- •Preface
- •Contents
- •Chapter 1
- •1.1 International Financial Markets
- •Foreign Exchange
- •Covered Interest Parity
- •Uncovered Interest Parity
- •Futures Contracts
- •1.2 National Accounting Relations
- •National Income Accounting
- •The Balance of Payments
- •1.3 The Central Bank’s Balance Sheet
- •Chapter 2
- •2.1 Unrestricted Vector Autoregressions
- •Lag-Length Determination
- •Granger Causality, Econometric Exogeniety and Causal
- •Priority
- •The Vector Moving-Average Representation
- •Impulse Response Analysis
- •Forecast-Error Variance Decomposition
- •Potential Pitfalls of Unrestricted VARs
- •2.2 Generalized Method of Moments
- •2.3 Simulated Method of Moments
- •2.4 Unit Roots
- •The Levin—Lin Test
- •The Im, Pesaran and Shin Test
- •The Maddala and Wu Test
- •Potential Pitfalls of Panel Unit-Root Tests
- •2.6 Cointegration
- •The Vector Error-Correction Representation
- •2.7 Filtering
- •The Spectral Representation of a Time Series
- •Linear Filters
- •The Hodrick—Prescott Filter
- •Chapter 3
- •The Monetary Model
- •Cassel’s Approach
- •The Commodity-Arbitrage Approach
- •3.5 Testing Monetary Model Predictions
- •MacDonald and Taylor’s Test
- •Problems
- •Chapter 4
- •The Lucas Model
- •4.1 The Barter Economy
- •4.2 The One-Money Monetary Economy
- •4.4 Introduction to the Calibration Method
- •4.5 Calibrating the Lucas Model
- •Appendix—Markov Chains
- •Problems
- •Chapter 5
- •Measurement
- •5.2 Calibrating a Two-Country Model
- •Measurement
- •The Two-Country Model
- •Simulating the Two-Country Model
- •Chapter 6
- •6.1 Deviations From UIP
- •Hansen and Hodrick’s Tests of UIP
- •Fama Decomposition Regressions
- •Estimating pt
- •6.2 Rational Risk Premia
- •6.3 Testing Euler Equations
- •Volatility Bounds
- •6.4 Apparent Violations of Rationality
- •6.5 The ‘Peso Problem’
- •Lewis’s ‘Peso-Problem’ with Bayesian Learning
- •6.6 Noise-Traders
- •Problems
- •Chapter 7
- •The Real Exchange Rate
- •7.1 Some Preliminary Issues
- •7.2 Deviations from the Law-Of-One Price
- •The Balassa—Samuelson Model
- •Size Distortion in Unit-Root Tests
- •Problems
- •Chapter 8
- •The Mundell-Fleming Model
- •Steady-State Equilibrium
- •Exchange rate dynamics
- •8.3 A Stochastic Mundell—Fleming Model
- •8.4 VAR analysis of Mundell—Fleming
- •The Eichenbaum and Evans VAR
- •Clarida-Gali Structural VAR
- •Appendix: Solving the Dornbusch Model
- •Problems
- •Chapter 9
- •9.1 The Redux Model
- •9.2 Pricing to Market
- •Full Pricing-To-Market
- •Problems
- •Chapter 10
- •Target-Zone Models
- •10.1 Fundamentals of Stochastic Calculus
- •Ito’s Lemma
- •10.3 InÞnitesimal Marginal Intervention
- •Estimating and Testing the Krugman Model
- •10.4 Discrete Intervention
- •10.5 Eventual Collapse
- •Chapter 11
- •Balance of Payments Crises
- •Flood—Garber Deterministic Crises
- •11.2 A Second Generation Model
- •Obstfeld’s Multiple Devaluation Threshold Model
- •Bibliography
- •Author Index
- •Subject Index
(54)
(55)
74 CHAPTER 2. SOME USEFUL TIME-SERIES METHODS
Linear Filters
You can see how a Þlter changes the character of a time series by comparing the spectral density function of the original observations with that of the Þltered data.
