I conti economici trimestrali: avanzamenti metodologici e prospettive di innovazione
Seminario
Roma, 21 aprile 2016
Istat, Aula Magna
Via Cesare Balbo, 14
Scalable inference for a full multivariate stochastic volatilitySYRTO Project
Scalable inference for a full multivariate stochastic volatility
P. Dellaportas, A. Plataniotis and M. Titsias UCL(London), AUEB(Athens), AUEB(Athens)
Final SYRTO Conference - Université Paris1 Panthéon-Sorbonne
February 19, 2016
Spillover Dynamics for Systemic Risk Measurement Using Spatial Financial Time...SYRTO Project
Spillover Dynamics for Systemic Risk Measurement Using Spatial Financial Time Series Models. Andre Lucas. Amsterdam - June, 25 2015. European Financial Management Association 2015 Annual Meetings.
Network and risk spillovers: a multivariate GARCH perspectiveSYRTO Project
M. Billio, M. Caporin, L. Frattarolo, L. Pelizzon: “Network and risk spillovers: a multivariate GARCH perspective”.
Final SYRTO Conference - Université Paris1 Panthéon-Sorbonne
February 19, 2016
Clustering in dynamic causal networks as a measure of systemic risk on the eu...SYRTO Project
Clustering in dynamic causal networks as a measure of systemic risk on the euro zone
M. Billio, H. Gatfaoui, L. Frattarolo, P. de Peretti
IESEG/ Universitè Paris1 Panthèon-Sorbonne/ University Ca' Foscari
Final SYRTO Conference - Université Paris1 Panthéon-Sorbonne
February 19, 2016
Scalable inference for a full multivariate stochastic volatilitySYRTO Project
Scalable inference for a full multivariate stochastic volatility
P. Dellaportas, A. Plataniotis and M. Titsias UCL(London), AUEB(Athens), AUEB(Athens)
Final SYRTO Conference - Université Paris1 Panthéon-Sorbonne
February 19, 2016
Spillover Dynamics for Systemic Risk Measurement Using Spatial Financial Time...SYRTO Project
Spillover Dynamics for Systemic Risk Measurement Using Spatial Financial Time Series Models. Andre Lucas. Amsterdam - June, 25 2015. European Financial Management Association 2015 Annual Meetings.
Network and risk spillovers: a multivariate GARCH perspectiveSYRTO Project
M. Billio, M. Caporin, L. Frattarolo, L. Pelizzon: “Network and risk spillovers: a multivariate GARCH perspective”.
Final SYRTO Conference - Université Paris1 Panthéon-Sorbonne
February 19, 2016
Clustering in dynamic causal networks as a measure of systemic risk on the eu...SYRTO Project
Clustering in dynamic causal networks as a measure of systemic risk on the euro zone
M. Billio, H. Gatfaoui, L. Frattarolo, P. de Peretti
IESEG/ Universitè Paris1 Panthèon-Sorbonne/ University Ca' Foscari
Final SYRTO Conference - Université Paris1 Panthéon-Sorbonne
February 19, 2016
The dangers of policy experiments Initial beliefs under adaptive learningGRAPE
The paper studies the implication of initial beliefs and associated confidence on the system’s
dynamics under adaptive learning. We first illustrate how prior beliefs determine learning dynamics
and the evolution of endogenous variables in a small DSGE model with credit-constrained agents,
in which rational expectations are replaced by constant-gain adaptive learning. We then examine
how discretionary experimenting with new macroeconomic policies is affected by expectations that
agents have in relation to these policies. More specifically, we show that a newly introduced macroprudential policy that aims at making leverage counter-cyclical can lead to substantial increase in
fluctuations under learning, when the economy is hit by financial shocks, if beliefs reflect imperfect
information about the policy experiment. This is in the stark contrast to the effects of such policy
under rational expectations.
Estimating Financial Frictions under LearningGRAPE
The paper studies the implication of initial beliefs and associated confidence under adaptive learning. We first illustrate how prior beliefs determine learning dynamics and the evolution of endogenous variables in a small DSGE model with credit-constrained agents, in which rational expectations are replaced by constant-gain adaptive learning. We then examine how discretionary experimenting with new macroeconomic policies is affected by expectations that agents have in relation to these policies. More specifically, we show that a newly introduced macro-prudential policy that aims at making leverage counter-cyclical can lead to substantial increase in fluctuations under learning, when the economy is hit by financial shocks, if beliefs reflect imperfect information about the policy experiment.
Bayesian inference for mixed-effects models driven by SDEs and other stochast...Umberto Picchini
An important, and well studied, class of stochastic models is given by stochastic differential equations (SDEs). In this talk, we consider Bayesian inference based on measurements from several individuals, to provide inference at the "population level" using mixed-effects modelling. We consider the case where dynamics are expressed via SDEs or other stochastic (Markovian) models. Stochastic differential equation mixed-effects models (SDEMEMs) are flexible hierarchical models that account for (i) the intrinsic random variability in the latent states dynamics, as well as (ii) the variability between individuals, and also (iii) account for measurement error. This flexibility gives rise to methodological and computational difficulties.
Fully Bayesian inference for nonlinear SDEMEMs is complicated by the typical intractability of the observed data likelihood which motivates the use of sampling-based approaches such as Markov chain Monte Carlo. A Gibbs sampler is proposed to target the marginal posterior of all parameters of interest. The algorithm is made computationally efficient through careful use of blocking strategies, particle filters (sequential Monte Carlo) and correlated pseudo-marginal approaches. The resulting methodology is is flexible, general and is able to deal with a large class of nonlinear SDEMEMs [1]. In a more recent work [2], we also explored ways to make inference even more scalable to an increasing number of individuals, while also dealing with state-space models driven by other stochastic dynamic models than SDEs, eg Markov jump processes and nonlinear solvers typically used in systems biology.
