.14% duke.edu idc.ac.il

Size: px
Start display at page:

Download ".14% duke.edu idc.ac.il"

Transcription

1 .14% duke.edu idc.ac.il

2

3

4

5 .54%.01%.18%.14% 2.3%.05%

6

7 d t = 1,, T d i j j = 0 J i,d,t J i,d,t+1 = J i,d,t j j a i,d,t j i t d j t d μ i,j,d i j γ i > 0 ε i,j,d,t t i j t d U i,j,d,t = μ i,j,d γ i + ε i,j,d,t

8 U i,0,d,t = ε i,0,d,t μ i,j,d j μ i,j,d i j d z j ν j,d v i μ i,j,d = (z j + ν j,d) v i z j = v i v i = 1 z j = 1 z j = 1 j z j ν j,d j ν j,d j d ε i,j,d,t ν j,d N (0, τ 1 ν ) τ 1 ν l d ν j,d j l j j s j,l,d s j,l,d ν j,d N (z j + ν j,d, τ 1 s )

9 s j,l,d j l d z j + ν j,d j l j j τs 1 ν j,d t d z j ν j,d ω l,j l j ω l,j ω j,l ω τ s n i,j,d,t E (μ i,j,d I i,d,t) = z j v i + ( τ s n i,j,d,t + τ ν ) ( s i,j,d,t z j) v i t d I i,d,t {n i,d,t, s i,d,t, h i,d,t} n i,j,d,t j t s i,j,d,t

10 j h i,j,d,t j I i,d,t = {n i,d,t, s i,d,t, h i,d,t} t z j v i t s i,j,d,t v i τ s τ 1 ν n i,j,d,t n i,j,d,t = 0 j z j v i i d V (I t, ε t) = ( ε 0,t, j J t 0 {E (μ j I t) γ + ε j,t + δ V (I, ε ) f (I I t, j) g (ε ) di dε }) t δ f (I I t, j) I t j g (ε) ε f (I I t, j) I t {n t, s t, h t} t h t t = 1 ε i,j,d,1

11 j h h t j n t s t j l j l l j ω l,j j n t s t f (I I t, j) j j δ z j

12 R δ = 0 L

13

14 Table 1: t 60% 35% 5% 2.7 {.5,.5} D i i t = 1,, T d a i,d,t

15 Table 2: i d

16 Table 3: 0 1,140 1,923 1,912 2,873 4,076 1,746 6,627 11,013 11,072 14,137 33, , ,113 4,906 4,482 6,336 9, ,068 1,769 n i,j,d,t ω

17 i j i j j i (a = j n i,j > 0) = d t 1 (a i,d,t = j n i,j,d,t > 0) d t 1 (n i,j,d,t > 0) i j i (a = j n i,j = 0) = d t 1 (a i,d,t = j n i,j,d,t = 0) d t 1 (n i,j,d,t = 0) i i (a > 0 n a > 0) i (a > 0 n a = 0) i a n a > 0 Δ i = i (a > 0 n a > 0) i (a > 0 n a = 0) i Δ i > 0 Δ i < 0 Δ i 0 t = 2 t = 1 t = 2 Δ i Δ i < 0 Δ i > 0 (a = j n j > 0) (a = j n j = 0) l l = 1,, 50 Δ i < 0 Δ i > 0

18 Figure 1: Share of consumers Sample Step 2 5 choices Step 2 choices only -25% 0% 25% 50% Difference in average visit probability when links are observed (Δ i ) x Δ i t > 1.3% 3.6% 3.7% μ i,j,d γ i ε i,j,d,t j) d t

19 t β i,j,d,t U i,j,d,t = μ i,j,d + β i,j,d,t γ i + ε i,j,d,t β i,j,d,t 0 β i,j,d,t 0 β i,j,d,t μ i,j,d d N

20 λ i > 0 K i,d,t j K +j i,d,t j K +j i,d,t K i,d,t i j t i j t d β i,j,d,t = λ i ( K+j i,d,t K i,d,t). K i,d,t j K +j i,d,t j b j 1 (1 π b) α j π b U (0, 1) b α j (0, 1) j α j j t d K +j i,d,t K i,d,t K +j i,d,t K i,d,t K i,d,t, h i,d,t Binom { N K i,d,t, J A (h) = h k α k k=1 α j 1 + A (h i,d,t) + α j } h i,d,t {0, 1} J A (h) α j

21 N K i,d,t α j/ (1 + A (h i,d,t) + α j) j j t d E (β i,j,d,t I i,d,t) = λ i [( 1 + A (h i,d,t) + α j ) ( N K i,d,t) ] I i,d,t K i,d,t α j I i,d,t {n i,d,t, s i,d,t, h i,d,t, K i,d,t} j λ i α j λ i K i,d,t A (h) α j α j α j K words j,d w j,d (1 + words j,d) w j,d K i,d,1 d j K i,d,1 i j d w j,d K i,d,1 i K i,d,1 d

22 v i λ i γ i D i v i N (η v + D i φ v, ζv 2 ), λ i N (η λ + D i φ λ, ζλ) 2, γ i N (η γ + D i φ γ, ζγ 2 ) γ i γ i,d = γ i (γ w) γ i d γ w > 0 ε i,d,j,t EV (0, 1) j I i,d,t V j (I i,d,t) + ε i,d,j,t V j (I i,d,t) V j (I i,d,t) = E (μ i,d,j I i,d,t) + E (β i,d,j,t I i,d,t) γ i,d + δ k J i,d,t j [V k (I )] f (I I i,d,t, k) di j t j ε i,d,j,t θ a = {a i,d,t} I = {I i,d,t} L (θ a, I, ω, w) i d T i,d t j Ji,d,t { [V j (I i,d,t θ)] 1 + ȷ J i,d,t [V ȷ (I i,d,t θ)] } 1(a i,d,t =j) I K s

23 Table 4: (z j, α j) 5 2 (φ v, φ λ, φ γ) 7 3 v i λ i γ i (η λ, η γ) 1 2 (ζ λ, ζ γ) 1 2 γ w 1 1 τ s 1 1 δ 1 1 L (θ a, ω, n, w, h) n ω w h K s γ i z j

24 v i τ s 0, 1, α j λ i δ L R L L L R L R R L R L R

25 N K i,d,t λ i N N = 30 τ ν = 1 τ s /τ ν j z j = 0 η v = 0 ζ v = 1 δ τ s

26 Table 5: , , , δ = , , , δ = 0 τ s = , , , Table 6: δ = δ = 0 τ s = k (n)k k n Table 7: z α z j α j (0.003) (0.007) (0.002) (0.003) (0.002)