Let the original data qt have the Wold moving-average representation, qt = b(L)²t where b(L) = P∞ bjLj and ²t iid with E(²t) = 0
j=0
and Var(²t) = σ²2. The k-th autocovariance is
γk = E(qtqt−k) = E[b(L)²tb(L)²t−k] |
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But from (2.111), you know that s(ω) = g(2eπiω) . To summarize, these results, the spectral density of qt can be represented as
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the Þltered data is g˜(z) = σ²2b(z)b(z−1) = σ²2a(z)b(z)b(z−1)a(z−1) = a(z)a(z−1)g(z), and letting z = e−iω, the spectral density function of
the Þltered data is
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2.7. FILTERING |
75 |
The Þlter has the e ect of scaling the spectral density of the original observations by a(e−iω)a(eiω). Depending on the properties of the Þlter, some frequencies will be magniÞed while others are downweighted.
One way to classify Þlters is according to the frequencies that are allowed to pass through and those that are blocked. A high pass Þlter lets through only the high frequency components. A low pass Þlter allows through the trend or growth frequencies. A business cycle pass Þlter allows through frequencies ranging from 6 to 32 quarters. The most popular Þlter used in RBC research is the Hodrick—Prescott Þlter, which we discuss next.
The Hodrick—Prescott Filter
Hodrick and Prescott [76] assume that the original series qt is generated by the sum of a trend component (τt) and a cyclical (ct) component, qt = τt + ct. The trend is a slow-moving low-frequency component and is in general not deterministic. The objective is to construct a Þlter to to get rid of τt from the data. This leaves ct, which is the part of the data to be studied. The problem is that for each observation qt, there are two unknowns (τt and ct). The question is how to identify the separate components?
The cyclical part is just the deviation of the original series from the long-run trend, ct = qt − τt. Suppose your identiÞcation scheme is to minimize the variance of the cyclical part. You would end up setting its variance to 0 which means setting τt = qt. This doesn’t help at all—the trend is just as volatile as the original observations. It therefore makes sense to attach a penalty for making τt too volatile. Do this by minimizing the variance of ct subject to a given amount of prespeciÞed ‘smoothness’ in τt. Since ∆τt is like the Þrst derivative of the trend and ∆2τt is like the second derivative of the trend, one way to get a smoothly evolving trend is to force the Þrst derivative of the trend to evolve smoothly over time by limiting the size of the second derivative. This is what Hodrick and Prescott suggest. Choose a sequence of points {τt} to minimize
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76 CHAPTER 2. SOME USEFUL TIME-SERIES METHODS
where λ is the penalty attached to the volatility of the trend component. For quarterly data, researchers typically set λ = 1600.33 Noting that ∆2τt+1 = τt+1 − 2τt + τt−1, di erentiate (2.114) with respect to τt and re-arrange the Þrst-order conditions to get the Euler equations
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Get the trend component by τ = (λG+IT )−1q. The cyclical component
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33The following derivation of the Þlter follows Pederson [121].
2.7. FILTERING |
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Properties of the Hodrick—Prescott Filter
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You’ve already determined that qt = (λu(L) + 1)τt = v(L)τt where v(L) = 1 + λu(L) = 1 + λ(1 − L)2(1 − L−1)2, so it follows that
τt = v(L)−1qt = 1 + λ(1 − Lq)t2(1 − L−1)2 .
v−1(L) is the trend Þlter. Once you compute τt, subtract the result from the data, qt to get ct. This is equivalent to forming ct = δ(L)qt where
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Since (1 − L)2(1 − L−1) = L−2(1 − L)4, the Þlter is equivalent to Þrst applying (1 −L)4 on qt, and then applying λL−2v−1(L) on the result.34 This means the Hodrick-Prescott Þlter can induce stationary into the cyclical component from a process that is I(4).
The spectral density function of the cyclical component is sc(ω) = δ(e−iω)δ(eiω)sq(ω), where
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From our trigonometric identities, (1−e−iω)(1−eiω) = 2(1−cos(ω)), it follows that δ(ω) = 4λ[1−cos(ω)]2+1 . Each frequency of the original series
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34This is shown in King and Rebelo (84).
78 CHAPTER 2. SOME USEFUL TIME-SERIES METHODS
1.2 |
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Figure 2.4: Scale factor |δ(ω)|2 for cyclical component in the Hodrick— Prescott Þlter.