[1] S. Wiqvist, A. Golightly, AT McLean, U. Picchini (2020). Efficient inference for stochastic differential mixed-effects models using correlated particle pseudo-marginal algorithms, CSDA, https://doi.org/10.1016/j.csda.2020.107151
[2] S. Persson, N. Welkenhuysen, S. Shashkova, S. Wiqvist, P. Reith, G. W. Schmidt, U. Picchini, M. Cvijovic (2021). PEPSDI: Scalable and flexible inference framework for stochastic dynamic single-cell models, bioRxiv doi:10.1101/2021.07.01.450748.
Entropy and systemic risk measures
M. Billio, R. Casarin, M. Costola, A. Pasqualini
Ca’ Foscari Venice University
Final SYRTO Conference - Université Paris1 Panthéon-Sorbonne
February 19, 2016
Random Matrix Theory and Machine Learning - Part 1Fabian Pedregosa
ICML 2021 tutorial on random matrix theory and machine learning. Part 1 covers: 1. A brief history of Random Matrix Theory, 2. Classical Random Matrix Ensembles (basic building blocks)
Random Matrix Theory and Machine Learning - Part 3Fabian Pedregosa
ICML 2021 tutorial on random matrix theory and machine learning.
Part 3 covers: 1. Motivation: Average-case versus worst-case in high dimensions 2. Algorithm halting times (runtimes) 3. Outlook
I conti economici trimestrali: avanzamenti metodologici e prospettive di innovazione
Seminario
Roma, 21 aprile 2016
Istat, Aula Magna
Via Cesare Balbo, 14
I conti economici trimestrali: avanzamenti metodologici e prospettive di innovazione
Seminario
Roma, 21 aprile 2016
Istat, Aula Magna
Via Cesare Balbo, 14
The dangers of policy experiments Initial beliefs under adaptive learningGRAPE
The paper studies the implication of initial beliefs and associated confidence on the system’s
dynamics under adaptive learning. We first illustrate how prior beliefs determine learning dynamics
and the evolution of endogenous variables in a small DSGE model with credit-constrained agents,
in which rational expectations are replaced by constant-gain adaptive learning. We then examine
how discretionary experimenting with new macroeconomic policies is affected by expectations that
agents have in relation to these policies. More specifically, we show that a newly introduced macroprudential policy that aims at making leverage counter-cyclical can lead to substantial increase in
fluctuations under learning, when the economy is hit by financial shocks, if beliefs reflect imperfect
information about the policy experiment. This is in the stark contrast to the effects of such policy
under rational expectations.
Estimating Financial Frictions under LearningGRAPE
The paper studies the implication of initial beliefs and associated confidence under adaptive learning. We first illustrate how prior beliefs determine learning dynamics and the evolution of endogenous variables in a small DSGE model with credit-constrained agents, in which rational expectations are replaced by constant-gain adaptive learning. We then examine how discretionary experimenting with new macroeconomic policies is affected by expectations that agents have in relation to these policies. More specifically, we show that a newly introduced macro-prudential policy that aims at making leverage counter-cyclical can lead to substantial increase in fluctuations under learning, when the economy is hit by financial shocks, if beliefs reflect imperfect information about the policy experiment.
Bayesian inference for mixed-effects models driven by SDEs and other stochast...Umberto Picchini
An important, and well studied, class of stochastic models is given by stochastic differential equations (SDEs). In this talk, we consider Bayesian inference based on measurements from several individuals, to provide inference at the "population level" using mixed-effects modelling. We consider the case where dynamics are expressed via SDEs or other stochastic (Markovian) models. Stochastic differential equation mixed-effects models (SDEMEMs) are flexible hierarchical models that account for (i) the intrinsic random variability in the latent states dynamics, as well as (ii) the variability between individuals, and also (iii) account for measurement error. This flexibility gives rise to methodological and computational difficulties.
Fully Bayesian inference for nonlinear SDEMEMs is complicated by the typical intractability of the observed data likelihood which motivates the use of sampling-based approaches such as Markov chain Monte Carlo. A Gibbs sampler is proposed to target the marginal posterior of all parameters of interest. The algorithm is made computationally efficient through careful use of blocking strategies, particle filters (sequential Monte Carlo) and correlated pseudo-marginal approaches. The resulting methodology is is flexible, general and is able to deal with a large class of nonlinear SDEMEMs [1]. In a more recent work [2], we also explored ways to make inference even more scalable to an increasing number of individuals, while also dealing with state-space models driven by other stochastic dynamic models than SDEs, eg Markov jump processes and nonlinear solvers typically used in systems biology.
[1] S. Wiqvist, A. Golightly, AT McLean, U. Picchini (2020). Efficient inference for stochastic differential mixed-effects models using correlated particle pseudo-marginal algorithms, CSDA, https://doi.org/10.1016/j.csda.2020.107151
[2] S. Persson, N. Welkenhuysen, S. Shashkova, S. Wiqvist, P. Reith, G. W. Schmidt, U. Picchini, M. Cvijovic (2021). PEPSDI: Scalable and flexible inference framework for stochastic dynamic single-cell models, bioRxiv doi:10.1101/2021.07.01.450748.