27 Figure 2: α j z j Average vertical quality (α j ) egotastic dlisted celebuzz thesuperficial Average horizontal match location (z j ) perezhilton Posterior density: Figure 3: Average remaining match uncertainty 100% 95% 90% 85% 80% Number of links observed y n = 0,, 4 x (μ j,d n j,d = 0,, 4) / (μ j,d n j,d = 0) (τ s n + 1) 1

28 Table 8: v λ γ (0.18) (0.26) (0.10) (0.19) (0.25) (0.10) (0.32) (0.50) (0.17) (0.24) (0.37) (0.14) (0.24) (0.34) (0.12) (0.24) (0.33) (0.12) (0.36) (0.52) (0.20) η (0.36) (0.14) ζ (0.10) (0.04) % 16.0% 6.0%

29 i j z j v i τ s z j x v i z j < 0 z j > 0 τ s τ s (0.01, 0.22) 0.06 τs 1/2

30 5.2 (2.1, 10.3) α j y λ i γ i γ i γ w δ )

31 0.001, 0.645) z j α j ω j x y z j x z j α j

32 Figure 4: Average vertical quantity ( α ) E D C S Average horizontal match location ( z ) P Link frequency: 20% 40% 60% ω z α S S S ω n ω S S = 500

33 Table 9: 0.59% 0.11% 0.14% 0.05% 0.54% 0.06% 0.10% 0.18% 0.14% 0.09% 0.01% 95% 0 y E θ [(y baseline y counter ) /y counter ].59%.14%.54%

34 Table 10: t > 1 t = 1 t > % 0.45% 0.04% 0.01% 0.21% 0.42% 0.26% 0.02% 0.03% 1.32% 0.08% 0.00% 0.21% 0.55% 0.47% 0.14% 0.76% 0.14% 0.27% 0.03% 0.11% 0.07% 0.14% 0.02% 95% 0.18%.14% ω n t = 1 t = 1 t = 1

35 t = 1.03% 1.32%.26% 3.8%.14% 2.3%.05% L R d L d R

36 .14% 2.3%

37 .05%

38 archive.org/web/ / https: //web.archive.org/web/ / / actividades / informe - economico - del - impacto - del - nuevo - articulo de-la-lpi-nera-para-la-aeepp.html

39 org/files/2016/07/pj_ _modern-news-consumer_final.pdf N i d i d b j j

40 π b (0, 1) b α j (0, 1) j b j 1 (1 π b) α j j α j 1 b j π b j α j 0 b j α j j π b π b U (0, 1) α t α j t b t 1 (1 π b) α 1 (1 π b) α t 1 = (1 π b) A t A t A (h t) α j π b π b (1 π A t b) p (π b A t) = 1 0 (1 π A = t (1 π b) At (1 + A t) = Beta (π b 1, 1 + A t) b) dπ b b j π b b j [b j b ] = 1 α (1 (1 π b) αj ) (1 π b) At j (1 + A t) dπ b = α j + A t j N K t α j/ (1 + α j + A t) I t {n t, s t, K t, h t} A t j h t,j α j

41 I I t j f (I I t, j) = f (n, s, K, h n t, s t, K t, h t, j) f (I I t, j) = p (s n, n t, s t) p (n n t, j) p (K K t, h t, j) p (h h t, j) p (K K t, h t, j) h j δ x x p (h h t, j) = δ 1 (h t,j), h h t h j 1 n s n ȷ j n ȷ n t,ȷ + 1 ω j,ȷ n t,ȷ 1 ω j,ȷ p ( n ȷ n t, j ) = ω j,ȷ δ nt,ȷ +1 ( n ȷ ) + (1 ω j,ȷ ) δ nt,ȷ ( n ȷ ) ȷ s ȷ s ȷ = s t,ȷ p ( s j n j, n t,j, s t,j) = N z ( j + τsn t,j[s t,j z j], τ τ s n t,j +τ s 1 + ν [n t,j τ s + τ 1 ν] ), n j = n t,j + 1 δ st,j (s j), n j = n t,j w j,d K i,d,t K i,d,1 E [K i,d,1] = Nα j /(1 + α j ) w j,d K i,d,1 K i,d,1 E [K i,d,1 w j,d] = N q (w j,d) q (w j,d) j d K i,d,1 K i,d,t t > 1 q (w j,d) q (w j,d)

42 w j,d ( 0, 1 2) α j (0, 1) α j/ (1 + α j) ( 0, 1 2) 2 q (w j,d) = 1+( w j,d c) 1 c 3 {w j,d} d i K i,d,1 = 0 {w j,d} i K i,d,1 = N/2 E (μ i,1) γ i a i,1 ω 1 E (μ i,1) γ i E (μ i,1) ε i,j,d,1 z j v i δ ω ω δ = 0 t = 2 ω 2 w i,1 t > 2

43 a i,2 n i,1 τ s /τ ν ν j,d s j,l,d ν j,d s j,l,d ε i,j,d,t α j λ i v i λ i γ i D i γ w j t n i,j,t j ε i,j,d,t j s ν j,d ε i,j,d,t ν j,d n i,j,t n i,j,t ε i,j,d,t j k s k,j,d ε i,j,d,t s k,j,d n i,j,t ε i,j,d,t ν j,d n i,j,t ν j,d j j j

44 Table 11: E (μ i,1) γ i a i,1 ω 1 z j v i E (μ i,1) δ (a i,1, a i,2,, ω 1, ω 2, ) ω τ s/τ ν (a i,2, n i,1) ω 2, w i,1 ν s E (β i,2) (a i,2, w i,1) ω 2, n i,1 K α j λ i E (β i,2) φ v v i D i v i φ λ η λ ζ 2 λ λ i D i λ i φ γ η γ ζγ 2 γ i D i γ i γ w (a i,1, weekend) a i,1 a i,2 ω 1 ω 2 w i,1 n i,1 E (μ i,1) E (β i,2) t = 2 ε i,j,d,t s k,j,d n i,j,t j k j j j k k N λ i N λ i N = 30 ν j,d s j,k,d τ ν = 1 τ s z j v i z j v i

45 v i η v = 0 ζ v = 1 K s s s j,l,d (s j,l,d z j ν j,d) τs 1/2 s j,l,d z j ν j,d E ( s j,l,d) = 0 V ( s j,l,d) = 1 s ν j,d α j N (0, 1), z j N (0, 1), τ 1/2 s Ga (.4, 5) E (τ 1/2 s ) = 2, η λ N (1,.5), η γ N ( 1,.5) φ ζ N (0, ζ 2 ), φ v N (0, 1), ζ 2 χ 2 (10,.4), γ w N (0, 1) δ U (0, 1)

46 f (x) f (x) f (x) z j α j

47 Table 12: z j α j z j α j z j α j z j α j z j α j α j z j

48 δ = 1 τ s =.2 τ s = 2 γ = 2 v = 2 z = 0 ω L,R = 1 ω R,L = 0 Figure 5: Probability of initiating a session (No links) Noisy Informative Links Behavior Myopic Forward looking

