 100 µm
andσ
R
= 10 µm
.The error bars are the standard deviationsasso iatedtothevariousparametersderivingfromthenoise(ǫ = 0.001
)present onthedata(errorbarslargerthanthedatapointsarenotdisplayed).Fig.7 Test3:Comparisonbetween theaveragere overeddistributions(redsymbols)
ob-tainedwithouralgorithmatvarious
γ
-values(γ = 0
isLR)andatrueGaussiandistributionφ
true
(R)
withwithhRi = 0.05 µm
andσ
R
= 0.005 µm
.Theerrorbarsarethestandard de-viations asso iatedto thebinsofthe re overedhistogram dueto the noise(aǫ = 0.001
) presentonthedata.Fig. 8 Ee ts ofsystemati errors on the
c
V
onstraintwith respe tthe quality ofthe re overeddistributionsinthe aseofatrueGaussiandistributionφ
true
(R)
withwithhRi =
0.05 µm
andσ
R
= 0.005 µm
: (a)Behavior of RRE versus the per entage errorδc
V
;(b) behavior of MRSD versusthe per entage errorδc
V
;( )-(d)-(e): omparisonbetweenthe truedistribution(solidline)andtheaveragere overeddistributions(redsymbols)obtainedwith
γ = 10
−
2
and
−5%
,0%
and+5%
per entageerrors.Thestandarddeviationsasso iated tothe binsofthere overedhistogramsareduetothe noise(aǫ = 0.001
)presentonthe data.is not ableto work properly. The other importantparameter des ribingthe
performan esoftheinversionalgorithminpresen eofsystemati errorson
c
V
isthebehaviorofMRSD(seeFigure8(b)).Asshown,withintheoptimalrangeγ
opt
∼ [10
−3
− 10
1
]
andforerrors.
±5%
,alltheMRSD valuesare ompatible with the fra tional statisti al errors on the data (ǫ = 10
−3
). Outside these
ranges,MRSD tendstoin reasebe ause onvergen eissloweddownand
10
6
iteration are not su ient or be ause signal re onstru tions are very poor
whatsoever.
InthelastthreepanelsofFigure8wereportanexampleofthedistributions
re overed for
γ = 10
−2
at errors on
c
V
equal to−5%
,0%
and+5%
. As expe ted,the entraldistribution(paneld,0%
error)mat hesverya urately the input ones (RRE≈ 8.7 × 10
−3
), whereas the other two are learly less
a urate, beingRRE
≈ 3.2 × 10
−1
for the
−5%
errorand RRE≈ 8.8 × 10
−2
forthe
+5%
error,butstill verymeaningfulfromaphysi alpointofview.5Con lusions
Inthispaperwehaveproposedasimpleandee tivevariantoftheLRmethod
by addinga weak onstraintto be imposed asa penalty term onthe
re ov-eredsolution.Thenewmethod, alledWeakly ConstrainedLu y-Ri hardson
(WCLR), wasapplied and tested on the inversionof simulated elasti light
volume-size,
φ
true
(R)
, distributions of the parti les omposing the sample over the largestpossibleintervalof parti lesizes.Forthisproblem,there aretwophysi al onstraintsrelatedto the
knowl-edgeoftheparti lenumber,
c
N
,andvolume,c
V
, on entrations,whi h orre-spond,mathemati ally,to theintegralofN
true
(R)
andφ
true
(R)
,respe tively. Both onstraints an be determined experimentally but, whereasc
V
an be measured with high a ura y, the estimation ofc
N
anbeae ted by large errors.Thus in this paperweused asa onstraintonlyc
V
andexploitedc
N
fordeterminingaaposteriori riterionforadjusting thestrength,γ
,ofc
V
.By the use of extensive numeri al simulations, we have shown that the
optimal value
γ
opt
, i.e., the onethat provides the highesta ura ies in the re overyof bothc
N
andφ
true
(R)
(orN
true
(R)
),isnot riti al at allbe ause there isabroadrange(∼ 2 − 4
ordersofmagnitude)ofγ
-valuesaroundγ
opt
where bothrestorations are equally good. Thus, in areal experiment whereφ
true
(R)
isnotknown,theoptimalγ
opt
anbeinferredonlybylookingatc
N
and, thanksto thefa t that theγ
-rangeis sowide, even ahuge un ertainty onthevalueofc
N
wouldnotae tsigni antlythea ura yonthere overed distributions.We have also provided a new proto ol for stopping the iterative
pro e-dure,whi hisbasedonthefour riteriades ribedinSe t.4.3.Althoughsu h
riteria relyon the hoi e of the twoparameters
k
min
andk
max
whi h for e thepro edureto stop atk
it
sothatk
min
< K
it
< k
max
, thea tual valuesofK
it
veryrarelyare astontheextremesofsu h arange.Thus,theparti ular hoi efork
min
andk
max
doesnotae ttheresultsofthemethod.Itmustbe said,however,thatthetuningofk
min