Entropy and systemic risk measures
M. Billio, R. Casarin, M. Costola, A. Pasqualini
Ca’ Foscari Venice University
Final SYRTO Conference - Université Paris1 Panthéon-Sorbonne
February 19, 2016
Random Matrix Theory and Machine Learning - Part 1Fabian Pedregosa
ICML 2021 tutorial on random matrix theory and machine learning. Part 1 covers: 1. A brief history of Random Matrix Theory, 2. Classical Random Matrix Ensembles (basic building blocks)
Random Matrix Theory and Machine Learning - Part 3Fabian Pedregosa
ICML 2021 tutorial on random matrix theory and machine learning.
Part 3 covers: 1. Motivation: Average-case versus worst-case in high dimensions 2. Algorithm halting times (runtimes) 3. Outlook
I conti economici trimestrali: avanzamenti metodologici e prospettive di innovazione
Seminario
Roma, 21 aprile 2016
Istat, Aula Magna
Via Cesare Balbo, 14
I conti economici trimestrali: avanzamenti metodologici e prospettive di innovazione
Seminario
Roma, 21 aprile 2016
Istat, Aula Magna
Via Cesare Balbo, 14
I conti economici trimestrali: avanzamenti metodologici e prospettive di innovazione
Seminario
Roma, 21 aprile 2016
Istat, Aula Magna
Via Cesare Balbo, 14
I conti economici trimestrali: avanzamenti metodologici e prospettive di innovazione
Seminario
Roma, 21 aprile 2016
Istat, Aula Magna
Via Cesare Balbo, 14
I conti economici trimestrali: avanzamenti metodologici e prospettive di innovazione
Seminario
Roma, 21 aprile 2016
Istat, Aula Magna
Via Cesare Balbo, 14
I conti economici trimestrali: avanzamenti metodologici e prospettive di innovazione
Seminario
Roma, 21 aprile 2016
Istat, Aula Magna
Via Cesare Balbo, 14
I conti economici trimestrali: avanzamenti metodologici e prospettive di innovazione
Seminario
Roma, 21 aprile 2016
Istat, Aula Magna
Via Cesare Balbo, 14
I conti economici trimestrali: avanzamenti metodologici e prospettive di innovazione
Seminario
Roma, 21 aprile 2016
Istat, Aula Magna
Via Cesare Balbo, 14
I conti economici trimestrali: avanzamenti metodologici e prospettive di innovazione
Seminario
Roma, 21 aprile 2016
Istat, Aula Magna
Via Cesare Balbo, 14
A Study on Youth Violence and Aggression using DEMATEL with FCM Methodsijdmtaiir
The DEMATEL method is then a good technique for
making decisions. In this paper we analyzed the risk factors of
youth violence and what makes them more aggressive. Since
there are more risk factors of youth violence, to relate each
other more complex to construct FCM and analyze them.
Moreover the data is an unsupervised one obtained from
survey as well as interviews. Hence fuzzy alone has the
capacity to analyses these concepts.
Digital Signal Processing[ECEG-3171]-Ch1_L07Rediet Moges
This Digital Signal Processing Lecture material is the property of the author (Rediet M.) . It is not for publication,nor is it to be sold or reproduced.
Data fusion is the process of combining data from different sources to enhance the utility of the combined product. In remote sensing, input data sources are typically massive, noisy, and have different spatial supports and sampling characteristics. We take an inferential approach to this data fusion problem: we seek to infer a true but not directly observed spatial (or spatio-temporal) field from heterogeneous inputs. We use a statistical model to make these inferences, but like all models it is at least somewhat uncertain. In this talk, we will discuss our experiences with the impacts of these uncertainties and some potential ways addressing them.
Financial Time Series Analysis Based On Normalized Mutual Information FunctionsIJCI JOURNAL
A method of predictability analysis of future values of financial time series is described. The method is based on normalized mutual information functions. In the analysis, the use of these functions allowed to refuse any restrictions on the distributions of the parameters and on the correlations between parameters. A comparative analysis of the predictability of financial time series of Tel Aviv 25 stock exchange has been carried out.
The International Journal of Engineering and Science (The IJES)theijes
The International Journal of Engineering & Science is aimed at providing a platform for researchers, engineers, scientists, or educators to publish their original research results, to exchange new ideas, to disseminate information in innovative designs, engineering experiences and technological skills. It is also the Journal's objective to promote engineering and technology education. All papers submitted to the Journal will be blind peer-reviewed. Only original articles will be published.
A Stochastic Model by the Fourier Transform of Pde for the Glp - 1IJERA Editor
The peptide hormone glucagon like peptide GLP -1 has most important actions resulting in glucose lowering
along with weight loss in patients with type 2 diabetes. As a peptide hormone, GLP -1 has to be administered by
injection. A few small-molecule agonists to peptide hormone receptors have been described.
Here we develop a model for credit risk based on a model with stochastic eigen values called principal
component stochastic covariance.
In this paper, we consider an AAI with two types of insurance business with p-thinning dependent
claims risk, diversify claims risk by purchasing proportional reinsurance, and invest in a stock with Heston
model price process, a risk-free bond, and a credit bond in the financial market with the objective of maximizing
the expectation of the terminal wealth index effect, and construct the wealth process of AAI as well as the the
model of robust optimal reinsurance-investment problem is obtained, using dynamic programming, the HJB
equation to obtain the pre-default and post-default reinsurance-investment strategies and the display expression
of the value function, respectively, and the sensitivity of the model parameters is analyzed through numerical
experiments to obtain a realistic economic interpretation. The model as well as the results in this paper are a
generalization and extension of the results of existing studies.