49 Figure 6: Share of sessions starting at linking site (No links) Noisy Informative Links Behavior Myopic Forward looking Figure 7: Number of sites visited during session (No links) Noisy Informative Links Behavior Myopic Forward looking

50 Figure 8: 0.62 Share of sessions visiting linked site (No links) Noisy Informative Links Behavior Myopic Forward looking Figure 9: Conditional probability of visiting the linked site Myopic Forward looking (No links) Noisy Informative (No links) Noisy Informative Links Signal Lower than expected match (No links) Higher than expected match

51 p (θ W ) D θ D θ D θ D θ f (, ) θ θ D θ θ c θ c D θ c t θ c θ c θ θ

52 Θ W t θ θ (t 1) b θ p(θ W ) D θ // [1] (m, S) f(θ, D θ ) // [2] θ c N(m, S) p(θ c W ) D θ c // [1] (m, S ) f(θ c, D θ c) // [3] α p(θc )N(θ m,s ) p(θ)n(θ c m,s) u U(0, 1) u < α θ (t) b θ c θ (t) b θ I p(i θ (t) ) W f(i, θ (t) ) // [4] W { W, I, θ (t) } Θ θ (t)

3% 5% 1% 2% d t = 1,, T d i j J i,d,t J i,d,t+ = J i,d,t j j a i,d,t j i t d γ i > 0 i j t d U i,j,d,t = μ i,j,d + β i,j,d,t γ i + ε i,j,d,t ε i,j,d,t t ε i,,d,t μ β μ μ i,j,d d t d, t j μ i,j,d i j d

More information

Introduction Benchmark model Belief-based model Empirical analysis Summary. Riot Networks. Lachlan Deer Michael D. König Fernando Vega-Redondo

Introduction Benchmark model Belief-based model Empirical analysis Summary. Riot Networks. Lachlan Deer Michael D. König Fernando Vega-Redondo Riot Networks Lachlan Deer Michael D. König Fernando Vega-Redondo University of Zurich University of Zurich Bocconi University June 7, 2018 Deer & König &Vega-Redondo Riot Networks June 7, 2018 1 / 23

More information

Lecture 4: Dynamic models

Lecture 4: Dynamic models linear s Lecture 4: s Hedibert Freitas Lopes The University of Chicago Booth School of Business 5807 South Woodlawn Avenue, Chicago, IL 60637 http://faculty.chicagobooth.edu/hedibert.lopes hlopes@chicagobooth.edu

More information

K e sub x e sub n s i sub o o f K.. w ich i sub s.. u ra to the power of m i sub fi ed.. a sub t to the power of a

K e sub x e sub n s i sub o o f K.. w ich i sub s.. u ra to the power of m i sub fi ed.. a sub t to the power of a - ; ; ˆ ; q x ; j [ ; ; ˆ ˆ [ ˆ ˆ ˆ - x - - ; x j - - - - - ˆ x j ˆ ˆ ; x ; j κ ˆ - - - ; - - - ; ˆ σ x j ; ˆ [ ; ] q x σ; x - ˆ - ; J -- F - - ; x - -x - - x - - ; ; 9 S j P R S 3 q 47 q F x j x ; [ ]

More information

I. Relationship with previous work

I. Relationship with previous work x x i t j J t = {0, 1,...J t } j t (p jt, x jt, ξ jt ) p jt R + x jt R k k ξ jt R ξ t T j = 0 t (z i, ζ i, G i ), ζ i z i R m G i G i (p j, x j ) i j U(z i, ζ i, x j, p j, ξ j ; G i ) = u(ζ i, x j,

More information

Multilevel Sequential 2 Monte Carlo for Bayesian Inverse Problems

Multilevel Sequential 2 Monte Carlo for Bayesian Inverse Problems Jonas Latz 1 Multilevel Sequential 2 Monte Carlo for Bayesian Inverse Problems Jonas Latz Technische Universität München Fakultät für Mathematik Lehrstuhl für Numerische Mathematik jonas.latz@tum.de November

More information

. α β γ δ ε ζ η θ ι κ λ μ Aμ ν(x) ξ ο π ρ ς σ τ υ φ χ ψ ω. Α Β Γ Δ Ε Ζ Η Θ Ι Κ Λ Μ Ν Ξ Ο Π Ρ Σ Τ Υ Φ Χ Ψ Ω. Friday April 1 ± ǁ

. α β γ δ ε ζ η θ ι κ λ μ Aμ ν(x) ξ ο π ρ ς σ τ υ φ χ ψ ω. Α Β Γ Δ Ε Ζ Η Θ Ι Κ Λ Μ Ν Ξ Ο Π Ρ Σ Τ Υ Φ Χ Ψ Ω. Friday April 1 ± ǁ . α β γ δ ε ζ η θ ι κ λ μ Aμ ν(x) ξ ο π ρ ς σ τ υ φ χ ψ ω. Α Β Γ Δ Ε Ζ Η Θ Ι Κ Λ Μ Ν Ξ Ο Π Ρ Σ Τ Υ Φ Χ Ψ Ω Friday April 1 ± ǁ 1 Chapter 5. Photons: Covariant Theory 5.1. The classical fields 5.2. Covariant

More information

. α β γ δ ε ζ η θ ι κ λ μ Aμ ν(x) ξ ο π ρ ς σ τ υ φ χ ψ ω. Α Β Γ Δ Ε Ζ Η Θ Ι Κ Λ Μ Ν Ξ Ο Π Ρ Σ Τ Υ Φ Χ Ψ Ω. Wednesday March 30 ± ǁ

. α β γ δ ε ζ η θ ι κ λ μ Aμ ν(x) ξ ο π ρ ς σ τ υ φ χ ψ ω. Α Β Γ Δ Ε Ζ Η Θ Ι Κ Λ Μ Ν Ξ Ο Π Ρ Σ Τ Υ Φ Χ Ψ Ω. Wednesday March 30 ± ǁ . α β γ δ ε ζ η θ ι κ λ μ Aμ ν(x) ξ ο π ρ ς σ τ υ φ χ ψ ω. Α Β Γ Δ Ε Ζ Η Θ Ι Κ Λ Μ Ν Ξ Ο Π Ρ Σ Τ Υ Φ Χ Ψ Ω Wednesday March 30 ± ǁ 1 Chapter 5. Photons: Covariant Theory 5.1. The classical fields 5.2. Covariant

More information

Further Maths A2 (M2FP2D1) Assignment ψ (psi) A Due w/b 19 th March 18

Further Maths A2 (M2FP2D1) Assignment ψ (psi) A Due w/b 19 th March 18 α β γ δ ε ζ η θ ι κ λ µ ν ξ ο π ρ σ τ υ ϕ χ ψ ω The mathematician s patterns, like the painter s or the poet s, must be beautiful: the ideas, like the colours or the words, must fit together in a harmonious