isalittlebittri kybe ause onvergen e dependson thefeaturesof thedistributionto bere overedand, atthe sametime,onthenoiselevelpresentonthedata.Inour asewhere su halevelis
∼ 1%
orless,wefoundthatfornottoonarrowbellshapeddistributions (rela-tivewidthσ/ < R >
∼ 10%
orlarger)theuseofasinglevaluek
min
= 10
5
was
areasonable ompromise.Intheextremelyrare asethatthebestrestoration
isobtainedataniterationlowerthan
k
min
,wedonotobservetheinsurgen e ofartifa ts, ortheyareat leastfairly weak, be auseWCLR algorithm hasaverystable onvergen e,espe ially againstreasonable levels (
∼ 1%
). In any ase,forhighernoiselevels,aprepro essingdenoisingpro edure ouldalwaysbeapplied.In on lusiontherefore,although
k
min
ouldhavebeenoptimized from aseto ase,thesinglevaluek
min
= 10
5
allowedustore overa urately
distributions spanning the entire
[R
min
, R
max
]
range, without introdu ing a furtheradjusting parameterinthepro edure.Ournumeri alsimulationsshowthat,whentheparti lesizesto be
re ov-eredliewithinarangeextension omparablewiththat ofthemeasurements,
WCLR and LR are fairlyequivalent:they areboth simple,robustand,
pro-vided thatthe iterativepro edure isstopped after alargeenoughnumberof
steps, equallya urate. The only slightdieren e is that, whereas LR truly
requires no adjusting parameter, in the ase of WCLR, the only adjustable
parameterwould be
γ
, but asmentionedabove,it anbevariedoversu h a largerangeofvaluesthat,asamatteroffa t,doesnotneedtobeoptimized.errors on the knowledge of the onstraint
c
V
with respe t to the quality of there onstru ted distributions. Ourndings showthat, aslongastheerroron
c
V
is within±2%
, the quality of the re onstru ted distributions is well preservedandtheuseofaweak onstraintisadvantageouswith respe tto astrong onstraint.Thisfeatureisfundamentalinpra ti alappli ationswhere,
typi ally,therelativea ura yon
c
V
isoftheorderofafewper ents. AswestatedintheIntrodu tionthenatureoftheproblemitselfsuggestedthat theLR algorithmwouldhavebeenagood hoi e, whileother methods,
inparti ulartheoneswhi hreliesontheminimizationoftheEu lideannorm,
would havebeeninee tive.
Themaindrawba koftheproposed approa hisstilltherequirementofa
fairlyhighnumberofiterations,eventhoughwehaveshownthatthenumber
ofiterationsrequiredbyWLCRismu hsmallerthantheonerequiredbythe
standardLRmethod. However,thedimensionoftheproblem athand,while
notsmall,isnottoolarge(asseenintheexamplesinSe tion4)andthusthe
overall omputationeortislimitedevenwhenahighnumberofiterationsis
required.
Itwillbesubje toffuturestudiesthe ombinationofthete hniques
pro-posedin this paperwithmoree ientmethods from theliterature,starting
from the work in [8,27℄. In parti ular, it would be interesting to insert the
methods from[13℄ in ourframework,aswell astheto ombine ourapproa h
withModulus-Methodforill-posedproblems, see[1℄andreferen estherein.
Finally, we would like to point out that variants of the lassi al
Lu y-Ri hardson,likethosein [4,24℄, ouldbeusefulforfurther improvingour
al-gorithm.Wewouldalsoliketostressthat,althoughinthisarti leourWCLR
methodhasbeentestedanditsperforman esas ertainedforthespe i
opti- alproblemrelatedtotheinversionoftheelasti lights atteringdata,the
pro-posemethod anbeinprin ipleappliedtoanyotherproblemwheresome
on-straintsasso iatedtointegralsofthedistribution tobere overedareknown.
Examplesofsu hproblemsareagainintheeldsofopti swiththete hnique
known asmulti-spe tral extin tion turbidity [10,11℄ or in the eld of
stere-ology,aninterdis iplinarymethodologythat is on ernedwiththere overing
of the 3D properties of asample from its 2D se tions (see for example [20℄
and referen es therein). Work is in progress for extending WCLR to these
6A knowledgments
The author would like to thank the reviewers for their insightful omments
thatgreatlyimprovedthereadabilityandtheoverallqualityofthiswork.The
work of thersttwoauthorsis supported in partbyMIUR -PRIN2012 N.
2012MTE38NandbyagrantofthegroupGNCS ofINdAM.
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