S. Corradini, L. Martinez, 30 Novembre - 1 Dicembre 2021 -
Webinar: L'inclusione lavorativa: il panorama nazionale e l'esperienza dell'Istat
Titolo: La condizione occupazionale delle persone con disabilità
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Webinar: Il quadro informativo per il Green Deal: sviluppi e domanda informativa per le questioni energetiche
Titolo: La misura della povertà energetica in Italia
V. Buratta, 30 Novembre - 1 Dicembre 2021 -
Webinar: La strategia dei dati: l’iniziativa europea e la risposta nazionale
Titolo: Il ruolo dell'Istat nella Strategia Nazionale ed Europea dei Dati
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Webinar: Gender statistics by default: il cambiamento di paradigma nelle statistiche e oltre
Titolo: Illusioni, luoghi comuni e verità nella lotta alle disparità di genere
A. Perrazzelli, 30 Novembre - 1 Dicembre 2021 -
Webinar: Gender statistics by default: il cambiamento di paradigma nelle statistiche e oltre
Titolo: Qualità di genere per sostenere la crescita
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Webinar: Gli effetti della pandemia sulla soddisfazione per la vita e il benessere: analisi e prospettive
Titolo: L'impatto della pandemia sulla componente soggettiva del Benessere Equo e Sostenibile
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Webinar: Gli effetti della pandemia sulla soddisfazione per la vita e il benessere: analisi e prospettive
Titolo: La pandemia attraverso gli indicatori soggettivi a livello internazionale: un paradosso?
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Webinar: La lezione della crisi per le statistiche demografiche e sociali
Titolo: Il sistema di sorveglianza dei decessi dell'ISS e le nuove prospettive
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Webinar: La lezione della crisi per le statistiche demografiche e sociali
Titolo: Nuovi strumenti e indagini per un'informazione pertinente in fase di emergenza
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Webinar: La lezione della crisi per le statistiche demografiche e sociali
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A review of the growth of the Israel Genealogy Research Association Database Collection for the last 12 months. Our collection is now passed the 3 million mark and still growing. See which archives have contributed the most. See the different types of records we have, and which years have had records added. You can also see what we have for the future.
A workshop hosted by the South African Journal of Science aimed at postgraduate students and early career researchers with little or no experience in writing and publishing journal articles.
How to Make a Field invisible in Odoo 17Celine George
It is possible to hide or invisible some fields in odoo. Commonly using “invisible” attribute in the field definition to invisible the fields. This slide will show how to make a field invisible in odoo 17.
Exploiting Artificial Intelligence for Empowering Researchers and Faculty, In...Dr. Vinod Kumar Kanvaria
Exploiting Artificial Intelligence for Empowering Researchers and Faculty,
International FDP on Fundamentals of Research in Social Sciences
at Integral University, Lucknow, 06.06.2024
By Dr. Vinod Kumar Kanvaria
Executive Directors Chat Leveraging AI for Diversity, Equity, and InclusionTechSoup
Let’s explore the intersection of technology and equity in the final session of our DEI series. Discover how AI tools, like ChatGPT, can be used to support and enhance your nonprofit's DEI initiatives. Participants will gain insights into practical AI applications and get tips for leveraging technology to advance their DEI goals.
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Normal labor is also termed spontaneous labor, defined as the natural physiological process through which the fetus, placenta, and membranes are expelled from the uterus through the birth canal at term (37 to 42 weeks
T. Proietti, M. Marczak, G. Mazzi - EuroMInd-D: A density estimate of monthly gross domestic product for the Euro Area
1. EuroMInd-D: A Density Estimate of Monthly
Gross Domestic Product for the Euro Area
Tommaso Proietti
University of Rome Tor Vergata and CREATES
Martyna Marczak
University of Hohenheim, Germany
Gianluigi Mazzi
Eurostat, Luxembourg
T. Proietti, M. Marczak and G. Mazzi 1 / 37
2. Introduction
Introduction
EuroMInd-D is a density estimate of monthly gross domestic product (GDP)
constructed according to a bottom–up approach, pooling the density estimates of
eleven GDP components, by output and expenditure type.
The components density estimates are obtained from a medium-size dynamic
factor model handling mixed frequencies of observation and ragged–edged
data structures.
They reflect both parameter and filtering uncertainty and are obtained by
implementing a bootstrap algorithm for simulating from the distribution of
the maximum likelihood estimators of the model parameters, and conditional
simulation filters for simulating from the predictive distribution of GDP.
Both algorithms process sequentially the data as they become available in
real time.
The GDP density estimates for the output and expenditure approach are
combined using alternative weighting schemes and evaluated with different
tests based on the probability integral transform and by applying scoring rules.
T. Proietti, M. Marczak and G. Mazzi 2 / 37
3. Introduction
Breakdown of GDP at market prices by output and expenditure type:
From the output side GDP is decomposed as follows:
Label Value added of branch
A–B Agriculture, hunting, forestry and fishing +
C–D–E Industry, incl. Energy +
F Construction +
G–H–I Trade, transport and communication services +
J–K Financial services and business activities +
L–P Other services =
Total Gross Value Added +
TlS Taxes less subsidies on products =
GDP at market prices
The breakdown of total GDP from the expenditure side is the following:
Label Component
FCE Final consumption expenditure +
GCF Gross capital formation +
EXP Exports of goods and services -
IMP Imports of goods and services =
GDP at market prices
T. Proietti, M. Marczak and G. Mazzi 3 / 37
4. Model specification and inference The single index dynamic factor model for the complete data
Model specification: dynamic factor model for the
complete data
Let yt = [y1t, . . . , yit, . . . , yNt]′
, t = 1, . . . n, denote an N × 1 vector of time series,
that we assume to be integrated of order one, or I(1).