More information

Celeste: Variational inference for a generative model of astronomical images

Celeste: Variational inference for a generative model of astronomical images Celeste: Variational inference for a generative model of astronomical images Jerey Regier Statistics Department UC Berkeley July 9, 2015 Joint work with Jon McAulie (UCB Statistics), Andrew Miller, Ryan

More information

State Space and Hidden Markov Models

State Space and Hidden Markov Models State Space and Hidden Markov Models Kunsch H.R. State Space and Hidden Markov Models. ETH- Zurich Zurich; Aliaksandr Hubin Oslo 2014 Contents 1. Introduction 2. Markov Chains 3. Hidden Markov and State

More information

Testing Algebraic Hypotheses

Testing Algebraic Hypotheses Testing Algebraic Hypotheses Mathias Drton Department of Statistics University of Chicago 1 / 18 Example: Factor analysis Multivariate normal model based on conditional independence given hidden variable:

More information

Mathematics Review Exercises. (answers at end)

Mathematics Review Exercises. (answers at end) Brock University Physics 1P21/1P91 Mathematics Review Exercises (answers at end) Work each exercise without using a calculator. 1. Express each number in scientific notation. (a) 437.1 (b) 563, 000 (c)

More information

Motion Models (cont) 1 2/15/2012

Motion Models (cont) 1 2/15/2012 Motion Models (cont 1 Odometry Motion Model the key to computing p( xt ut, xt 1 for the odometry motion model is to remember that the robot has an internal estimate of its pose θ x t 1 x y θ θ true poses

More information

Trajectory-tracking control of a planar 3-RRR parallel manipulator

Trajectory-tracking control of a planar 3-RRR parallel manipulator Trajectory-tracking control of a planar 3-RRR parallel manipulator Chaman Nasa and Sandipan Bandyopadhyay Department of Engineering Design Indian Institute of Technology Madras Chennai, India Abstract

More information

David Giles Bayesian Econometrics

David Giles Bayesian Econometrics 9. Model Selection - Theory David Giles Bayesian Econometrics One nice feature of the Bayesian analysis is that we can apply it to drawing inferences about entire models, not just parameters. Can't do

More information

Zone 252, Master Map Normal View

Zone 252, Master Map Normal View Zone Master, Normal View, 10 deg FOV, Master Map Normal View χ1 α ζ ε γ1 γ2 β η1 η3 η2 ψ Fornax ι2 ι1 λ2 ω λ1 φ µ No Map ν π ε π Cetus Sculptor τ -38 00' -36 00' -34 00' -32 00' -30 00' -28 00' -26 00'

More information

and in each case give the range of values of x for which the expansion is valid.

and in each case give the range of values of x for which the expansion is valid. α β γ δ ε ζ η θ ι κ λ µ ν ξ ο π ρ σ τ υ ϕ χ ψ ω Mathematics is indeed dangerous in that it absorbs students to such a degree that it dulls their senses to everything else P Kraft Further Maths A (MFPD)

More information

The Faroese Cohort 2. Structural Equation Models Latent growth models. Multiple indicator growth modeling. Response profiles. Number of children: 182

The Faroese Cohort 2. Structural Equation Models Latent growth models. Multiple indicator growth modeling. Response profiles. Number of children: 182 The Faroese Cohort 2 Structural Equation Models Latent growth models Exposure: Blood Hg Hair Hg Age: Birth 3.5 years 4.5 years 5.5 years 7.5 years Number of children: 182 Multiple indicator growth modeling

More information

EXERCISES FOR SECTION 1 AND 2

EXERCISES FOR SECTION 1 AND 2 EXERCISES FOR SECTION AND Exercise. (Conditional probability). Suppose that if θ, then y has a normal distribution with mean and standard deviation σ, and if θ, then y has a normal distribution with mean

More information

y it = α i + β 0 ix it + ε it (0.1) The panel data estimators for the linear model are all standard, either the application of OLS or GLS.

y it = α i + β 0 ix it + ε it (0.1) The panel data estimators for the linear model are all standard, either the application of OLS or GLS. 0.1. Panel Data. Suppose we have a panel of data for groups (e.g. people, countries or regions) i =1, 2,..., N over time periods t =1, 2,..., T on a dependent variable y it and a kx1 vector of independent

More information

Design of HIV Dynamic Experiments: A Case Study

Design of HIV Dynamic Experiments: A Case Study Design of HIV Dynamic Experiments: A Case Study Cong Han Department of Biostatistics University of Washington Kathryn Chaloner Department of Biostatistics University of Iowa Nonlinear Mixed-Effects Models

More information

T m / A. Table C2 Submicroscopic Masses [2] Symbol Meaning Best Value Approximate Value

T m / A. Table C2 Submicroscopic Masses [2] Symbol Meaning Best Value Approximate Value APPENDIX C USEFUL INFORMATION 1247 C USEFUL INFORMATION This appendix is broken into several tables. Table C1, Important Constants Table C2, Submicroscopic Masses Table C3, Solar System Data Table C4,

More information

The Effects of Monetary Policy on Stock Market Bubbles: Some Evidence

The Effects of Monetary Policy on Stock Market Bubbles: Some Evidence The Effects of Monetary Policy on Stock Market Bubbles: Some Evidence Jordi Gali Luca Gambetti ONLINE APPENDIX The appendix describes the estimation of the time-varying coefficients VAR model. The model

More information

arxiv: v1 [cs.ds] 13 Jan 2017

arxiv: v1 [cs.ds] 13 Jan 2017 ON DOUBLE-RESOLUTION IMAGING IN DISCRETE TOMOGRAPHY ANDREAS ALPERS AND PETER GRITZMANN arxiv:70.0499v [cs.ds] Jan 07 Abstract. Super-resolution imaging aims at improving the resolution of an image by enhancing

More information

Markov Chains and Hidden Markov Models

Markov Chains and Hidden Markov Models Chapter 1 Markov Chains and Hidden Markov Models In this chapter, we will introduce the concept of Markov chains, and show how Markov chains can be used to model signals using structures such as hidden

More information

4sec 2xtan 2x 1ii C3 Differentiation trig

4sec 2xtan 2x 1ii C3 Differentiation trig A Assignment beta Cover Sheet Name: Question Done Backpack Topic Comment Drill Consolidation i C3 Differentiation trig 4sec xtan x ii C3 Differentiation trig 6cot 3xcosec 3x iii C3 Differentiation trig

More information

Classical and Bayesian inference

Classical and Bayesian inference Classical and Bayesian inference AMS 132 January 18, 2018 Claudia Wehrhahn (UCSC) Classical and Bayesian inference January 18, 2018 1 / 9 Sampling from a Bernoulli Distribution Theorem (Beta-Bernoulli