The elements of the vector yt include a set of monthly coincident indicators and
the relevant GDP component.
Let xt denote a k × 1 vector of explanatory variables.
The single–index dynamic factor model is specified as follows:
yt = θ(L)µt + µ∗
t + Bxt, t = 1, ..., n,
µt = µt−1 + χt, µ0 = 0,
φ(L)χt = ηt , φ(L) = 1 − φ1L − . . . − φpLp
, ηt ∼ IID N(0, 1),
µ∗
t = [µ∗
1t, . . . , µ∗
it, . . . , µ∗
Nt]′
, i = 1, . . . , N
µ∗
it = µ∗
i,t−1 + mi + χ∗
it,
ϕi (L)χ∗
it = η∗
it, ϕi (L) = 1 − ϕi1L − . . . − ϕipi Lpi
, η∗
it ∼ IID N(0, σ2
i ),
(1)
where L denotes the lag operator.
T. Proietti, M. Marczak and G. Mazzi 4 / 37
5. Model specification and inference The single index dynamic factor model for the complete data
Model’s features:
All the series share a common factor (the single index µt) which is an
integrated AR(p) process driven by standard Gaussian random disturbances.
The contemporaneous and lagged factor loadings are in the lag polynomial
θ(L) which we assume to be of order one, i.e. θ(L) = θ0 + θ1L, with θ0 and
θ1 being N × 1 vectors.
The component µ∗
t is a vector of idiosyncratic trends, whose first differences
are modelled as independent stationary AR(pi ) processes with mean mi , for
i = 1, . . . , N. We assume that the AR processes φ(L)χt = ηt and
ϕi (L)χ∗
it = η∗
it are stationary.
The disturbances ηt and η∗
it, i = 1, . . . , N, are mutually uncorrelated.
The common cyclical trend is often termed the single index (Stock and Watson,
1991). As for the first differences of yit, we can write
∆yit = mi + θi (L)χt + χ∗
it, t = 2, . . . , n, where θi (L) is the i-th element of θ(L).
T. Proietti, M. Marczak and G. Mazzi 5 / 37
6. Model specification and inference State space form and temporal aggregation
State space representation and temporal aggregation
The monthly model for the complete data in (1) can be represented in state
space form (SSF).
The SSF is modified to take into consideration the observational constraints
arising as a result of temporal aggregation (mixed frequency data).
Partition the vector yt as yt = [y′
1t, y′
2t ]′
y1t collects N1 monthly indicators
y2t is the GDP component, subject to temporal aggregation, so that we
observe
y2,3τ + y2,3τ−1 + y2,3τ−2, τ = 1, 2, . . . , [n/3], (2)
with τ denoting quarters and [·] being integer division.
T. Proietti, M. Marczak and G. Mazzi 6 / 37
7. Model specification and inference State space form and temporal aggregation
Our treatment of temporal aggregation draws on Harvey 1989, who introduced
the so–called cumulator variable, yc
2t , constructed as follows:
yc
2,t = ρtyc
2,t−1 + y2t , (3)
where
ρt =
0, if t = 3(τ − 1) + 1,
1, otherwise.
The vector yc
2t used to create new augmented state and observation vectors. Its
values are unobserved for the first and second month of each quarter.
T. Proietti, M. Marczak and G. Mazzi 7 / 37
8. Model specification and inference State space form and temporal aggregation
Table: Temporal aggregation
t Unobserved y2t Cumulator Availability of yc
2t
1 y21 yc
21 = y21 missing
2 y22 yc
22 = y21 + y22 missing
3 y23 yc
23 = y21 + y22 + y23 observed
4 y24 yc
24 = y24 missing
5 y25 yc
25 = y24 + y25 missing
6 y26 yc
26 = y24 + y25 + y26 observed
7 y27 yc
27 = y27 missing
..
.
..
.
..
.
..
.
T. Proietti, M. Marczak and G. Mazzi 8 / 37
9. Model specification and inference Estimation and signal extraction
Estimation and signal extraction
The model is estimated by maximum likelihood, using the prediction error
decomposition, performed by the Kalman filter
Sequential processing is used as an efficient algorithm for multivariate time
series with missing values and ragged-edge structure. The univariate time
series are processed in a sequence that reflects their publication schedule.
T. Proietti, M. Marczak and G. Mazzi 9 / 37
10. Density estimation, bootstrapping and conditional simulation Density estimation for GDP components
Density estimation (nowcasting and forecasting)
Let yt denote a generic monthly GDP component; the aim is drawing samples
y
(r)
t+l , t = 1, . . . , n, r = 1, . . . , R, and l ≥ 0, from the conditional distribution
f (yt+l |Y†
s ).