More information

Technical Appendix: Imperfect information and the business cycle

Technical Appendix: Imperfect information and the business cycle Technical Appendix: Imperfect information and the usiness cycle Farice Collard Harris Dellas Frank Smets March 29 We would like to thank Marty Eichenaum, Jesper Lindé, Thomas Luik, Frank Schorfheide and

More information

A geometric solution of the Kervaire Invariant One problem

A geometric solution of the Kervaire Invariant One problem A geometric solution of the Kervaire Invariant One problem Petr M. Akhmet ev 19 May 2009 Let f : M n 1 R n, n = 4k + 2, n 2 be a smooth generic immersion of a closed manifold of codimension 1. Let g :

More information

Image segmentation combining Markov Random Fields and Dirichlet Processes

Image segmentation combining Markov Random Fields and Dirichlet Processes Image segmentation combining Markov Random Fields and Dirichlet Processes Jessica SODJO IMS, Groupe Signal Image, Talence Encadrants : A. Giremus, J.-F. Giovannelli, F. Caron, N. Dobigeon Jessica SODJO

More information

A Frequentist Assessment of Bayesian Inclusion Probabilities

A Frequentist Assessment of Bayesian Inclusion Probabilities A Frequentist Assessment of Bayesian Inclusion Probabilities Department of Statistical Sciences and Operations Research October 13, 2008 Outline 1 Quantitative Traits Genetic Map The model 2 Bayesian Model

More information

Sequential Monte Carlo Algorithms for Bayesian Sequential Design

Sequential Monte Carlo Algorithms for Bayesian Sequential Design Sequential Monte Carlo Algorithms for Bayesian Sequential Design Dr Queensland University of Technology c.drovandi@qut.edu.au Collaborators: James McGree, Tony Pettitt, Gentry White Acknowledgements: Australian

More information

Entities for Symbols and Greek Letters

Entities for Symbols and Greek Letters Entities for Symbols and Greek Letters The following table gives the character entity reference, decimal character reference, and hexadecimal character reference for symbols and Greek letters, as well

More information

Dynamic Learning in Supply Chain with Repeated Transactions and Service Contributions

Dynamic Learning in Supply Chain with Repeated Transactions and Service Contributions Dynamic Learning in Supply Chain with Repeated Transactions and Service Contributions Chayakrit Charoensiriwath and Jye-Chyi Lu School of Industrial and Systems Engineering, Georgia Institute of Technology

More information

Core Inflation and Trend Inflation. Appendix

Core Inflation and Trend Inflation. Appendix Core Inflation and Trend Inflation Appendix June 2015 (Revised November 2015) James H. Stock Department of Economics, Harvard University and the National Bureau of Economic Research and Mark W. Watson

More information

Likelihood NIPS July 30, Gaussian Process Regression with Student-t. Likelihood. Jarno Vanhatalo, Pasi Jylanki and Aki Vehtari NIPS-2009

Likelihood NIPS July 30, Gaussian Process Regression with Student-t. Likelihood. Jarno Vanhatalo, Pasi Jylanki and Aki Vehtari NIPS-2009 with with July 30, 2010 with 1 2 3 Representation Representation for Distribution Inference for the Augmented Model 4 Approximate Laplacian Approximation Introduction to Laplacian Approximation Laplacian

More information

1. Introduction. We consider an inverse problem based on a first-kind Volterra integral equation of the form

1. Introduction. We consider an inverse problem based on a first-kind Volterra integral equation of the form FUTURE POLYNOMIAL REGULARIZATION OF ILL-POSED VOLTERRA EQUATIONS AARON C. CINZORI AND PATRICIA K. LAMM Abstract. We examine a new discrete method for regularizing ill-posed Volterra problems. Unlike many

More information

Symmetry and Properties of Crystals (MSE638) Stress and Strain Tensor

Symmetry and Properties of Crystals (MSE638) Stress and Strain Tensor Symmetry and Properties of Crystals (MSE638) Stress and Strain Tensor Somnath Bhowmick Materials Science and Engineering, IIT Kanpur April 6, 2018 Tensile test and Hooke s Law Upto certain strain (0.75),

More information

CS1820 Notes. hgupta1, kjline, smechery. April 3-April 5. output: plausible Ancestral Recombination Graph (ARG)

CS1820 Notes. hgupta1, kjline, smechery. April 3-April 5. output: plausible Ancestral Recombination Graph (ARG) CS1820 Notes hgupta1, kjline, smechery April 3-April 5 April 3 Notes 1 Minichiello-Durbin Algorithm input: set of sequences output: plausible Ancestral Recombination Graph (ARG) note: the optimal ARG is

More information

Latent variable interactions

Latent variable interactions Latent variable interactions Bengt Muthén & Tihomir Asparouhov Mplus www.statmodel.com November 2, 2015 1 1 Latent variable interactions Structural equation modeling with latent variable interactions has

More information

SC7/SM6 Bayes Methods HT18 Lecturer: Geoff Nicholls Lecture 2: Monte Carlo Methods Notes and Problem sheets are available at http://www.stats.ox.ac.uk/~nicholls/bayesmethods/ and via the MSc weblearn pages.

More information

Demand Shocks with Dispersed Information

Demand Shocks with Dispersed Information Demand Shocks with Dispersed Information Guido Lorenzoni (MIT) Class notes, 06 March 2007 Nominal rigidities: imperfect information How to model demand shocks in a baseline environment with imperfect info?

More information

A biased review of Leptogenesis. Lotfi Boubekeur ICTP

A biased review of Leptogenesis. Lotfi Boubekeur ICTP A biased review of Leptogenesis Lotfi Boubekeur ICTP Baryogenesis: Basics Observation Our Universe is baryon asymmetric. n B s n b n b s 10 11 BAU is measured in CMB and BBN. Perfect agreement with each

More information

Demand Shocks, Monetary Policy, and the Optimal Use of Dispersed Information

Demand Shocks, Monetary Policy, and the Optimal Use of Dispersed Information Demand Shocks, Monetary Policy, and the Optimal Use of Dispersed Information Guido Lorenzoni (MIT) WEL-MIT-Central Banks, December 2006 Motivation Central bank observes an increase in spending Is it driven

More information

Bayesian Inference on Joint Mixture Models for Survival-Longitudinal Data with Multiple Features. Yangxin Huang

Bayesian Inference on Joint Mixture Models for Survival-Longitudinal Data with Multiple Features. Yangxin Huang Bayesian Inference on Joint Mixture Models for Survival-Longitudinal Data with Multiple Features Yangxin Huang Department of Epidemiology and Biostatistics, COPH, USF, Tampa, FL yhuang@health.usf.edu January