If ψ denotes the vector containing the hyperparameters of the model, we let ˜ψ
denote its maximum likelihood estimator (MLE). Assume that ˜ψ has a distribution
represented by a density function f (˜ψs). The required density is obtained as
f (yt+l |Y†
s ) = f (yt+l |˜ψ, Y†
s )f (˜ψ)d˜ψ. (4)
T. Proietti, M. Marczak and G. Mazzi 10 / 37
11. Density estimation, bootstrapping and conditional simulation Density estimation for GDP components
Bootstrap and conditional simulation
We can draw samples y
(r)
t+l , r = 1, . . . , R, from (4) by the method of composition,
using the following algorithm:
1 Obtain a bootstrap sample ˜ψ
(r)
∼ f (˜ψ). The paper documents a bootstrap
algorithm that obtains simulated series from the innovations form of the
univariate representation of the multivariate state space form, conditional on
the MLE ˜ψ.
2 Obtain an independent sample y
(r)
t+l ∼ f (yt+l |˜ψ
(r)
, Y†
s ), by the simulation
smoother. Conditional on the parameter vector ˜ψ
(r)
, we draw samples from
the conditional distribution of the states, and hence of the monthly GDP
component, given the past (filtered distribution), the current information
(real–time distribution), and all the available information (smoothed
distribution).
T. Proietti, M. Marczak and G. Mazzi 11 / 37
12. Density estimation, bootstrapping and conditional simulation Pooling the density estimates of the GDP components
Pooling the density estimates of the GDP components
The methods outlined in the previous section yield estimates for the monthly
GDP components in chain–linked volumes, with the year 2000 as the
reference year.
As it is well known, chain–linked volume measures are not consistent in
aggregation, e.g. the sum of the value added of the six sectors plus taxes less
subsidies would not deliver GDP at market prices, unless they are first
expressed at the average prices of the previous years.
To obtain our density estimates of monthly GDP at market prices and
chained volumes from the output and expenditure approaches, labelled
EuroMInd-Do and EuroMInd-De, we need to pool the GDP components
density draws, according to a multistep procedure proposed by Frale et al
(2011), that enforces the so–called annual overlap method.
T. Proietti, M. Marczak and G. Mazzi 12 / 37
13. Density estimation, bootstrapping and conditional simulation Pooling the density estimates of the GDP components
The procedure consists essentially of three main steps:
1 Dechaining, aiming at expressing the draws at the average prices of the
previous years.
2 Aggregation, which computes total GDP for the output and expenditure
approaches, expressed at the average prices of the previous year, according to
the two identities:
GDP at market prices = i Value added of branch i + TlS,
i = A–B, C–D–E, F, G–H–I, J–K, L–P
GDP at market prices = FCE + GCF + EXP −IMP
3 Chain linking, aiming at expressing GDP at chain–linked volumes with
reference year 2000.
T. Proietti, M. Marczak and G. Mazzi 13 / 37
14. Density estimation, bootstrapping and conditional simulation Pooling the density estimates of the GDP components
Application of this procedure results in the density estimates of monthly GDP
from the output and expenditure approaches, labelled EuroMInd-Do and
EuroMInd-De, respectively. These estimates arise from a linear opinion pool with
known fixed aggregation weights of the conditional densities of the GDP
components at the prices of the previous years, and the final densities are then
converted into chain–linked volumes.
Our methodology ensures that the sum of draws from the conditional GDP density
across the months making up the quarter is consistent with the GDP figure at the
average prices of the previous year published by Eurostat.
T. Proietti, M. Marczak and G. Mazzi 14 / 37
15. Empirical analysis: EuroMInd-D estimates The data
The data
A total of 36 time series is used to estimate EuroMInd-D.
The sample period starts in January 1995 and ends in June 2014 for most of
the monthly indicators.
The GDP quarterly components are available up to the first quarter of 2014;
for the second quarter, only the flash estimate of total GDP is available.
The series concerning the GDP components are released with 65 days of
delay with respect to the end of each quarter.
Among the monthly indicators, the financial aggregates are compiled by the
ECB with a publication delay of around 30 days from the closing of the
reference month. The data for the Industry sector and retail (such as the
Industrial Production Index and Car registrations) are released about 45 days
after the end of the reference month. Other indicators, such as those for
construction (index of production and building permits), the series for the
agricultural sector and the labour market (employment and hours worked)
have a publication delay of about 70 days.
T. Proietti, M. Marczak and G. Mazzi 15 / 37
16. Empirical analysis: EuroMInd-D estimates The data
Time series Frequency Delay
A–B: Agriculture, hunting and fishing
Production of milk m 60
Bovine meat production in tons m 60
Value added (chain–linked volumes) AB q 65
C–D–E: Industry, incl. energy
Index of Industrial Production Germany m 45
Index of Industrial Production France m 45
Index of Industrial Production Italy m 45
Index of Industrial Production Spain m 45
Volume of work done (hours worked) m 60
Value added (chain–linked volumes) CDE q 65
F: Construction
Monthly production index m 70
Building permits m 70
Volume of work done (hours worked) m 70
Value added (chain–linked volumes) F q 65
G–H–I: Trade, transport and communication services
Monthly production index for consumption goods m 45
Index of deflated turnover m 35
Car registrations m 15
Value added (chain–linked volumes) GHI q 65
J–K: Financial services and business activities
Monetary aggregate M3 (deflated) m 27
Loans of MFI (deflated) m 27
Value added (chain–linked volumes) JK q 65
L–P: Other services
Debt securities issued by central government (deflated) m 27
Value added (chain–linked volumes) LP q 65
T. Proietti, M. Marczak and G. Mazzi 16 / 37
17. Empirical analysis: EuroMInd-D estimates The data
Time series Frequency Delay
TlS: Taxes less subsidies on products
Index of Industrial Production for the euro area m 45
Index of deflated turnover, retail sector m 35
Taxes less subsidies (chain–linked volumes) q 65
FCE: Final consumption expenditure
Monthly production index for consumption goods m 45
Index of deflated turnover, retail sector m 35
Car registrations m 15
Final consumption expenditure (chain–linked volumes) q 65
GCF: Gross capital formation
Monthly production index (CDE) euro area m 45
Monthly production index for capital goods m 45
Building permits m 70
Gross capital formation (chain–linked volumes) q 65
EXP: Exports of goods and services
Monthly Export volume index m 42
Monthly production index for intermediate goods m 45
Exports of goods and services (chain–linked volumes) q 65
IMP: Imports of goods and services
Monthly Import volume index m 42
Monthly production index for intermediate goods m 45
Imports of goods and services (chain–linked volumes) q 65
T. Proietti, M. Marczak and G. Mazzi 17 / 37
18. Empirical analysis: EuroMInd-D estimates The EuroMInd-D historical density estimates
The EuroMInd-D historical density Estimates
We illustrate the monthly GDP density estimates conditional on the complete
dataset available at the time of writing (mid July 2014). Our density
estimates are based on M = 5, 000 draws from the conditional distribution of
total GDP, obtained from pooling the draws of the components.