More information

ASSIGNMENT COVER SHEET omicron

ASSIGNMENT COVER SHEET omicron ASSIGNMENT COVER SHEET omicron Name Question Done Backpack Ready for test Drill A differentiation Drill B sketches Drill C Partial fractions Drill D integration Drill E differentiation Section A integration

More information

arxiv: v1 [math.pr] 4 Nov 2016

arxiv: v1 [math.pr] 4 Nov 2016 Perturbations of continuous-time Markov chains arxiv:1611.1254v1 [math.pr 4 Nov 216 Pei-Sen Li School of Mathematical Sciences, Beijing Normal University, Beijing 1875, China E-ma: peisenli@ma.bnu.edu.cn

More information

Formalism of the Tersoff potential

Formalism of the Tersoff potential Originally written in December 000 Translated to English in June 014 Formalism of the Tersoff potential 1 The original version (PRB 38 p.990, PRB 37 p.6991) Potential energy Φ = 1 u ij i (1) u ij = f ij

More information

MARKOV CHAIN MONTE CARLO

MARKOV CHAIN MONTE CARLO MARKOV CHAIN MONTE CARLO RYAN WANG Abstract. This paper gives a brief introduction to Markov Chain Monte Carlo methods, which offer a general framework for calculating difficult integrals. We start with

More information

Lecture 3: Adaptive Construction of Response Surface Approximations for Bayesian Inference

Lecture 3: Adaptive Construction of Response Surface Approximations for Bayesian Inference Lecture 3: Adaptive Construction of Response Surface Approximations for Bayesian Inference Serge Prudhomme Département de mathématiques et de génie industriel Ecole Polytechnique de Montréal SRI Center

More information

Equilibrium Conditions and Algorithm for Numerical Solution of Kaplan, Moll and Violante (2017) HANK Model.

Equilibrium Conditions and Algorithm for Numerical Solution of Kaplan, Moll and Violante (2017) HANK Model. Equilibrium Conditions and Algorithm for Numerical Solution of Kaplan, Moll and Violante (2017) HANK Model. January 8, 2018 1 Introduction This document describes the equilibrium conditions of Kaplan,

More information

Lecture 10 Demand for Autos (BLP) Bronwyn H. Hall Economics 220C, UC Berkeley Spring 2005

Lecture 10 Demand for Autos (BLP) Bronwyn H. Hall Economics 220C, UC Berkeley Spring 2005 Lecture 10 Demand for Autos (BLP) Bronwyn H. Hall Economics 220C, UC Berkeley Spring 2005 Outline BLP Spring 2005 Economics 220C 2 Why autos? Important industry studies of price indices and new goods (Court,

More information

Onboard Engine FDI in Autonomous Aircraft Using Stochastic Nonlinear Modelling of Flight Signal Dependencies

Onboard Engine FDI in Autonomous Aircraft Using Stochastic Nonlinear Modelling of Flight Signal Dependencies Onboard Engine FDI in Autonomous Aircraft Using Stochastic Nonlinear Modelling of Flight Signal Dependencies Dimitrios G. Dimogianopoulos, John D. Hios and Spilios D. Fassois Stochastic Mechanical Systems

More information

Theory of Statistical Tests

Theory of Statistical Tests Ch 9. Theory of Statistical Tests 9.1 Certain Best Tests How to construct good testing. For simple hypothesis H 0 : θ = θ, H 1 : θ = θ, Page 1 of 100 where Θ = {θ, θ } 1. Define the best test for H 0 H

More information

Bayesian tsunami fragility modeling considering input data uncertainty

Bayesian tsunami fragility modeling considering input data uncertainty Bayesian tsunami fragility modeling considering input data uncertainty Raffaele De Risi Research Associate University of Bristol United Kingdom De Risi, R., Goda, K., Mori, N., & Yasuda, T. (2016). Bayesian

More information

ESTIMATION of a DSGE MODEL

ESTIMATION of a DSGE MODEL ESTIMATION of a DSGE MODEL Paris, October 17 2005 STÉPHANE ADJEMIAN stephane.adjemian@ens.fr UNIVERSITÉ DU MAINE & CEPREMAP Slides.tex ESTIMATION of a DSGE MODEL STÉPHANE ADJEMIAN 16/10/2005 21:37 p. 1/3

More information

Hierarchical models. Dr. Jarad Niemi. August 31, Iowa State University. Jarad Niemi (Iowa State) Hierarchical models August 31, / 31

Hierarchical models. Dr. Jarad Niemi. August 31, Iowa State University. Jarad Niemi (Iowa State) Hierarchical models August 31, / 31 Hierarchical models Dr. Jarad Niemi Iowa State University August 31, 2017 Jarad Niemi (Iowa State) Hierarchical models August 31, 2017 1 / 31 Normal hierarchical model Let Y ig N(θ g, σ 2 ) for i = 1,...,

More information

University College London. Frank Deppisch. University College London

University College London. Frank Deppisch. University College London Frank Deppisch f.deppisch@ucl.ac.uk University College London Nuclear Particle Astrophysics Seminar Yale 03/06/2014 Neutrinos Oscillations Absolute Mass Neutrinoless Double Beta Decay Neutrinos in Cosmology

More information

PHYS 4390: GENERAL RELATIVITY NON-COORDINATE BASIS APPROACH

PHYS 4390: GENERAL RELATIVITY NON-COORDINATE BASIS APPROACH PHYS 4390: GENERAL RELATIVITY NON-COORDINATE BASIS APPROACH 1. Differential Forms To start our discussion, we will define a special class of type (0,r) tensors: Definition 1.1. A differential form of order

More information

Modeling conditional distributions with mixture models: Applications in finance and financial decision-making

Modeling conditional distributions with mixture models: Applications in finance and financial decision-making Modeling conditional distributions with mixture models: Applications in finance and financial decision-making John Geweke University of Iowa, USA Journal of Applied Econometrics Invited Lecture Università

More information

Gibbs Sampling in Linear Models #2

Gibbs Sampling in Linear Models #2 Gibbs Sampling in Linear Models #2 Econ 690 Purdue University Outline 1 Linear Regression Model with a Changepoint Example with Temperature Data 2 The Seemingly Unrelated Regressions Model 3 Gibbs sampling

More information

Variant of Optimality Criteria Method for Multiple State Optimal Design Problems

Variant of Optimality Criteria Method for Multiple State Optimal Design Problems Variant of Optimality Criteria Method for Multiple State Optimal Design Problems Ivana Crnjac J. J. STROSSMAYER UNIVERSITY OF OSIJEK DEPARTMENT OF MATHEMATICS Trg Ljudevita Gaja 6 3000 Osijek, Hrvatska