The EuroMInd indicator by Frale et al. (2011) combines the two point
estimates of monthly GDP obtained from the output and the expenditure
approaches using weights that are proportional to the average estimation
error variance. The weights used for EuroMind could be adopted to combine
the density forecasts as well, so that EuroMInd-D = 0.75 × EuroMInd-Do +
0.25 × EuroMInd-De.
T. Proietti, M. Marczak and G. Mazzi 18 / 37
19. Empirical analysis: EuroMInd-D estimates The EuroMInd-D historical density estimates
1996 1998 2000 2002 2004 2006 2008 2010 2012 2014
500
520
540
560
580
600
620
640
660
Median
Figure: EuroMInd-D. Shaded regions correspond to 50%, 70% and 95% probability
bands, respectively.
T. Proietti, M. Marczak and G. Mazzi 19 / 37
20. Empirical analysis: EuroMInd-D estimates The EuroMInd-D historical density estimates
1998 2000 2002 2004 2006 2008 2010 2012 2014
−6
−4
−2
0
2
4 Median
Figure: EuroMInd-D in growth rates. Shaded regions correspond to 50%, 70% and 95%
probability bands, respectively
T. Proietti, M. Marczak and G. Mazzi 20 / 37
21. Empirical analysis: EuroMInd-D estimates The EuroMInd-D historical density estimates
1998 2000 2002 2004 2006 2008 2010 2012 2014
−6
−4
−2
0
2
4 Median
(a) Output approach
1998 2000 2002 2004 2006 2008 2010 2012 2014
−6
−4
−2
0
2
4 Median
(b) Expenditure approach
Figure: EuroMInd-D in growth rates. Shaded regions correspond to 50%, 70% and 95%
probability bands, respectively.
T. Proietti, M. Marczak and G. Mazzi 21 / 37
22. Empirical analysis: EuroMInd-D estimates Evaluation and combination: a pseudo real–time experiment (hindcasting)
Evaluation and combination: a pseudo real–time
experiment
We assess the accuracy of the density estimates by comparing them to the
quarterly GDP observations by a pseudo real-time exercise.
We divide the whole sample into the training sample from 1995.Q1 to
2000.Q4 and the evaluation sample from 2001.Q1 to 2014.Q1.
We focus on three GDP density estimates for quarter τ, that we make
available respectively 3, 2, and 1 months in advance with respect to the
published GDP figure.
The GDP figure becomes available 65 days after the closing of the reference
quarter τ, i.e. at time (in months) 3τ + 2.5
T. Proietti, M. Marczak and G. Mazzi 22 / 37
23. Empirical analysis: EuroMInd-D estimates Evaluation and combination: a pseudo real–time experiment (hindcasting)
Our estimates are computed respectively after the closing of quarter τ − 1 at
times 3(τ − 1) + 1.5, 3(τ − 1) + 2.5 and 3(τ − 1) + 3.5. In providing density
forecasts for quarter τ, we thus distinguish between three information sets.
The first density estimate is conditional on the information until 3(τ − 1) and
the monthly indicators available in 3(τ − 1) + 1.5.
The second information set additionally includes the monthly indicators in
3(τ − 1) + 2.5 and GDP for quarter τ − 1.
The last density forecasts is conditioned on the third information up to and
including period 3(τ − 1) + 3.5.
Depending on a particular information set, forecast samples are first obtained
for every month of the considered quarter τ and are subsequently aggregated
to quarterly density forecasts.
Density forecasts for every GDP component are based on M = 1, 000 draws
from the respective conditional distribution.