More information

Practical Bayesian Optimization of Machine Learning. Learning Algorithms

Practical Bayesian Optimization of Machine Learning. Learning Algorithms Practical Bayesian Optimization of Machine Learning Algorithms CS 294 University of California, Berkeley Tuesday, April 20, 2016 Motivation Machine Learning Algorithms (MLA s) have hyperparameters that

More information

Counterfactuals via Deep IV. Matt Taddy (Chicago + MSR) Greg Lewis (MSR) Jason Hartford (UBC) Kevin Leyton-Brown (UBC)

Counterfactuals via Deep IV. Matt Taddy (Chicago + MSR) Greg Lewis (MSR) Jason Hartford (UBC) Kevin Leyton-Brown (UBC) Counterfactuals via Deep IV Matt Taddy (Chicago + MSR) Greg Lewis (MSR) Jason Hartford (UBC) Kevin Leyton-Brown (UBC) Endogenous Errors y = g p, x + e and E[ p e ] 0 If you estimate this using naïve ML,

More information

Hierarchical Modeling for Spatial Data

Hierarchical Modeling for Spatial Data Bayesian Spatial Modelling Spatial model specifications: P(y X, θ). Prior specifications: P(θ). Posterior inference of model parameters: P(θ y). Predictions at new locations: P(y 0 y). Model comparisons.

More information

Smooth Macro-Elements on Powell-Sabin-12 Splits

Smooth Macro-Elements on Powell-Sabin-12 Splits Smooth Macro-Elements on Powell-Sabin-12 Splits Larry L. Schumaker 1) and Tatyana Sorokina 2) Abstract. Macro-elements of smoothness C r are constructed on Powell-Sabin- 12 splits of a triangle for all

More information

General Franklin systems as bases in H 1 [0, 1]

General Franklin systems as bases in H 1 [0, 1] STUDIA MATHEMATICA 67 (3) (2005) General Franklin systems as bases in H [0, ] by Gegham G. Gevorkyan (Yerevan) and Anna Kamont (Sopot) Abstract. By a general Franklin system corresponding to a dense sequence

More information

Structural Change, Demographic Transition and Fertility Di erence

Structural Change, Demographic Transition and Fertility Di erence Structural Change, Demographic Transition and Fertility Di erence T. Terry Cheung February 14, 2017 T. Terry Cheung () Structural Change and Fertility February 14, 2017 1 / 35 Question Question: The force

More information

http://orcid.org/0000-0001-8820-8188 N r = 0.88 P x λ P x λ d m = d 1/ m, d m i 1...m ( d i ) 2 = c c i m d β = 1 β = 1.5 β = 2 β = 3 d b = d a d b = 1.0

More information

Y1 Double Maths Assignment λ (lambda) Exam Paper to do Core 1 Solomon C on the VLE. Drill

Y1 Double Maths Assignment λ (lambda) Exam Paper to do Core 1 Solomon C on the VLE. Drill α β γ δ ε ζ η θ ι κ λ µ ν ξ ο π ρ σ τ υ ϕ χ ψ ω Nature is an infinite sphere of which the centre is everywhere and the circumference nowhere Blaise Pascal Y Double Maths Assignment λ (lambda) Tracking

More information

The QHE as laboratory system to study quantum phase transitions

The QHE as laboratory system to study quantum phase transitions The QHE as laboratory system to study quantum phase transitions Anne de Visser, WZI-UvA Quantum Hall effect Critical behavior and scaling Magnetotransport at the plateau-insulator transition Scaling functions

More information

Holomorphic linearization of commuting germs of holomorphic maps

Holomorphic linearization of commuting germs of holomorphic maps Holomorphic linearization of commuting germs of holomorphic maps Jasmin Raissy Dipartimento di Matematica e Applicazioni Università degli Studi di Milano Bicocca AMS 2010 Fall Eastern Sectional Meeting

More information

θ 1 θ 2 θ n y i1 y i2 y in Hierarchical models (chapter 5) Hierarchical model Introduction to hierarchical models - sometimes called multilevel model

θ 1 θ 2 θ n y i1 y i2 y in Hierarchical models (chapter 5) Hierarchical model Introduction to hierarchical models - sometimes called multilevel model Hierarchical models (chapter 5) Introduction to hierarchical models - sometimes called multilevel model Exchangeability Slide 1 Hierarchical model Example: heart surgery in hospitals - in hospital j survival

More information

Resonances, Divergent series and R.G.: (G. Gentile, G.G.) α = ε α f(α) α 2. 0 ν Z r

Resonances, Divergent series and R.G.: (G. Gentile, G.G.) α = ε α f(α) α 2. 0 ν Z r B Resonances, Divergent series and R.G.: (G. Gentile, G.G.) Eq. Motion: α = ε α f(α) A A 2 α α 2 α...... l A l Representation of phase space in terms of l rotators: α=(α,...,α l ) T l Potential: f(α) =

More information

Basic math for biology

Basic math for biology Basic math for biology Lei Li Florida State University, Feb 6, 2002 The EM algorithm: setup Parametric models: {P θ }. Data: full data (Y, X); partial data Y. Missing data: X. Likelihood and maximum likelihood

More information

Approximate Bayesian inference

Approximate Bayesian inference Approximate Bayesian inference Variational and Monte Carlo methods Christian A. Naesseth 1 Exchange rate data 0 20 40 60 80 100 120 Month Image data 2 1 Bayesian inference 2 Variational inference 3 Stochastic

More information

Primordial and Doppler modulations with Planck Antony Lewis On behalf of the Planck collaboration

Primordial and Doppler modulations with Planck Antony Lewis On behalf of the Planck collaboration Primordial and Doppler modulations with Planck Antony Lewis On behalf of the Planck collaboration http://cosmologist.info/ Outline Primordial modulations and power asymmetry τ NL trispectrum Kinematic

More information

Gaussian Elimination for Linear Systems

Gaussian Elimination for Linear Systems Gaussian Elimination for Linear Systems Tsung-Ming Huang Department of Mathematics National Taiwan Normal University October 3, 2011 1/56 Outline 1 Elementary matrices 2 LR-factorization 3 Gaussian elimination

More information

Quantizations and classical non-commutative non-associative algebras

Quantizations and classical non-commutative non-associative algebras Journal of Generalized Lie Theory and Applications Vol. (008), No., 35 44 Quantizations and classical non-commutative non-associative algebras Hilja Lisa HURU and Valentin LYCHAGIN Department of Mathematics,

More information

International Trade Lecture 16: Gravity Models (Theory)

International Trade Lecture 16: Gravity Models (Theory) 14.581 International Trade Lecture 16: Gravity Models (Theory) 14.581 Week 9 Spring 2013 14.581 (Week 9) Gravity Models (Theory) Spring 2013 1 / 44 Today s Plan 1 The Simplest Gravity Model: Armington

More information

The Bernstein and Nikolsky inequalities for trigonometric polynomials

The Bernstein and Nikolsky inequalities for trigonometric polynomials he ernstein and Nikolsky ineualities for trigonometric polynomials Jordan ell jordanbell@gmailcom Department of Mathematics, University of oronto January 28, 2015 1 Introduction Let = R/2πZ For a function

More information

Existence of Optimal Strategies in Markov Games with Incomplete Information

Existence of Optimal Strategies in Markov Games with Incomplete Information Existence of Optimal Strategies in Markov Games with Incomplete Information Abraham Neyman 1 December 29, 2005 1 Institute of Mathematics and Center for the Study of Rationality, Hebrew University, 91904

More information

PROBABILITY: LIMIT THEOREMS II, SPRING HOMEWORK PROBLEMS

PROBABILITY: LIMIT THEOREMS II, SPRING HOMEWORK PROBLEMS PROBABILITY: LIMIT THEOREMS II, SPRING 218. HOMEWORK PROBLEMS PROF. YURI BAKHTIN Instructions. You are allowed to work on solutions in groups, but you are required to write up solutions on your own. Please

More information

Hierarchical Linear Models

Hierarchical Linear Models Hierarchical Linear Models Statistics 220 Spring 2005 Copyright c 2005 by Mark E. Irwin The linear regression model Hierarchical Linear Models y N(Xβ, Σ y ) β σ 2 p(β σ 2 ) σ 2 p(σ 2 ) can be extended

More information

Contact the LHC

Contact the LHC SUSY07, Karlsruhe, 31/07/2007 15th International Conference on Supersymmetry and the Unification of Fundamental Interactions Contact Interactions @ the LHC Mónica L. VázuezV Acosta (CERN) on behalf of

More information

Stochastic Collocation Methods for Polynomial Chaos: Analysis and Applications

Stochastic Collocation Methods for Polynomial Chaos: Analysis and Applications Stochastic Collocation Methods for Polynomial Chaos: Analysis and Applications Dongbin Xiu Department of Mathematics, Purdue University Support: AFOSR FA955-8-1-353 (Computational Math) SF CAREER DMS-64535

More information

Statistics & Data Sciences: First Year Prelim Exam May 2018

Statistics & Data Sciences: First Year Prelim Exam May 2018 Statistics & Data Sciences: First Year Prelim Exam May 2018 Instructions: 1. Do not turn this page until instructed to do so. 2. Start each new question on a new sheet of paper. 3. This is a closed book

More information

November 2002 STA Random Effects Selection in Linear Mixed Models

November 2002 STA Random Effects Selection in Linear Mixed Models November 2002 STA216 1 Random Effects Selection in Linear Mixed Models November 2002 STA216 2 Introduction It is common practice in many applications to collect multiple measurements on a subject. Linear

More information

Bayesian Ingredients. Hedibert Freitas Lopes

Bayesian Ingredients. Hedibert Freitas Lopes Normal Prior s Ingredients Hedibert Freitas Lopes The University of Chicago Booth School of Business 5807 South Woodlawn Avenue, Chicago, IL 60637 http://faculty.chicagobooth.edu/hedibert.lopes hlopes@chicagobooth.edu

More information

Gaussian Multiscale Spatio-temporal Models for Areal Data

Gaussian Multiscale Spatio-temporal Models for Areal Data Gaussian Multiscale Spatio-temporal Models for Areal Data (University of Missouri) Scott H. Holan (University of Missouri) Adelmo I. Bertolde (UFES) Outline Motivation Multiscale factorization The multiscale

More information

Lecture 1: Introduction

Lecture 1: Introduction Principles of Statistics Part II - Michaelmas 208 Lecturer: Quentin Berthet Lecture : Introduction This course is concerned with presenting some of the mathematical principles of statistical theory. One

More information

Statistical Tools and Techniques for Solar Astronomers

Statistical Tools and Techniques for Solar Astronomers Statistical Tools and Techniques for Solar Astronomers Alexander W Blocker Nathan Stein SolarStat 2012 Outline Outline 1 Introduction & Objectives 2 Statistical issues with astronomical data 3 Example:

More information

Supplementary Material: What Inventory Behavior Tells Us About How Business Cycles Have Changed

Supplementary Material: What Inventory Behavior Tells Us About How Business Cycles Have Changed Supplementary Material: What Inventory Behavior Tells Us About How Business Cycles Have Changed Thomas Lubik Pierre-Daniel G. Sarte Felipe Schwartzman Research Department, Federal Reserve Bank of Richmond

More information

Representation homology and derived character maps

Representation homology and derived character maps Representation homology and derived character maps Sasha Patotski Cornell University ap744@cornell.edu April 30, 2016 Sasha Patotski (Cornell University) Representation homology April 30, 2016 1 / 18 Plan

More information

Splitting Techniques in the Face of Huge Problem Sizes: Block-Coordinate and Block-Iterative Approaches

Splitting Techniques in the Face of Huge Problem Sizes: Block-Coordinate and Block-Iterative Approaches Splitting Techniques in the Face of Huge Problem Sizes: Block-Coordinate and Block-Iterative Approaches Patrick L. Combettes joint work with J.-C. Pesquet) Laboratoire Jacques-Louis Lions Faculté de Mathématiques

More information

Supplementary Appendix to A Bayesian DSGE Model of Stock Market Bubbles and Business Cycles

Supplementary Appendix to A Bayesian DSGE Model of Stock Market Bubbles and Business Cycles Supplementary Appendix to A Bayesian DSGE Model of Stock Market Bubbles and Business Cycles Jianjun Miao, Pengfei Wang, and Zhiwei Xu May 9, 205 Department of Economics, Boston University, 270 Bay State

More information

Properties for systems with weak invariant manifolds

Properties for systems with weak invariant manifolds Statistical properties for systems with weak invariant manifolds Faculdade de Ciências da Universidade do Porto Joint work with José F. Alves Workshop rare & extreme Gibbs-Markov-Young structure Let M

More information

Sparse Quadrature Algorithms for Bayesian Inverse Problems

Sparse Quadrature Algorithms for Bayesian Inverse Problems Sparse Quadrature Algorithms for Bayesian Inverse Problems Claudia Schillings, Christoph Schwab Pro*Doc Retreat Disentis 2013 Numerical Analysis and Scientific Computing Disentis - 15 August, 2013 research

More information

Pattern Recognition and Machine Learning. Bishop Chapter 2: Probability Distributions

Pattern Recognition and Machine Learning. Bishop Chapter 2: Probability Distributions Pattern Recognition and Machine Learning Chapter 2: Probability Distributions Cécile Amblard Alex Kläser Jakob Verbeek October 11, 27 Probability Distributions: General Density Estimation: given a finite

More information