T. Proietti, M. Marczak and G. Mazzi 23 / 37
24. Empirical analysis: EuroMInd-D estimates Evaluation and combination: a pseudo real–time experiment (hindcasting)
Figure: EuroMInd-Do (output approach): information set 1
2002 2004 2006 2008 2010 2012 2014
−4
−2
0
2
4
Median
Actual
T. Proietti, M. Marczak and G. Mazzi 24 / 37
25. Empirical analysis: EuroMInd-D estimates Evaluation and combination: a pseudo real–time experiment (hindcasting)
Figure: EuroMInd-Do (output approach): information set 2
2002 2004 2006 2008 2010 2012 2014
−6
−4
−2
0
2
4
T. Proietti, M. Marczak and G. Mazzi 25 / 37
26. Empirical analysis: EuroMInd-D estimates Evaluation and combination: a pseudo real–time experiment (hindcasting)
Figure: EuroMInd-Do (output approach): information set 3
2002 2004 2006 2008 2010 2012 2014
−6
−4
−2
0
2
4
T. Proietti, M. Marczak and G. Mazzi 26 / 37
27. Empirical analysis: EuroMInd-D estimates Evaluation and combination: a pseudo real–time experiment (hindcasting)
Figure: EuroMInd-De (expenditure approach): information set 1
2002 2004 2006 2008 2010 2012 2014
−6
−4
−2
0
2
4
Median
Actual
T. Proietti, M. Marczak and G. Mazzi 27 / 37
28. Empirical analysis: EuroMInd-D estimates Evaluation and combination: a pseudo real–time experiment (hindcasting)
Figure: EuroMInd-De (expenditure approach): information set 2
2002 2004 2006 2008 2010 2012 2014
−6
−4
−2
0
2
4
T. Proietti, M. Marczak and G. Mazzi 28 / 37
29. Empirical analysis: EuroMInd-D estimates Evaluation and combination: a pseudo real–time experiment (hindcasting)
Figure: EuroMInd-De (expenditure approach): information set 3
2002 2004 2006 2008 2010 2012 2014
−6
−4
−2
0
2
4
T. Proietti, M. Marczak and G. Mazzi 29 / 37
30. Empirical analysis: EuroMInd-D estimates Evaluation and combination: a pseudo real–time experiment (hindcasting)
Density combination
We combine the predictive densities arising from the output and the expenditure
approaches using a linear opinion pool.
cτ (u) = wo,τ fτ (u|Io,κ) + we,τ fτ (u|Ie,κ),
cτ (u): pooled forecast density at quarter τ,
Ii,κ, i = o, e,: information set available at time point κ for forecasting quarter τ.
We use recursive weights:
wi,τ =
si,τ
i∈ o,e si,τ
, i = o, e
based on the log score, si,τ = exp τ
τ LogSτ (yτ |Ii,κ) .
based on the continuous ranked prob. score (CRPS),
si,τ =
τ
τ CRPSτ (yτ |Ii,κ) .
Additionally, we consider two non–recursive weighing schemes (wi,τ = wi ):
equal weights (wi = 1/2) and weights based on the MSE (si = 1/MSEi ) .
T. Proietti, M. Marczak and G. Mazzi 30 / 37
31. Empirical analysis: EuroMInd-D estimates Evaluation and combination: a pseudo real–time experiment (hindcasting)
2002 2004 2006 2008 2010 2012 2014
−6
−4
−2
0
2
4
Median
Actual
2002 2004 2006 2008 2010 2012 2014
−6
−4
−2
0
2
4
2002 2004 2006 2008 2010 2012 2014
−6
−4
−2
0
2
4
2002 2004 2006 2008 2010 2012 2014
−6
−4
−2
0
2
4
Median
Actual
2002 2004 2006 2008 2010 2012 2014
−6
−4
−2
0
2
4
2002 2004 2006 2008 2010 2012 2014
−6
−4
−2
0
2
4
Figure: Combined real–time quarterly density forecasts of the Euro area annual GDP
growth rates 2001.Q1 – 2014.Q1. Left panels: log score, information set 1, 2, 3. Right
panels: CRPS: information set 1, 2, 3
T. Proietti, M. Marczak and G. Mazzi 31 / 37
32. Empirical analysis: EuroMInd-D estimates Evaluation and combination: a pseudo real–time experiment (hindcasting)
2004 2008 2012
0.2
0.4
0.6
0.8
2004 2008 2012
0.4
0.6
0.8
2004 2008 2012
0.3
0.4
0.5
0.6
0.7
Figure: Recursive CRPS weights: information set 1, 2, 3, respectively (columns); solid
line: output approach, dash–dot line: expenditure approach
T. Proietti, M. Marczak and G. Mazzi 32 / 37
35. Conclusions
Conclusions
The paper has presented EuroMInd-D, a density estimate of monthly GDP in
chain-linked volumes based on the pooling of the density estimates for 11
GDP components.
The density predictions and nowcasts appear to be well calibrated, when they
are conditional on an information set that includes at least the release of the
quarterly national accounts for the previous quarter.
The sharpness of the probabilistic estimates renders EuroMInd-D a useful
tool for the assessment of macroeconomic conditions in the euro area.
While the current paper concentrated on the evaluation of its predictive
accuracy, we think that EuroMInd-D can serve well the purpose of
characterising the business cycle via the probabilistic detection of turning
points and the decomposition of output into trends and cycles.
T. Proietti, M. Marczak and G. Mazzi 35 / 37
36. Conclusions
The density estimates reflect parameter and filtering uncertainty. They do
not incorporate model uncertainty, as the specification of the model is taken
as given and capitalises upon the indicator selection and specification search
(number of factors and their lags, autoregressive orders) performed in Frale et
al. (2011).
Further research should be directed towards the incorporation of business
survey variables, often referred to as soft indicators, in the information set.
Our preliminary experimentation, based on the two factors specification
considered in Frale et al. (2011), led to reject their inclusion on the grounds
of the lack of sharpness and overdispersion of the density estimates, due to
the contribution of parameter uncertainty.
T. Proietti, M. Marczak and G. Mazzi 36 / 37